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East-West Asymmetry in Coastal Temperatures of Hudson Bay as a Proxy for Sea Ice
by
Peter Graeme McGovern
A thesis submitted in conformity with the requirements for the degree of Masters of Science Graduate Department of Geography
University of Toronto
© Copyright by Peter Graeme McGovern (2013)
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East-West Asymmetry in Coastal Temperatures of Hudson Bay as a Proxy for Sea Ice
Peter Graeme McGovern
Masters of Science
Graduate Department of Geography
University of Toronto
2013
Abstract
The seasonal asymmetry in coastal temperatures on Hudson Bay was explored
and evaluated as a proxy to hindcast sea ice conditions prior to 1972. Various indices of
air temperature difference (∆T) between Churchill, MB and Inukjuak, QC were tested for
linear correlations with spatially averaged sea ice concentration (SIC) and ice-free season
length (IFS). A multiple regression equation employing a 31-day average of peak ∆T and
a 61-day average of temperature during freeze-up reproduced the IFS record with an
average error of 8.1 days. This equation was employed to extend the IFS record by 28
years. The resulting 68-year time series revealed a significant increasing trend most
pronounced from 1985 to 2011. Hindcast data helped eliminate low-frequency climate
oscillations of periodicity <68 years as a source of this trend, lending further evidence to
the growing consensus of a declining sea ice being the result of anthropogenic climate
forcing.
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Acknowledgments
First and foremost I would like to thank my supervisor, Dr. Bill Gough, for giving
me the opportunity to study a topic of great interest and importance to me, while offering
his expertise and mentorship along the way. I am incredibly grateful for this formative
experience, which was made all the more valuable and interesting by Bill’s unique
teaching style and infectious enthusiasm for geography and climatology.
I would like to extend my gratitude to the two other committee members, Dr.
Sharon Cowling and Dr. Tanzina Mohsin, for offering their feedback in the final stages of
my thesis, and for cultivating my interests through thought-provoking coursework.
I would also like to acknowledge the contributions of individuals who graciously
offered their time to ensure the statistical soundness of the results presented herein:
Shannon Allen for taking her time to address all my concerns relating to climate data,
Slawomir Kowal for offering his help with sea ice data, and Dr. Ken Butler for lending
his expertise on statistics and trend analysis.
I am also very grateful to the University of Toronto Geography Department for
providing the funding that made this research possible
To my family, and to my partner Danielle, thank you for your continued love and
support.
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Table of Contents Chapter 1: Introduction ....................................................................................................... 1
1.1 Relevance .................................................................................................................. 2 1.2 Research Objectives .................................................................................................. 4
Chapter 2: Literature Review .............................................................................................. 6 2.1 Sea Ice Measurement ................................................................................................ 6 2.2 Seasonal Breakup and Freeze-up Patterns on Hudson Bay ...................................... 7 2.3 Temporal Trends in Hudson Bay Sea Ice ................................................................. 8 2.4 East-West Asymmetry in Hudson Bay ................................................................... 10 2.5 Thermal Modification ............................................................................................. 11
2.5.1 Physical Properties of Sea Ice vs. Water ......................................................... 12 2.5.2 Heat Flux over Open Water ............................................................................. 14 2.5.3 Heat Flux over Ice ............................................................................................ 16
2.6 Temperature as a Proxy for Sea Ice ........................................................................ 18 2.7 Other Proxies for Sea Ice ........................................................................................ 21 2.8 Literature Summary ................................................................................................ 23
Chapter 3: Methodology ................................................................................................... 25 3.1 Site Selection and Description ................................................................................ 25
3.1.1 Hudson Bay Region ......................................................................................... 25 3.1.2 Churchill and Inukjuak: Local Climatic Factors .............................................. 26 3.1.3 Weather Stations/Climate Data ........................................................................ 28
3.2 Defining Temperature Asymmetry: ∆T .................................................................. 29 3.3 Assessing Weekly SIC-ΔTW Correlation ................................................................ 29 3.4 Assessing IFS -∆T Correlation ............................................................................... 31
3.4.1 Capturing Maximum ∆T .................................................................................. 31 3.4.2 Determining Ice-Free Season Length .............................................................. 32 3.4.3 Classification of ∆TMAX by IFS ....................................................................... 33
3.5 Wind Direction Analysis ......................................................................................... 35 3.5.1 Wind Direction Counts/Wind Rose Construction for ∆TMAX Period ............... 35 3.5.2 Re-classification of ∆TMAX for Low NE+E Years ........................................... 36
3.6 Evaluating Proxy Performance: Temperature as a Benchmark .............................. 37 3.7 Combined Approach: ∆TMAX and TF in a Multi-Proxy .......................................... 38 3.8 Hindcasting and Trend Analysis of Extended Record ............................................ 39 3.9 Notes on Data Quality ............................................................................................. 41
3.8.1 Temperature Data ............................................................................................. 41 3.8.2 Wind Direction Data ........................................................................................ 42 3.8.3 Ice-free Season Data ........................................................................................ 43
Chapter 4: Results ............................................................................................................. 44 4.1 ΔT Climate Normal ................................................................................................. 44 4.2 Weekly SIC-ΔTW Correlation ................................................................................. 45 4.3 IFS-ΔTMAX Correlation ........................................................................................... 46
4.3.1 Classification of ∆TMAX by IFS ........................................................................ 48 4.4 Wind Direction Analysis ......................................................................................... 51
4.4.1 Wind Direction Frequency Distributions ......................................................... 51
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4.4.2 Correlation of Wind Direction Components to IFS ......................................... 58 4.4.3 Classification of ∆TMAX by IFS for Low NE+E Years .................................... 58
4.5 IFS-TF Correlation .................................................................................................. 61 4.5.1 Classification of TF by IFS .............................................................................. 62
4.6 IFS-∆TMAX-TF Multiple Linear Regression ............................................................. 64 4.7 Hindcast IFS............................................................................................................ 67
Chapter 5: Discussion ....................................................................................................... 70 5.1 Interpreting ∆T Climate Normal ............................................................................. 70 5.2 SIC-∆TW Relationship ............................................................................................. 71 5.3 IFS-∆TMAX Relationship ......................................................................................... 72 5.5 Wind Direction ........................................................................................................ 75 5.5 Multiple Variable Approach ................................................................................... 79 5.6 Evaluating Proxies .................................................................................................. 79
5.6.1 Classifications .................................................................................................. 80 5.6.2 Linear Regression ............................................................................................ 81
5.7 Trend Analysis of Extended Record ....................................................................... 82 5.8 Complicating Factors in the Sea Ice-∆T Relationship ............................................ 84 5.8 Sources of Error ...................................................................................................... 87 5.9 Research Impacts .................................................................................................... 88
Chapter 6: Conclusion ....................................................................................................... 90 6.1 Research Objectives ................................................................................................ 90 6.2 Recommendations for Future Research .................................................................. 91
References ......................................................................................................................... 93 Appendix: Wind Roses ................................................................................................... 100
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List of Tables Table 1: Climate station summary. ................................................................................... 28 Table 2: Definition of classes of ice-free season length. .................................................. 33 Table 3: Ice-free season length and ∆TMAX for 1972-2011. ............................................. 47 Table 4: Classification of ∆TMAX by IFS for all years on record. ..................................... 48 Table 5: P-values obtained from interclass comparison of ∆TMAX means by
one-tailed t-test, adjusted using the Bonferroni correction. ................................ 49 Table 6: Identification of misclassified years based on ∆TMAX thresholds. ..................... 50 Table 7: Classification of ∆TMAX by IFS for years when NE+E wind count
is below average. ................................................................................................ 59 Table 8: Identification of misclassified years when NE+E winds count is
below average. .................................................................................................... 60 Table 9: Ice-free season lengths and TF for 1972-2011. .................................................. 61 Table 10: Classification of TF by IFS for all years on record. ......................................... 62 Table 11: P-values obtained from interclass comparison of TF means by
one-tailed t-test, adjusted using the Bonferroni correction. ............................. 63 Table 12: Identification of misclassified years based on TF thresholds ........................... 63 Table 13: Comparison of temperature variables in terms of coefficients
of determination, statistical significance, and percent misclassifications. ....... 64 Table 14: IFS results from Eqn. 1 (TF+∆TMAX) compared with actual IFS in
terms of absolute error for the period 1972-2011. ............................................ 65 Table 15: IFS results from Eqn. 2 (TF) compared with actual IFS in terms of
absolute error for the period of 1972-2011. ..................................................... 66 Table 16: Comparison of temperature variables in terms of the coefficients of
determination and statistical significance of linear relationships with IFS. ....... 67 Table 17: Comparison between baseline and trend in terms of τ and statistical
significance for different time series divisions. .................................................. 69
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List of Figures Figure 1: Site map of Hudson Bay indicating the location of the 36 points for which
breakup and freeze-up dates were derived. ......................................................... 33 Figure 2: Climate normal for ∆T (Churchill Daily Mean T - Inukjuak Daily Mean T)
calculated over the period 1944-2011. ................................................................ 44 Figure 3: Correlation of ∆TW with spatially averaged SIC for all weekly observations
on record 1971-2011. .......................................................................................... 45 Figure 4: Correlation of ∆TW with spatially averaged SIC for all weekly observations
during the breakup period, 1971-2011. ............................................................... 45 Figure 5: Correlation of ∆TW with spatially averaged SIC for all weekly observations
during the freeze-up period, 1971-2011. ............................................................ 46 Figure 6: Climate normal wind rose for Inukjuak over Julian days 320-350, calculated
over the period of 1981-2007. ............................................................................ 51 Figure 7: 1981 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -2.4°C,
IFS = 153 (Long). ............................................................................................... 52 Figure 8: 1982 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -10.5°C,
IFS = 133 (Medium). .......................................................................................... 52 Figure 9: 1983 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -0.2°C,
IFS = 137 (Medium). .......................................................................................... 53 Figure 10: 1985 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.6°C ...... 53 Figure 11: 1986 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = 0.0°C,
IFS = 130 (Medium). .......................................................................................... 54 Figure 12: 1988 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.7C,
IFS = 147 (Medium). .......................................................................................... 54 Figure 13: 1990 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -10.3°C,
IFS = 144 (Medium). .......................................................................................... 55 Figure 14: 1991 wind rose for Inukjuak over Julian days 320-250: ∆TMAX = -12.7°C,
IFS = 141 (Medium). .......................................................................................... 56 Figure 15: 2000 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.4°C,
IFS = 144 (Medium). .......................................................................................... 56 Figure 16: 2002 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -4.0°C,
IFS = 146 (Medium). .......................................................................................... 57 Figure 17: 2004 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.4°C,
IFS = 134 (Medium). .......................................................................................... 57 Figure 18: 2005 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -7.6°C,
IFS = 160 (Long). ............................................................................................... 58 Figure 19: Time series of IFS from 1944-2011 constructed using actual observations
and data derived by proxy from ∆TMAX and TF [Eqn. 2]. ................................... 68 Figure 20: Time series for actual and hindcast IFS smoothed by use of a 5-year
moving average. .................................................................................................. 68 Figure 21: 1984 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -5.1°C,
IFS = 132 (Medium). ........................................................................................ 100 Figure 22: 1987 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -2.8°C,
IFS = 128 (Short). ............................................................................................. 101
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Figure 23: 1989 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -7.6°C, IFS = 141 (Medium). ........................................................................................ 102
Figure 24: 1995 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -5.3°C, IFS = 147 (Medium). ........................................................................................ 102
Figure 25: 1996 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.0°C, IFS = 151 (Long). ............................................................................................. 103
Figure 26: 2001 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.2°C, IFS = 164 (Long). ............................................................................................. 104
Figure 27: 2003 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.6°C, IFS = 158 (Long). ............................................................................................. 105
Figure 28: 2006 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.7°C, IFS = 170 (Long). ............................................................................................. 105
Figure 29: 2007 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.0°C, IFS = 162 (Long). ............................................................................................. 106
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Chapter 1: Introduction
Northeastern Canada’s Hudson Bay, through its unique geographical
characteristics, presents a compelling case study for climatologists and geographers alike.
As the second largest bay in the world, occupying 1,300,000 km2, it exerts a powerful
influence over the regional climate (Martini, 1986). Hudson Bay (HB, the Bay) is also the
largest water body in the world to undergo an annual cycle between total sea ice coverage
and complete open water. This annual cryogenic cycle adds another layer of complexity
to the regional climate, as the interaction between the Bay and the boundary layer
atmosphere fluctuates considerably on a seasonal basis.
Open water bodies have a significant impact on local and regional climate through
exchanges of heat, moisture and momentum with the air above them. The effects of this
are manifest in coastal regions, where temperatures are moderated by open water and
meteorological phenomena such as lake-effect snow and land-sea breezes are common
(Oke, 1978). Sea ice acts to limit this exchange of energy and mass between atmosphere
and water, thus reducing or eliminating these effects (Gerbush et al., 2008; McPhee,
2008; Niziol, 1987). Differences in physical properties between water and sea ice, most
importantly their ability to reflect shortwave radiation, means an even greater contrast in
the energy budgets of an ice-covered vs. an ice-free water body (McPhee, 2008). On
Hudson Bay, the seasonal variation of sea ice, combined with the prevailing westerly
winds, creates an interesting seasonal asymmetry in coastal temperatures. During the ice-
free season, winds arriving on the east coast have been thermally modified through
advection over the Bay, leading to generally warmer conditions than on the west coast.
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This asymmetric temperature signal is very evident following annual extremes of sea ice
cover. The aim of this study is to determine if unique temperature signals exist not only at
these extremes, but also for varying degrees of sea ice cover, with a view to
reconstructing the sea ice record using coastal temperatures as a proxy.
1.1 Relevance
The current consensus that sea ice in Hudson Bay is in decline is based largely on
observations of an approximately 40-year sea ice record (Gagnon & Gough 2005; Gough
et al., 2004a; Hochheim & Barber, 2010; Hochheim et al., 2011). This record, made
available by Environment Canada’s Canadian Ice Service (CIS), relies heavily upon
satellite imagery to maintain accurate, high-resolution coverage of Canada’s northern
regions (CIS, 2013). Prior to the advent of satellite imagery, sea ice data for this area is
sparse and unreliable, constrained to observations from coastal stations, sea vessels, and
airplanes. Trend analysis for any climate variable is sensitive to the length of its record,
as short-term changes sometimes prove less significant in the context of long-term
variability (Hodgkins, 2013). Lengthening the sea ice record could serve to strengthen
the conclusion that a decline has indeed been forced by anthropogenic climate change, as
is the current hypothesis. Alternatively, a longer record might prove recent changes to be
part of some natural low frequency climate oscillation (W. Gough, pers. comm., 2012).
Either way, a more accurate characterization of the trend in Hudson Bay sea ice would be
highly valuable to researchers and policy makers from local to global levels.
The observed negative trend in sea ice on Hudson Bay has social, economic, and
environmental implications at all geographic scales. A thorough understanding of these
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historical trends is essential to establishing linkages to current impacts as well as
projecting future impacts. A longer ice-free season on the Bay has potential positive
economic impacts as it opens up the opportunity for improved navigation of sea vessels
to the Port of Churchill on the Bay’s western coast (Ho, 2010; Stewart et al., 2010).
While this is one example of an impact of sea ice decline that could be construed as
positive, it must nevertheless be weighed against the many negative impacts. Traditional
ways of life for communities along the Bay may cease to be viable as seasonal sea ice
patterns continue to change. Coastal communities practicing subsistence hunting, which
often rely on the presence of sea ice floes as hunting platforms, may be forced to adapt in
response to changes in sea ice (Laidler et al., 2009). The ecological impacts of a negative
sea ice trend have also been studied extensively and shown to be significantly deleterious
to local fauna (Kovacs et al., 2011; Moore & Huntington, 2008). Perhaps the most
notable species to be affected by these changes is the polar bear, whose reliance on sea
ice as a transportation corridor and primary hunting platform leaves them particularly
vulnerable to changes in its patterns (Kovacs et al., 2011; Stirling et al., 1999). The most
significant impact of declining sea ice on a global scale is the potential amplification of
global warming through the ice-albedo feedback loop (Curry et al., 1994). This feedback
mechanism relies on the significantly lower albedo of water compared to sea ice or snow.
Declining sea ice results in a concomitant decline in the sea ice: open water ratio and
hence the overall albedo of Hudson Bay, and the Arctic Ocean in general. A lower albedo
means greater absorption of incoming shortwave radiation, leading to further
amplification of atmospheric warming.
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The impacts described above are all associated with a decline in sea ice or
changes in sea ice patterns that have been correlated with anthropogenic climate change.
Improvements to the sea ice record in terms of continuity and length might serve to
strengthen the basis for the observed trends and their associated impacts. Any new
information garnered in the process would be a boon to researchers and stakeholders in
climate change mitigation and adaptation.
1.2 Research Objectives The two primary research objectives for this thesis are:
1. To investigate the relationship between the east-west coastal asymmetry in temperature of Hudson Bay and sea ice concentration (or other metric of sea ice), identifying and accounting for any other climatic variables obscuring this relationship.
2. To develop a proxy using this temperature asymmetry for the purpose of
reconstructing the sea ice record for Hudson Bay prior to 1972 and conducting a temporal trend analysis.
The basis for this study is the observation of a seasonal change in the temperature
difference between coasts. Objective 1 aims to further explore that asymmetry as it
relates to sea ice, testing the correlation between temperature difference and sea ice
concentration. I hypothesize that though there will be a correlation, it will be limited by
inherent climatic variability, such that the relationship will only be significant at coarser
temporal resolutions. As part of objective 1, it is presumed that wind direction will be an
important climatic variable in need of consideration to effectively characterize the
relationship. I hypothesize that the strength of the temperature asymmetry, while largely
driven by sea ice conditions, will also be highly dependent on, and proportional to, the
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frequency of westerly winds.
In the process of pursuing objective 1, the groundwork is being laid for completing
objective 2. Having characterized the sea ice-temperature asymmetry relationship, a
realistic, simple proxy method will be developed. This proxy will be evaluated by its
ability to reconstruct the existing record. Should it be deemed a useful proxy by this
measure, it will be used to reconstruct sea ice conditions prior to 1972, producing a
lengthened time series upon which temporal trend analyses may be conducted.
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Chapter 2: Literature Review
The following literature review serves to identify the most significant
contributions to the current body of knowledge on sea ice in Hudson Bay. The theoretical
basis for the relationship between sea ice and coastal temperatures will be established
along with the gaps in the knowledge this study aims to address by investigating this
relationship.
2.1 Sea Ice Measurement There are many different metrics employed to track the seasonal patterns of sea
ice formation/melt as well as its long-term trends. Thickness has been used as a measure
of sea ice to track its decline in both the Hudson Bay region (Gagnon & Gough, 2006;
Gough et al., 2004b) and the broader Arctic Ocean (Kwok & Rothrock, 2009; Rothrock
et al., 1999). A thinning trend naturally translates into a decline in sea ice volume,
another unit of measurement for sea ice with precedent in the literature (Kwok et al.,
2009; Rothrock & Zhang, 2005). The most commonly used metrics, however, are sea ice
extent (SIE) and sea ice concentration (SIC). SIE is usually defined as the area that
contains sea ice above a certain concentration threshold, and is widely used in the
literature to monitor climate-induced changes to sea ice (Comiso et al., 2008; Vinnikov et
al., 1999; Parkinson et al., 1999). SIC, on the other hand, is defined as the relative
proportion of sea ice to open water for a given area, usually reported in tenths. SIC has
been a particularly popular metric for examining sea ice patterns and trends in the
Hudson Bay region (Hochheim et al., 2011; Hochheim & Barber, 2010; Wang et al.,
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1994). The advantage of SIC over SIE is that it gives the user specific information on the
ice cover for a particular point or area of interest. SIE can be derived from a map of SIC,
but not vice versa, so SIC inherently contains more information. Breakup and freeze-up
dates, important variables for areas undergoing annual freeze/thaw cycles, have been
defined using the SIC threshold of 5/10. With this methodology, first proposed by Etkin
(1991), breakup is defined as the earliest date when SIC equals 5/10 or less, while freeze-
up is defined as the earliest date when SIC equals 5/10 or more. Though somewhat
arbitrary, this 50% threshold also carries some significance to nautical navigators
(Gagnon & Gough, 2005). This methodology for determining breakup/freeze-up dates
has been adapted and used by Stirling et al. (1999), Gough et al., (2004a), and Gagnon &
Gough (2005).
2.2 Seasonal Breakup and Freeze-up Patterns on Hudson Bay
The progression of sea ice freeze-up and breakup on the Bay is influenced by
regional variations in wind, temperature and water circulation. James Bay is the first
region to undergo breakup in late June due to the relatively warm winds arriving from
northern Ontario (Gagnon & Gough, 2005). Eastern Hudson Bay also undergoes
relatively early breakup due to spring freshwater inputs (Markham, 1986). Shortly
thereafter, offshore SICs in northwestern Hudson Bay also surpass the 5/10 threshold,
likely due to sea ice advection by northwesterly winds (Saucier et al., 2004). Landfast ice
on the northwestern and northeastern shores persists for another 3-4 weeks. The last
region of the Bay to break up is the southwestern shore, typically around the third week
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of July, though remnants of ice may still be present as late as mid-August (Gagnon &
Gough, 2005; Hochheim et al, 2011).
The ice-free period for Hudson Bay is quite short (<3 months), as ice formation in
the northern region begins in late October, starting along the northwestern coast and
along the shores of South Hampton Island (Hochheim & Barber, 2010). In mid-
November, northern Hudson Bay is the first region to reach the 5/10 freeze-up threshold
(Gagnon & Gough, 2005). From there, freeze-up progresses southward and eastward
(Maxwell, 1986) with the southeast portion of the Bay freezing last (Hochheim & Barber,
2010). The Bay as a whole is usually consolidated (SIC≥80%) by late December to early
January. Hence, the ice-covered period is significantly longer than the ice-free period,
lasting on average almost 6 months. These general patterns of breakup and freeze-up
persist from year to year, however the specific dates exhibit a strong interannual
variability and have undergone long-term changes in response to climate forcing (Gough
et al., 2004a; Gagnon & Gough, 2005; Wang et al., 1994).
2.3 Temporal Trends in Hudson Bay Sea Ice
In light of the observed decline in sea ice for the Arctic as a whole (Comiso et al.,
2008: Parkinson et al., 1999; Stroeve et al., 2007; Vinnikov et al., 1999), many recent
studies have attempted to assess what trends might emerge on a more regional scale, with
a particular focus on the Hudson Bay region. Gagnon and Gough (2005) identified trends
in the sea ice freeze-up and breakup dates for the Bay over the period of 1971-2002.
Their findings suggest an overall trend toward later freeze-up and earlier breakup, with
regional variation in the magnitude and statistical significance of these trends. James Bay,
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southern Hudson Bay, and western Hudson Bay all exhibited statistically significant
trends toward earlier breakup, while the northern and northeastern regions of the Bay
exhibited a trend toward later freeze-up. Hochheim et al. (2011) investigated the
atmospheric forces behind the observed trends in sea ice concentration and sea ice extent
in Hudson Bay from 1980 to 2005 during the spring period and Hochheim & Barber
(2010) during the fall period. Many of their findings corroborate previous descriptions of
SIC patterns and trends on the Bay. During the fall, statistically significant trends in SIC
anomalies averaged across the Bay ranged from -23.3% to -26.9% per decade. These
trends were in turn highly correlated with surface air temperature (SAT) anomalies
(Hochheim & Barber, 2010). The spring break-up exhibited similar trends of -15.1% to -
20.4% per decade, also concomitant with increased SATs (Hochheim et al., 2011).
Negative SIC trends in the breakup and freeze-up periods would be expected to
translate into a lengthening trend of the ice-free season. Gough et al. (2004a) found such
a trend in a regional assessment of southwestern Hudson Bay. This study showed a
statistically significant increase in the duration of the ice-free season for the area from
1971 to 2003, driven primarily by a decreasing trend in the breakup date of 0.3 days/year.
Passage of years was used as an implicit measure of warming temperatures, which is
justified by the fact that statistically significant positive trends in spring temperatures
have been observed in nearby northern Ontario locations (Gagnon & Gough, 2002).
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2.4 East-West Asymmetry in Hudson Bay
The basis for the proposed study lies in the seasonally varying differences in
temperature between the east and west coasts of Hudson Bay. This east/west asymmetry
has emerged as a common theme in much of the relevant literature. As described above,
the progression of sea ice breakup and freeze-up on the Bay is non-uniform and
regionally variable such that sea ice may be present on one side of the Bay and absent on
the other depending on the time of year. Hence, we see coastal asymmetry in sea ice
concentrations owing to regional climatic variations. These east-west variations in SIC
are further explored by Hochheim et al. (2011) who examine the role of dynamic and
thermodynamic forcing. Hochheim et al. (2011) compare SIC anomalies in east and west
regions of the Bay during the early spring period in relation to both surface air
temperature and wind. One of their most significant observations was that asymmetries in
SIC were correlated with westerly winds. For example, years with positive sea ice
anomalies in the eastern region and negative sea ice anomalies in the western region
(strong asymmetry) were correlated with strong westerly winds. On the other hand, years
with positive sea ice anomalies on both sides of the bay tended to be associated with
weaker westerly winds. A similar correlation between winds and ice thickness is
observed on an annual basis. Again as the result of eastward dynamic forcing, ice piles up
on the eastern side of Hudson Bay leading to a disparity in thickness when compared
with the upwind west coast (Gagnon & Gough, 2006). These results highlight the role of
dynamic advection on asymmetry of sea ice conditions.
The examples above demonstrate east/west asymmetry that can be observed in a
single year. When considering the long-term trends of sea ice, coastal asymmetry can
11
also arise. In a study investigating the long-term trends of landfast ice thickness in
Hudson Bay, Gagnon and Gough (2006) found very different results for either coast. A
statistically significant thickening trend on the west coast was contrasted with a
statistically insignificant thinning trend on the east coast. The contrasting trends on the
west and east coasts were associated with negative temperature trends and the lack of a
negative temperature trend, respectively, albeit with many exceptions for specific sites.
The lack of correlation between temperature trends and ice thickness for these sites
suggested another important variable, which was identified as snow cover. The results of
this study provide an example of asymmetry in the long-term trends of sea ice on the
Bay.
These observed coastal asymmetries on the Bay in both annual sea ice patterns
and long-term trends in sea ice are an interesting by-product of the unique geography of
Hudson Bay. With the exception of the long-term trend in thickness, the unifying element
seems to be the prevailing westerly/northwesterly winds. This, combined with the vast
distances over which the winds can exert their influence, leads to some interesting east-
west contrasts.
2.5 Thermal Modification
The underlying mechanism leading to the temperature asymmetry on the Bay is
the thermal modification of overlying air through sensible and latent heat transfer. The
seasonality of this temperature asymmetry is brought about by the seasonality of sea ice,
which interacts with the boundary layer in a manner very different from water. The
contrasting roles of ice and water in terms of their ability to modify overlying air arise
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from two fundamental differences (1) the physical properties that dictate how each gains
heat, and (2) the way each exchanges heat with overlying air.
2.5.1 Physical Properties of Sea Ice vs. Water
The contrasting physical properties of land and water are a major driver of
weather and climate from local to global scales. The properties of sea ice are in many
ways analogous to those of snow-covered land or permafrost, though as we will see it can
also behave quite differently. One of the most important distinctions between water and
sea ice is in their albedo (α), or reflecting power of their surface. The albedo of open
water, though very high for solar altitudes of <30°, remains consistently between 0.03 to
0.10 for the majority of the day when the sun is at least 30° above the horizon (Oke,
1978). Averaged over a cloudless day, α for water is approximately 0.06, meaning only
6% of incoming shortwave radiation is reflected (Dieckmann & Hellmer, 2009). The
remaining 94% of that energy is transmitted throughout the water column and absorbed,
increasing the temperature of the water (more on that below).
Obtaining a generalized value for sea ice albedo is much more complicated, as it
can exhibit significant spatial, temporal, and spectral variability (Perovich et al., 1998). If
one were considering a uniform chunk of first-year, snow-covered sea ice, the albedo
would likely be in the range of 0.8-0.9 (Brandt et al., 2005; Grenfell & Perovich, 1984).
Bare ice albedo is significantly lower than snow covered, usually in the range of 0.5-0.7
(Perovich, 1996). For snow-covered ice, the age of the snow is also important as it
becomes more compacted and soiled with time, decreasing its albedo (Oke, 1978).
However, the most dramatic change to sea ice albedo happens when its coverage is
13
interrupted by water. This interruption can be caused by leads (large fractures) or
polynyas (circular opening in the ice caused by oceanic heat flux), in which case the
lower albedo of water can reduce the overall albedo for a given area. Melt ponds, or pools
of open water on top of sea ice resulting from surficial melting in the thawing season, can
also reduce overall albedo. Melt ponds only a few cm deep can reduce albedo down to
~0.5, but this value decreases exponentially with depth until it reaches that of open water
(Morassutti & Ledrew, 1996). Hence, sea ice albedo will decrease as the melt season
progresses, but so long as ice remains in a given area, its α will be greater than that of
water, and less energy will be absorbed than if that area were completely ice-free. As
Hudson Bay undergoes a complete annual cryogenic cycle, its overall albedo will
undergo this change on an annual basis. Furthermore, since all sea ice on the Bay would
be considered first-year ice, there should be no variability in albedo owing to multi-year
ice and average albedo during the period of complete ice cover should be >0.8.
The implication of the large difference in albedo between sea ice and open water
is that open water absorbs a much greater proportion of incident shortwave radiation. For
sea ice, the resulting shortwave flux during the winter months is insufficient to produce
enough heat to initiate a phase change to water, so its temperature rarely surpasses 0°C.
The much larger shortwave flux into open water leaves the potential for a much greater
change in its temperature. However, it is at this point that the other important physical
properties of water present a paradox. Despite being an excellent absorber of radiation,
the thermal response of water to this energy flux is very slow due to its ability to transmit
shortwave radiation to considerable depths, ability to dissipate energy through
convection, and high thermal capacity (Oke, 1978). The resulting thermal inertia of large
14
water bodies is the reason they play such a significant role in weather and climate
through systems such as land-sea breezes and lake-effect snow. Despite this lag between
energy flux and thermal response, large bodies will continue to warm up so long as
incident shortwave radiation is maintained or increasing. In the case of Hudson Bay, the
spatially averaged sea surface temperature (SST) reaches its maximum in August and is
typically ~7.5°C but has been as high as 9.9°C (Galbraith & Larouche, 2011). The
contrast between the higher temperatures of open water and the temperature of the sea ice
surface (0°C or less) is key to understanding the east-west asymmetry.
2.5.2 Heat Flux over Open Water
Sensible and latent heat flux are driven by the differences in temperature and
moisture, respectively, between a surface and the boundary layer. If the air and water
differ in terms of temperature, then there exists a gradient that will eventually be
eliminated by a flux of sensible heat (QH). The formula for sensible heat illustrates how
its flux is proportional to this gradient:
QH=ρACpCH|V|(TA-TSfc)
where, ρA = air density, V= velocity, Cp = specific heat capacity of air at ground,
CH = turbulent exchange coefficient, TA= air temperature, and TSfc= surface temperature
(Friehe & Schmitt, 1976). Say, for example, the overlying air temperature is TA=2°C,
while the temperature of the water at the surface is Tsfc= 7°C, then QH will be directed
upward into the air until a new temperature equilibrium is reached when TA=TSfc.
For latent heat flux, in the case of air advecting over open water, there will always
be a difference in moisture between the two mediums, as air saturated near the surface is
15
diffused by the turbulent atmosphere. This creates a sustained gradient in vapour
concentration, along which evaporation transfers energy (Oke, 1978). Similarly to QH,
latent heat transfer is proportional to that gradient, as well as the turbulent exchange
coefficient. Energy is drawn from the water itself and transferred into the overlying air as
a vertical flux of latent heat (QE). Simply put, the greater the magnitude of the difference
in conditions between surface and air, the stronger the gradient and hence the larger the
heat flux (Oke, 1978). Hence, the higher the SSTs on the Bay, and the more area of
exposed water, the greater potential that exists for upward fluxes in sensible and latent
heat respectively.
When an air mass transitions between surfaces of contrasting temperature (in this
case from permafrost to warmer open water), a thermal internal boundary layer (TIBL)
develops above the new surface within the larger atmospheric boundary layer (Stull,
1988). As the distance travelled by the air mass increases, the TIBL deepens as the now-
unstable warm air rises, driving further convection. By definition, the entire TIBL has
been influenced to some degree by the surface below, but it is usually only the bottom
10% that is considered to be in equilibrium with that surface (Kaimal & Finnigan, 1994).
The distance covered by this air mass travelling over a water body is termed “fetch”.
Initially, the greater the fetch, the longer time an air mass has in contact with open water
and hence the greater the transfer of heat. However, as the TIBL deepens, the differences
in temperature and humidity at the air-water interface are in turn diminishing. Therefore,
there is an upper limit to a fetch distance beyond which equilibrium between air and
water is reached and heat flux ceases to have a warming effect on advecting air (Stull,
1988). Depth of the TIBL grows as a function of fetch to a certain power that is
16
dependent on atmospheric stability, in the range of 0.2 to 0.8. (Stull, 1988). Unstable
conditions promote development of the TIBL, so the power is inversely proportional to
stability. Fetch distances for air masses arriving on the east coast of Hudson Bay may
vary depending on the direction of the wind, but a geodesic line drawn from Churchill
(west coast) to Inukjuak (east coast) yields a distance of 928 km. Studies aiming to
quantify fetch distances required for full adjustment of the boundary layer to new
surfaces are usually concerned with distances far smaller than this, ranging from 10s of
metres to a few hundred km (Garratt, 1990). For fetch distances on the scale of those in
Hudson Bay, it is safe to say that even under stable conditions the TIBL will be fully
developed and hence modulate air temperature downstream.
2.5.3 Heat Flux over Ice
The exchange of heat at an interface between air and ice, while adhering to the
same physical principles outlined above, is very different than that which is seen in the
case of an air-water interface. The latent heat flux from ice is lower than that of water
because in order to release that heat the ice must undergo two phase changes. Hence,
energy that would be expended on transitioning water to vapour (releasing latent heat in
the process) must first be used to facilitate the transition from ice to water (Oke, 1978).
Likewise, sensible heat flux from ice will also be lower than that from water owing to the
fact that its temperature is always <0°C. At the onset of spring melt, when the ice/snow
approach 0°C these energy fluxes become more complicated, but in general upward heat
flux will increase as the surface becomes water-dominated.
17
One of the complicating factors that distinguish sea ice from snow-covered land is
that of ice thickness. While sea ice often acts as a barrier to energy flux between water
and the atmosphere, its insulating power is highly dependent on its thickness (Dieckmann
& Hellmer, 2009). Systems such as Hudson Bay that undergo complete annual cryogenic
cycles experience a continuum of ice thicknesses during the breakup and freeze-up
seasons. Furthermore, even when peak thickness is reached, there will be considerable
spatial variability latitudinally as well as longitudinally owing to the prevailing NW
winds (Gagnon & Gough, 2006; Gough et al., 2004b). It is important to account for these
variations as they can have a dramatic influence over the heat exchange between air and
water, especially when the ice is thin (Maykut, 1982). From the equation:
hQ*=k(TS-TW)
where, h=ice thickness, Q*=net heat flux, k=thermal conductivity of ice, TS=temperature
of ice surface, and TW=water temperature; we can see that heat flux through ice is
proportional to the temperature gradient between water and the ice surface, and inversely
proportional to ice thickness. To further complicate matters, the layer of snow often
found on sea ice has its own insulating properties that are depth-dependent, and act to
reduce heat losses from ice (Maykut, 1986). The heterogeneities in heat flux imparted by
melt ponds, variable ice thickness, and leads/polynyas suggest that: i) even under total ice
cover the energy budget of a water body may differ from that of snow-covered land,
hence ii) a TIBL will likely develop over the water body, but iii) said TIBL will also be
very spatially heterogeneous and complex, comprised of “IBLs within IBLs” (Stull,
1988). The last point is particularly applicable for freeze-up and breakup periods when
sea ice cover is highly variable.
18
Evidently, there are several complex interrelated variables that combine to dictate
energy exchange between air and water in a sea-ice system at any given time. What is
clear is that heat flux from water to the boundary layer is much greater for an ice-free
water surface than an ice-covered one. Studies aiming to quantify this disparity have
revealed a difference of two orders of magnitude. While heat flux over multi-year ice has
been shown to be less than 5 Wm-2 (Maykut, 1982), open water-air heat flux can be as
high as 600 Wm-2 (Maykut, 1986; Andreas & Murphy, 1986). Given that the balance of
this energy will go towards heating the boundary layer, it is evident that sea ice will
modulate regional temperatures to some degree. In areas that undergo seasonal growth
and retreat of sea ice such as Hudson Bay, this influence will be most evident between
annual extremes. In between these extremes, heterogeneities in sea ice concentration and
thickness conspire to make quantifying heat flux over the entire Bay, and hence effects
on temperature, very difficult.
2.6 Temperature as a Proxy for Sea Ice
The relationship between sea ice and the east-west coastal temperature asymmetry
on the Bay is a site-specific one. Since the relationship is dependent on the unique
geography of the area, its use as a tool for predicting or hindcasting cannot be reapplied
to other locations. There is currently no literature that explores this asymmetry, nor any
other metric of temperature as a potential proxy for sea ice on the Bay. Despite the
unique nature of the Bay, studies focusing on similar sites and their accompanying sea
ice-temperature relationships might prove valuable in developing a proxy hindcasting
tool. The fundamental difference between these studies and what is being undertaken by
19
this study must first be stressed. In most cases where temperature acts as proxy for sea
ice, it is the temperature that is driving the resulting sea ice concentration by creating
conditions leading to either its formation or degeneration. In the case of Hudson Bay,
while clearly this is also happening, it is presumed that the sea ice (or lack thereof) is
driving the temperature on the east coast and hence the asymmetric temperature signal.
Despite this important distinction, any use of temperature as a proxy for sea ice would
help evaluate the performance of a new method. Unfortunately, studies on the use of
temperature records as a proxy for Arctic sea ice are scant. More often, broad estimates
on sea ice conditions are inferred indirectly from temperatures which themselves have
been derived via other proxies (Macias-Fauria, 2010; Isaksson et al., 2005; Polyak et al.,
2010) This is perhaps due to the fact that temperatures only serve as a very coarse stand-
in for sea ice, and are therefore only useful when there are no superior alternatives.
Though there is little precedent in the literature for temperature proxies for sea
ice, studies on lake ice may be relevant given Hudson Bay’s morphology. The shallow
channels north of Hudson Bay limits water exchange and thermal influences from the
Atlantic Ocean while advection of sea ice into and out of the Bay is negligible,
characteristics befitting of lakes (Etkin, 1991; Saucier & Dionne, 1998). In a
comprehensive analysis of lake ice records for all Canadian lakes, Williams (1971) found
that the breakup date (defined in this case as the date at which the lake is 100% ice-free)
was predicted within a standard error of 1.6-4.3 days if the date of the start of breakup
was known along with temperatures for the duration of the melting period.
In certain cases, the predictor and predictand in the sea ice-temperature coupling
might be reversed such that sea ice conditions serve as a proxy for air temperature. This
20
approach has shown some success in reconstructing local air temperatures for areas with
extensive ice records. For example, the timing of ice-breakup on a high-altitude lake in
the Swiss Alps was shown to have a shared variance of 64% with local air temperatures
(Livingstone, 1997). In this case, where the ice records predate those of temperature,
breakup dates may be used as part of a multi-proxy approach to hindcast local air
temperature. However, other factors such as local weather, lake morphometry, and
sheltering prevent a more direct relationship between the two variables, and hence limit
accuracy of such predictions. In a similar study based on lakes in Finland, Palecki &
Barry (1986) suggested that freeze-up and breakup dates derived from satellite
observations could be used as a proxy for air temperature in mid-to-high latitudes that
lacked data coverage. This conclusion was drawn from the fact that they could correlate
changes in dates of freeze-up/breakup to a certain change in mean monthly temperature
leading up to that date. However, the regression coefficients varied across the country,
and were only suitable for hindcasting temperature for an area a few hundred km in
diameter.
The dearth of studies aimed at using temperature as a proxy for sea/lake ice, or
vice-versa, may be indicative of the inadequacies of such an approach. Indeed, of the few
studies found that do show some predictive value in certain sea ice-temperature
correlation models for a specific area, the authors admit such predictions are improved
upon or made redundant by complementary or alternative approaches employing other
proxies. The limited spatial scale of the studies that demonstrate some predictive value
also points toward the limitations of this approach. As scale increases, the
21
temperature/ice signal may be increasingly overridden by the effects of synoptic scale
systems.
2.7 Other Proxies for Sea Ice
Reconstruction of sea ice records need not necessarily rely on meteorological
proxies, the disadvantages of which have been noted. There is an abundance of evidence
in the paleorecord for decadal to millennial-scale changes in sea ice using marine
sediments, coastal depositions, driftwood and skeletons of microscopic organisms
(Polyak et al., 2010). Of primary interest to this study however are those proxies that can
resolve sea ice conditions at a sub-annual time scale.
Recent advances in ice core analysis have led to reconstructions of sea ice records
in Antarctica using chemical tracers preserved in the ice. One such advance involves the
analysis of methane sulfonic acid (MSA), produced through oxidation of the biogenic
dimethylsufide (DMS) from the ocean and subsequently aerially transported and
deposited in the continental Antarctic ice sheet (Abram et al., 2013). Since productivity
of DMS (and oxidation of MSA) increases with the area of ocean exposed to sunlight, a
positive relationship between Antarctic ice core MSA records and sea ice variability
should exist (Welch et al. 1993; Curran & Jones, 2000). This seems to be the case,
although the results are mixed and site-specific as the MSA production signal is
complicated by variability in its concentration resulting from its transport. Nevertheless,
researchers have found statistically significant relationships between SIE and MSA
production for various regions in the Antarctic that may be applied to reconstruct sea ice
22
records as far back as 160 years (Foster et al, 2006; Curran et al, 2003; Abram et al.,
2010; Abram et al, 2013; Becagli et al, 2009).
Another method employing ice core chemistry as a proxy for sea ice involves sea
salt aerosols generated through atmospheric interaction with open water. As with MSA,
the sea salt particles are transported to the Antarctic continental ice sheet where they are
deposited and preserved in the ice strata. Measurements of sodium in the ice core are
most representative of sea salt aerosols, and should in theory be negatively correlated
with sea ice extent (Abram et al., 2013). This was shown to be the case in the Canadian
Arctic, where sea salt sodium from an ice core on the Penny Ice Cap was negatively
correlated with spring SIE in Baffin Bay over the 20th century (Grumet et al., 2001). This
correlation was weak however, such that only 7% of the variability in sea salt was
accounted for by changes in SIE. Attempts to find a similar correlation in the Antarctic
have been complicated by the fact that sea ice itself seems to be a major source of
fractionated sea salt aerosols in the winter at coastal regions (Rankin et al, 2002; Douglas
et al, 2012; Abram et al, 2013). These findings have led researchers to believe that this
approach is best suited to areas that are dominated by open water such as the Arctic
Ocean (Abram et al, 2013).
Although ice core records contain a wealth of information of past climate
conditions, their application to sea ice conditions is still in its infancy. Both the MSA and
sodium methods have their limitations in their respective locales, and their applicability
to the broader Arctic is even more uncertain. Furthermore, as both methods rely on
atmospheric transport of chemical compounds, their accuracy diminishes with increasing
distances from source to deposition. This makes them particularly unsuitable for
23
reconstructing sea ice conditions on Hudson Bay as the distance between the Bay and the
nearest viable ice cores is on the order of 1000s of km.
2.8 Literature Summary
There is a clear consensus on the decline in Arctic sea ice (Comiso et al., 2008:
Parkinson et al., 1999; Stroeve et al., 2007; Vinnikov et al., 1999). Despite having
comparatively fewer studies on the subject, consensus appears to be growing for a similar
trend in Hudson Bay (Gagnon & Gough, 2005; Gough et al., 2004b; Hochheim et al.,
2011; Hochheim & Barber, 2010). A longer sea ice record would undoubtedly aid in
further characterizing this trend, but a review of the literature revealed no proxies for sea
ice on Hudson Bay. A few select studies on lake ice have had some success with proxies
exploiting its relationship to local temperatures, though limitations of scale suggest the
same approach for Hudson Bay might not yield the same results (Livingstone, 1997;
Williams, 1971; Palecki & Barry, 1986).
One of the defining characteristics of sea ice on Hudson Bay is the tremendous
spatial and temporal variability it exhibits throughout the cryogenic cycle (Hochheim &
Barber, 2010; Hochheim et al., 2011; Gagnon & Gough. 2005; Markham et al., 1986).
Often this variability manifests itself into a relatively well-defined east-west coastal
asymmetry. The prevailing westerly winds have been shown to have a strong role in these
asymmetries, through dynamic advection of sea ice eastward (Hochheim et al., 2011;
Gagnon & Gough, 2006; Saucier et al., 2004).
The theoretical basis for thermal modification of advecting air on the Bay has
been established by illustrating the contrast between open water and sea ice in terms of
24
their energy fluxes with the boundary layer atmosphere, which can vary by orders of
magnitude (Andreas & Murphy, 1986; Maykut, 1982; Maykut, 1986). Since these fluxes
vary with ice thickness, melt-pond coverage, snow depth, and other factors;
heterogeneous sea ice cover will likely have a much less predictable effect on advecting
air (Dieckmann & Hellmer, 2009, Maykut, 1986; Maykut, 1982). In summary, the
literature strongly supports the theory of sea ice leading to a temperature asymmetry on
Hudson Bay, but it remains unclear how this asymmetry will respond to the various states
of coverage seen throughout the cryogenic cycle.
25
Chapter 3: Methodology
3.1 Site Selection and Description
3.1.1 Hudson Bay Region
Hudson Bay covers an area of 1,300,000 km2 and has a drainage basin
encompassing 3,861,400 km2 (Martini, 1986; NRCAN, 1985). While connected to both
the Atlantic Ocean via Hudson Strait, and the Arctic Ocean via Foxe Basin, its waters
flow predominantly into the Atlantic (Lewis et al., 2000). Due to the large extent of the
Bay, its shores occupy various terrestrial ecozones, each exhibiting slight variations in
landform characteristics and regional climate (EFC, 2013). The Hudson Plains ecozone
covers much of the southern and western coasts of the Bay, including James Bay.
Roughly coincident with this ecozone is the Hudson Bay Lowlands, the largest wetland in
North America, characterized by vast stretches of peat bog and marsh. This region marks
a transition between temperate and arctic in terms of climate and biogeography. North of
the plains, the Taiga Shield ecozone covers much of the east coast of the Bay, and some
of the west coast. Here the peatlands give way to drier, flat terrain with rolling hills. The
northern half of the Bay is dominated by the Southern Arctic ecozone on both coasts. The
landscape of rolling plains is barren of trees due to harsh winters. Permafrost, defined as
ground that remains at or below 0°C for a minimum period of two years, is a prevalent
feature for all coastal areas of the Bay (NRCAN, 2009). All western coastal regions of
HB, as well as the northeastern coast, contain continuous permafrost (90-100%). James
Bay and the southeastern coast of HB experience isolated patches (0-10%) to extensive
discontinuous permafrost (50-90%), increasing in prevalence with latitude (NRCAN,
2009).
26
It is clear that the size of the Bay and resulting variability in climate factors
should be acknowledged when attempting to isolate for the influence of sea ice. Hence,
this study requires at least two sites with sufficiently lengthy climate records that also
fulfill the following criteria: (1) located on western and eastern coasts of the Bay (one of
each), (2) at latitudes comparable enough as to eliminate that as a source of climatic
variability, and (3) sharing other geographical characteristics that may contribute to
climatic differences such as terrain and altitude. Given the relative scarcity of climate
stations in the HB area, there are only two sites with climate records that fulfill criteria 1
and 2: Churchill, Manitoba and Inukjuak, Quebec. The suitability of these sites based on
criterion 3 is discussed below.
3.1.2 Churchill and Inukjuak: Local Climatic Factors
The town of Churchill, MB is located in the Northern region of Manitoba, on the
west coast of the Bay, at 58°46’09” N, 094°10’09” W. Inukjuak is a village and Inuit
community located in the Nord-du-Québec region of northern Quebec, on the east coast
of the Bay, at 58°27’00” N, 78°06’00” W. The fact that both sites are within less than
half a degree of latitude from each other means it is within reason to assume negligible
climatic variability owing to latitudinal differences. As temperatures typically decrease
with height, differences in elevation above sea level (m.a.s.l.) should be considered.
Orographic features that might obstruct or funnel wind, induce precipitation, or otherwise
influence climate should also be identified. As it turns out, the topography of Churchill
and Inukjuak are similar enough to discount these potential sources of climate variability.
Churchill being located at the intersection of the aforementioned Hudson Plain, Southern
27
Arctic and Taiga Plains ecozones, and Inukjuak being in the Taiga Plains ecozone,
topographic features for both sites are limited to rolling hills and plains. The elevations
of the weather stations used in this study are 29 and 25 m.a.s.l. for Churchill and
Inukjuak, respectively. Since both sites are located in regions classified as continuous
permafrost, energy and moisture flux at the land-atmosphere interface would be similar in
both cases and hence not account for differences in climate.
Both Churchill and Inukjuak are coastal communities, and as such we would
expect temperature and winds at both locations to be moderated to a certain degree by the
open water during the ice-free season. These effects play out on seasonal timescales (the
basis of this study), as well as diurnal time scales. For example, diurnal changes in
land/water temperature differences leads to a land and sea breeze circulation that can in
turn influence local air temperatures (Oke, 1978). This same mechanism accounts for
diurnal fluctuations in wind direction (e.g. an afternoon onshore breeze may change wind
direction). However, the design of this study assumes that these localized effects are
overridden by larger scale atmospheric circulation. In other words, it is assumed that over
the long term temperatures on both coasts are largely being driven by the westerlies – the
winds blowing from west to east that dominate in the middle latitudes. Monthly climate
normals show the most frequent wind direction for Churchill to be either W or NW in
every month except June (when it is NE). In Inukjuak, the westerlies appear to dominate
most months; however there are some months when the most frequent wind directions are
NE (March, April May) and N (June and November). Despite mostly prevailing
westerlies at both sites, wind frequency distributions show some variability month-to-
28
month and between coasts. Such differences will be taken into account as necessary (see
3.5 Wind Direction Analysis).
With the exception of wind direction, major climatological factors are very
similar between the proposed study sites. Therefore, most of the asymmetrical
temperature signal can confidently be attributed to the thermal influence of the Bay
combined with the prevailing westerlies.
3.1.3 Weather Stations/Climate Data
The weather stations used to represent climate in Churchill, MB and Inukjuak, QC
are listed below.
Table 1: Climate station summary.
Name Latitude Longitude Climate ID WMO ID Elevation Churchill (A) 58°44'21.0” N
94°03'59.0” W
5060600 N/A 29.30 m
Inukjuak (A) 58°28'00.0” N
78°05'00.0” W
7103283
N/A 25.30 m
Inukjuak (UA) 58°28'00.0” N
78°05'00.0” W
7103282
71907
24.40 m
While data for Churchill was sourced from a single climate station, it was
necessary to combine data from two Inukjuak stations to produce a record of comparable
length. Despite the change in station ID, the coordinates and elevation are nearly identical
so it is assumed there are no implications for data quality and continuity (See 3.9 Notes
on Data Quality).
29
3.2 Defining Temperature Asymmetry: ∆T
Since it is not the values of coastal temperatures themselves that are of primary
interest to this study, but rather the difference between those values, a new variable was
defined. The variable ΔT, with units of °C, is defined as the temperature at Inukjuak
subtracted from the temperature at Churchill for the same time interval (ΔT = TCHURCH –
TINUK). By this definition, a positive ΔT indicates that Churchill was warmer than
Inukjuak for that time interval, while a negative ΔT indicates that Inukjuak was warmer
than Churchill. Since the main period of interest for this study is the time between the
start of ice melt and when it is completely frozen, one would expect the thermal effect of
open water would result in warmer temperatures in Inukjuak most of the time (assuming
prevailing westerlies). Thus, it is expected that ΔT during this period of interest will most
often be negative. Ultimately the sign of ∆T is arbitrary, as long as it is clear which of the
two coasts is warmer, so it is the magnitude of this value that is of greatest importance.
The resulting database of ∆T values was used to construct a high-resolution
climate normal for this new variable. A single value was obtained for each Julian day (1-
366 including leap year days) by averaging ∆T values for that day from all years on
record. The resulting plot showed the average progression of ∆T throughout the year and
helped define another index of coastal temperature difference (See Figure 2).
3.3 Assessing Weekly SIC-ΔTW Correlation
The first approach taken to characterize the relationship between sea ice
concentration (SIC) and ΔT was to examine the correlation at a weekly time scale. The
assumption is that in the 1-week period between SIC observations, the SIC at the start of
30
that period is driving ΔT such that each SIC value might have a unique ΔT signal
associated with it. To assess that relationship, each SIC observation was paired with a 7-
day average ΔT (ΔTW) that spanned the day the SIC observation was made to the day
prior to that when the next SIC observation was made. In cases when more than 7 days
elapsed between observations, or when observations ceased at the end of the freeze-up
season, the same 7-day average was calculated to maintain consistency. Having
calculated a ΔTW for each unique SIC observation, the two variables were tested for
correlation using simple linear regression.
In addition to the analysis of all SIC observations, two further analyses were
conducted that separated the observations into those that occurred during breakup and
those that occurred during freeze-up. As shown in the Literature Review, the warming
effect of the Bay, and hence ΔT, is largely dependent on the temperature of the water
itself. Since water temperature will be increasing throughout the summer, it is likely that
the amount of temperature modulation for any given SIC will be different depending on
whether that observation is made during breakup or during freeze-up. Hence, another
simple linear regression analysis was performed only for those observations prior to the
first observation of SIC=0 in a year. Likewise, another analysis was performed only for
those observations following the last observation of SIC=0 in a given year. This provided
two sets of data, the former representing the breakup period and latter representing the
freeze-up period, in an attempt to eliminate the variability imparted by the seasonal
difference in water temperature.
31
3.4 Assessing IFS -∆T Correlation
In the event that the sea ice-∆T relationship could not be resolved at finer
spatial/temporal scales, it was hypothesized that the cumulative effects of open water
might produce a signal in ∆T towards the end of the season. In other words, the relative
length of time when the Bay is predominantly open water might be knowable based on
the maximum ∆T (averaged over a certain period to eliminate variability), which is
presumably reached towards the end of the season when the water itself is at its warmest.
If so, one would expect an anomalously lengthy ice-free season to correspond with an
anomalously high |∆T| (more negative by our definition of ∆T).
3.4.1 Capturing Maximum ∆T
Having created a high-resolution ∆T climate normal (Figure 2), it was possible to
identify the period(s) of greatest temperature asymmetry. From this visualization, the
time of year when the maximum |ΔT|s are most likely to occur seems to lie in the range
of Julian days 320-350 (November 16th to December 16th for normal years, November
15th to December 15th for leap years). Hence, a 31-day average of ∆T covering this period
was identified as ∆TMAX and calculated for all available years. The averaging of ∆T over
this specific period was done in hopes of i) capturing the time of year when |∆T| is at its
highest, and ii) eliminating some of the noise in the data.
32
3.4.2 Determining Ice-Free Season Length
As discussed in the Literature Review, breakup and freeze-up dates are defined as
the date when SIC passes the 5/10 threshold. Using these dates, a new variable was
identified as “ice-free season length” (IFS). This variable was defined as the number of
days between the breakup date and the freeze-up date. Note that, while by definition it is
the number of days when SIC<5, here it is serving as a general measure of the relative
lengths of the season where the Bay is predominantly open water. Gagnon & Gough
(2005) determined breakup and freeze-up dates from 1971-2003 for 36 point coordinates
evenly distributed throughout the Bay (See Figure 1). This database has since been
updated by S. Kowal (pers. comm., 2012) to include the years 2004-2011. Although
breakup and freeze-up dates vary significantly throughout the Bay according to sea ice
advance and retreat patterns, these data had to be homogenized into a single annual value
in order to capture the influence of season length on the Bay as a whole. To that end, a
single breakup date and a single freeze-up date were produced for each year in the record
by simply averaging the dates of the 36 points. The difference between the breakup and
freeze-up date was then calculated to provide a single value indicative of ice-free season
length for each year.
33
Figure 1: Site map of Hudson Bay indicating the location of the 36 points for which breakup and freeze-up dates were derived (Gagnon & Gough, 2005; reprinted with permission from the Arctic Institute of North America).
3.4.3 Classification of ∆TMAX by IFS
In the interest of ultimately developing a proxy tool that could approximate IFS
based on ∆TMAX alone, a simple classification scheme was devised consisting of three
categories:
Table 2: Definition of classes of ice-free season length.
Class Ice-Free Season Length (days) Short < 129
Medium 130-149 Long >150
This content downloaded on Wed, 16 Jan 2013 20:53:52 PMAll use subject to JSTOR Terms and Conditions
34
The range of these categories reflects the IFSs for the available 40-year sea ice
record, which ranges from 111-180. With exception to the outlier year when IFS=180,
values range from 111-170, meaning three equidistant categories with a range of roughly
20 days can be defined. Using this scheme, ∆TMAX values for each available year were
classified based on the IFS for that same year. This allows for a comparison of the ∆TMAX
values that arise in three generalized scenarios of IFS, as well as a measure of how likely
it is that a given year might be misclassified based on its ∆TMAX. A comparison of the
means of each category was conducted using the one-tailed homoscedastic Student’s t-
test. The resulting p-values were then adjusted using the Bonferroni correction. This
correction is a simple method by which we can counter the greater familywise error rate
associated with performing a multiple-hypothesis statistical test (Dunn, 1961). In this
case, the null hypothesis that all classes are not different in terms of their populations’
∆TMAX values is actually three null hypotheses that there are no differences between i)
short and long classes, ii) short and medium classes, and iii) medium and long classes.
Increasing the number of hypotheses applied to a dataset also increases the likelihood of
encountering anomalous events, and hence the likelihood of making a Type I error. To
mitigate this effect, p-values are multiplied by the number of hypotheses (three in this
case), and hence held to a higher standard of statistical significance.
Based on the results of this classification and comparison of means, thresholds of
∆TMAX were defined on the basis of minimizing overlap between categories. For
example, the threshold between the short and medium categories was selected by its
ability to maximize the actual short years captured while minimizing long or medium
35
years captured that simply had a ∆TMAX more indicative of short years. It is these ∆TMAX
thresholds that would eventually serve as the basis for classifying years as having a short,
medium or long IFS. To determine how well ∆TMAX predicts IFS, years with ∆TMAX s
outside of the defined threshold for their category were tallied. The count of these years
expressed as a percentage of n=33 provides the fraction of misclassified years using this
particular method. The closer this percentage value is to zero, the more successful the
method predicts the record, and hence the better it is expected to perform as a hindcasting
tool.
3.5 Wind Direction Analysis
3.5.1 Wind Direction Counts/Wind Rose Construction for ∆TMAX Period
As noted in 3.1.2, there are discrepancies in the climate normal between Churchill
and Inukjuak that prevent us from simply assuming prevailing westerlies during the
∆TMAX period. Inukjuak in particular seems to deviate from this pattern more frequently,
including during November when the most frequent direction is from the north. An
analysis of the wind directions in Inukjuak during the period of maximum ∆T might help
clarify why certain years do not exhibit the ∆TMAX signal expected given the length of the
ice-free season.
Wind direction data for the area was available in the form of hourly observations
in units of 10s of degrees on a 36-point wind rose. To simplify the data into more
meaningful directions, observations were reclassified on an eight-point rose in
accordance with Environment Canada’s guidelines (EC, 2013a). The frequency count for
each of these eight classes was then summed over the same 31-day period used for
36
calculating ∆TMAX (Julian Days 320-350). From these values, a single wind frequency
distribution chart (wind rose) was constructed for each year on record that is specific to
the period during which the Bay is exerting its greatest influence on advecting air. The
wind rose analysis focused on those years when ∆TMAX did not conform to the
established thresholds based on IFS (i.e. all misclassified years) in search of some pattern
explaining these anomalies.
Having qualified the relationship of anomalous ∆TMAX values to the distribution
of wind directions, the correlation between ∆TMAX and specific combinations of
directions was quantified by linear regression. The W and NW components of the
constructed wind roses were summed into a single value, NW+W, meant to be an
indicator of the relative frequency of winds arriving in Inukjuak that have been thermally
modified by the Bay. As a complementary approach, the summed components of NE+E
were calculated to serve as an indicator of the relative frequency of winds arriving in
Inukjuak over land and hence not subject to the same thermal modification. The northerly
component of the wind roses was omitted from this analysis as these winds have travelled
over both land and water and hence are not likely to contain as clear a signal of sea ice
conditions. Both NW+W and NE+E were correlated with IFS by linear regression and
tested for statistical significance.
3.5.2 Re-classification of ∆TMAX for Low NE+E Years
Having shown the correlation between IFS and NE+E to be the most statistically
significant, the classification of ∆TMAX values by IFS was done again. This time, only
years when NE+E counts were below average were included. The resulting percentage of
37
misclassifications was then compared to the original analysis to determine if this
approach eliminates weak ∆T signals on account of predominant easterly and
northeasterly winds.
3.6 Evaluating Proxy Performance: Temperature as a Benchmark
In order to evaluate ∆TMAX as a proxy for IFS, a benchmark using another proxy
method was established against which the rate of misclassification could be compared.
As discussed in 2.7, there has been some success in using temperature as a stand-in for
sea/lake ice conditions (Livingstone, 1997; Palecki & Barry, 1986; Williams, 1971).
These studies stress the limitations of such an approach, making temperature a very
coarse approximator of sea ice. This provides a suitable benchmark, as any method
outperforming it can be identified as a superior alternative to the worst-case scenario
proxy method.
There are a number of different indices of temperature one can use to correlate to
sea ice by focusing on different areas of the Bay and periods of the cryogenic cycle. For
simplicity and consistency, the same temperature records for Churchill and Inukjuak used
to calculate ∆T were used to calculate a new index of temperature that is representative of
the whole Bay. The two temperature records were combined into a single average
temperature record ([TCHURCH + TINUK]/2). The period over which this spatially averaged
temperature was temporally averaged was optimized to capture a period when
temperature is likely to be exerting an influence on IFS. This period was chosen to be the
61 days spanning Julian days 260-320 (Sept. 17th to Nov. 16th for regular years; Sept. 16th
to Nov. 15th for leap years). This period was chosen because it encompasses the vast
38
majority of the freeze-up process, during which air temperatures play a role in either
promoting or delaying ice formation, thereby lengthening of shortening IFS. Having
defined this index of temperature as TF, another classification scheme was developed in
the same fashion as that of ∆TMAX, using new thresholds of TF. All three classification
methods were then compared in terms of their performance in classifying the existing
record.
3.7 Combined Approach: ∆TMAX and TF in a Multi-Proxy Results from the evaluative process described above led to the consideration of TF
as either an alternative or a complementary proxy. The relationships that both ∆TMAX and
TF exhibit with IFS suggest that both variables each contain some unique information
regarding ice-free season length. Despite both variables being indices of mean air
temperature, they are different in terms of: i) the temporal period over which they are
calculated and, ii) the underlying mechanisms that relate them to IFS. In the case of
∆TMAX, it is the sea ice (or lack thereof) that is acting upon advecting air that leads to the
temperature difference signal. In the case of TF however, it is TF that is acting upon sea
ice (or open water), hence playing a role in determining IFS. Furthermore, despite being
the most highly correlated to IFS, TF by definition contains only information regarding
freeze-up conditions. By contrast, ∆TMAX is theoretically determined by the cumulative
effects of open water, and hence should inherently contain some information regarding
break-up conditions. Therefore, the information contained in TF and ∆TMAX with respect
to IFS should not be redundant, and it should be expected that a multiple regression
between both temperature variables and IFS would yield a more significant relationship
39
than either temperature variable alone. If so, the use of the regression equation to hindcast
IFS in lieu of the classification scheme might produce higher resolution results within an
acceptable range of error. To test this hypothesis, a multiple linear regression was
conducted on the 33-year record with IFS as the dependent variable and both ∆TMAX and
TF as independent variables. The resulting equation was assessed as a proxy by its ability
to recreate the historical IFS record. The difference between actual IFS values and those
produced from the equation was calculated as absolute error. As with the classification
approach, TF was used as a benchmark of comparison, to assess if the ∆TMAX + TF multi-
proxy results offer a significant improvement. Thus another comparison of actual IFS vs.
IFS derived from a linear equation was conducted, this time using a simple linear
regression equation derived from just TF and IFS. A comparison of the errors produced
from either approach informed the final decision of what proxy method is best suited to
hindcast IFS.
3.8 Hindcasting and Trend Analysis of Extended Record
Given the success the multiple regression equation had with recreating the
historical record, it was determined that this method could confidently hindcast IFS prior
to 1972 (See Tables 14 & 15). Hence, IFS values were calculated for all years prior to
1972 with available temperature data for both Churchill and Inukjuak. The resulting
hindcast time series was appended to the actual IFS time series for comparison. To
highlight the long-term trend in IFS, a five-year moving average time series was also
produced by producing new values for each year that are an average of the two preceding
values, the value itself, and the two following values. For example, the new IFS value for
1990 would be the average of values from 1988, 1989, 1990, 1991, and 1992. The
40
application of this method eliminates four years from the data set, as the first and last two
years of the data set are lacking the two preceding/following years respectively.
To determine if there are any trends in the data set, the Mann-Kendall statistical
test was employed to produce Kendall’s tau coefficients (τ) for various portions of the
original time series (not the data smoothed by moving average). This non-parametric test
provides a measure of rank correlation, or probability that two variables are ranked in the
same order (Kendall, 1938). The test yields a τ value between -1 and 1, with the sign and
magnitude of τ indicating the direction and probability of a correlation between two
variables, and a value of 0 indicating no correlation. In the case where the independent
variable is time, that correlation corresponds to a temporal trend in the dependent
variable. The test was run using the XLSTAT add-on for Microsoft Excel 2011. The
hypotheses for these tests were as follows:
H0= There is no trend in the time series. HA=There is a trend in the time series.
In order to contextualize any trends in IFS, τ values were obtained for various
periods of the extended time series. Firstly, the hindcast time series was considered on its
own as a baseline period for IFS and compared to the actual time series in terms of τ. In
order to identify the period where it is most probably that a trend is occurring, additional
analyses were done using different division points in the dataset at five-year intervals
from 1980 to 1990.
41
3.9 Notes on Data Quality
All climate data obtained from Environment Canada has been reviewed and
undergone the appropriate procedures to ensure it conforms to their own data quality
standards (EC, 2013b). Some issues may arise in this study as new variables are
constructed as a combination of other variables (e.g. 31-day temperature averages). To
ensure the validity of the conclusions drawn from this data, certain guidelines were
followed to omit variables for certain years if their constituent values were sufficiently
lacking.
3.8.1 Temperature Data
The mean daily temperature record for Churchill, which extends back to 1943, is
continuous and uninterrupted with the exception of three missing months in the period of
1944-1946. There are no missing values for the period of 1972-2011. Inukjuak’s
temperature record is more fractured, as it is split between two climate stations and
contains periods with intermittent gaps in the daily records. The records for both Inukjuak
stations were combined into a single record on the assumption that their nearly identical
geographic coordinates and elevation obviated any need for data homogenization. The
transition between stations occurs in 1994, and as a result that year is severely lacking in
data and thus omitted from the analysis.
Environment Canada’s “3 and 5” rule allows for the calculation of an average
monthly temperature if the month has no more than 3 consecutive missing daily values
and no more than 5 total missing daily values (S. Allen, pers. comm., 2013). This quality
standard serves as a useful benchmark in the calculation of ∆TMAX, as it is a 31-day
average. In this case, a slightly less stringent “4 and 7” rule was followed in calculating
42
31-day averages. This is to allow for the inclusion of the year 2001 in the analysis, when
the 320-350 period contains 4 consecutive missing days and a total of 7 out of 31 missing
days. Note that all other years adhere to the “3 and 5” rule.
The distribution of data for all temperature indices was tested for normality using
the Anderson-Darling test, with the null hypothesis that the input data come from a
normal population (Stephens, 1986). The test on ∆TMAX produced p-value of 0.1465,
meaning the null hypothesis cannot be rejected. The test on TF produced a p-value of
0.5456, meaning the null hypothesis cannot be rejected. The test was not run on the raw
∆T database as the population was extremely large and these values were not used for
any trend analysis, eliminating the need to demonstrate normality.
3.8.2 Wind Direction Data
The availability of wind data for Inukjuak is limited to the period of 1981 to 2007.
This record contains 24 hourly observations available for most days in the 320-350
period, with the exception of certain years when hourly observations may be as low as
12. In order to eliminate the influence of diurnal fluctuations in wind (e.g.
onshore/offshore breeze), it is important to use only those days whose hourly
observations number at or near 24. To that end, wind direction analysis was only
conducted for years when the 320-350 period met the following criteria: i) no more than
10 days when # of observations < 22, ii) no more than 2 days when # of observations <
20, and iii) 0 days when # of observations < 14. The application of these quality
standards resulted in the omission of years 1992 and 1993. The test for normality was
done only on the wind direction components used in the linear regression with IFS
43
(NE+E). The resulting p-value of 0.0016 indicates that the null hypothesis may be
rejected at the 99% confidence interval. This lack of normality means that any trend
analysis of IFS values obtained by a proxy that includes wind data would require the use
of non-parametric tests.
3.8.3 Ice-free Season Data
There are 36 geographical points used to derive the spatially averaged breakup
and freeze-up dates, and most years all of them are accounted for. However, there are a
few years when dates are unavailable for certain points, usually because freeze-up/break-
up had already occurred before observations were made (Gagnon & Gough, 2005). In
these cases, years were included only if n≥20. If either a breakup date or a freeze-up date
was deemed unusable, then the ice-free season length for that year was not calculated.
This resulted in the omission of years 1973, 1997, 1998, 1999, and 2002. The test for
normality on the IFS dataset yielded a p-value of 0.9489. Hence, there is insufficient
evidence to warrant the rejection of the null hypothesis that the data comes from a normal
population.
44
Chapter 4: Results
4.1 ΔT Climate Normal
The calculation of ΔT using Churchill and Inukjuak temperature data produced a
dataset 68 years in length spanning from 1944 to 2011. The only years missing enough
data to be omitted were 1994, when the moving of the Inukjuak station left a gap in its
record, and 2008 when the latter half of the year’s data is missing for Churchill. The
following graph depicts the daily fluctuations in ΔT for a year as an average of the entire
record.
Figure 2: Climate normal for ∆T (Churchill Daily Mean T - Inukjuak Daily Mean T) calculated over the period 1944-2011.
-‐10
-‐8
-‐6
-‐4
-‐2
0
2
4
6
40 80 120 160 200 240 280 320 360
∆T (°C )
Julian Date
45
4.2 Weekly SIC-ΔTW Correlation
The correlation of weekly SIC observations to average weekly ΔT was conducted
in three parts: one containing all observations, one covering the breakup period and one
covering the freeze-up period (Figs. 3, 4 & 5 respectively).
Figure 3: Correlation of ∆TW with spatially averaged SIC for all weekly observations on record 1971-2011.
Figure 4: Correlation of ∆TW with spatially averaged SIC for all weekly observations during the breakup period, 1971-2011.
-‐20
-‐15
-‐10
-‐5
0
5
10
15
20
0 2 4 6 8 10 ∆TW (° C)
Sea Ice Concentration (tenths)
-‐15
-‐10
-‐5
0
5
10
15
20
0 1 2 3 4 5 6 7 8 9 10 ∆TW (° C)
Sea Ice Concentration (tenths)
46
Figure 5: Correlation of ∆TW with spatially averaged SIC for all weekly observations during the freeze-up period, 1971-2011.
The above plots effectively demonstrate the lack of any correlation between SIC
and ΔT at a weekly temporal resolution. There is clearly no correlation when considering
all observations on record (R2= 0.0053, p= 0.287). Dividing the observations by season
fared no better, as a linear regression for the break-up period yielded an imperceptible
slope and an extremely low R2 of 0.003 (p = 0.42356). Likewise, linear regression on the
freeze-up period yielded no significant trends and an equally low R2 value (R2= 0.00227,
p= 0.7477).
4.3 IFS-ΔTMAX Correlation
The values of IFS and ΔTMAX for the period of 1972-2011 are presented in Table
3. Linear regression between these two variables yields a statistically significant negative
correlation (R2=0.25353, p=0.00331). Note that, by our definition of ∆T, a negative
correlation means that longer IFS are more likely to be associated with higher |∆TMAX|
-‐20
-‐15
-‐10
-‐5
0
5
10
15
0 2 4 6 8 10
∆TW (° C )
Sea Ice Concentration (tenths)
47
Table 3: Ice-free season length and ∆TMAX for 1972-2011.
*(Note that years when either variable was missing were omitted entirely)
Year IFS ΔTMAX
1972 111 -4.1 1974 124 -1.7 1975 143 -13.4 1976 137 -5.5 1977 149 -6.9 1978 122 -1.9 1979 143 -2.3 1980 146 -7.3 1981 153 -2.4 1982 133 -10.5 1983 137 -0.2 1984 132 -5.1 1985 131 -8.6 1986 130 0.0 1987 128 -2.8 1988 147 -9.7 1989 141 -7.6 1990 144 -10.3 1991 141 -12.7 1992 120 -1.9 1993 135 -6.6 1995 147 -5.3 1996 151 -9.0 2000 144 -8.4 2001 164 -9.2 2003 158 -9.6 2004 134 -8.4 2005 160 -7.6 2006 170 -9.7 2007 162 -8.0 2009 159 -6.2 2010 181 -10.9 2011 165 -8.4
48
4.3.1 Classification of ∆TMAX by IFS
The results of the classification of ΔTMAXs by IFS are presented in Table 4.
Table 4: Classification of ∆TMAX by IFS for all years on record.
Short Medium Long -1.7 0.0 -2.4 -1.9 -0.2 -6.2 -1.9 -2.3 -7.6 -2.8 -5.1 -8.0 -4.1 -5.3 -8.4 -5.5 -9.0 -6.6 -9.2 -6.9 -9.6 -7.3 -9.7 -7.6 -10.9 -8.4 -8.4 -8.6 -9.7 -10.3 -10.5 -12.7 -13.4 Mean -2.5 -7.2 -8.1 Std. Dev. 1.0 3.5 2.4
Since the data is normal, the medium category contains the largest sample size
(n=17), with the short and long categories being less populated (n=5 and 10 respectively).
The summary statistics for each category show their associated means appear to be
distinct, so a t-test was conducted to test for statistical significance (Table 5).
49
Table 5: P-values obtained from interclass comparison of ∆TMAX means by one-tailed t-test, adjusted using the Bonferroni correction.
Short Medium Short - 0.01833 Long 0.00036 0.70734
The t-test results show that the means for the short and long categories are very
distinct, with statistical significance at the 99% confidence interval. Of greater interest is
the level of differentiation of the medium category. The high p-value in the case of
medium vs. long means there is no statistically significant difference in their means.
However, in the case of medium vs. short, means are significantly different at the 99%
confidence interval.
Based on the distributions of ∆TMAX for each category, thresholds were defined
such that the chance of misclassification is minimized. When these thresholds are applied
to the same 33 years from which they were derived, the proportion of misclassified years
to correctly classified years serves as an indicator of the success of ∆TMAX as a proxy.
50
Table 6: Identification of misclassified years based on ∆TMAX thresholds.
Short Medium Long -1.7 0.0 -2.4 -1.9 -0.2 -6.2 -1.9 -2.3 -7.6 -2.8 -5.1 -8.0 -4.1 -5.3 -8.4 -5.5 -9.0 -6.6 -9.2 -6.9 -9.6 -7.3 -9.7 -7.6 -10.9 -8.4 -8.4 -8.6 -9.7 -10.3 -10.5 -12.7 -13.4 Threshold > -4.5 -4.5>∆TMAX> -8.0 < -8.0 Misclassified 0 11 3 Total % Mis 42 *Note: values in red indicate a misclassification by one category, values in red and italics misclassified by two categories.
51
4.4 Wind Direction Analysis
4.4.1 Wind Direction Frequency Distributions
Wind roses showing the distribution of direction frequencies over the period of
Julian days 320-350 were produced for every year from 1981-2007. Presented below are
the wind roses for all years that were misclassified based on ∆TMAX (those in red in Table
6). Anomalous distribution of wind direction frequencies are made clear by comparing a
year’s wind rose with the climate normal wind rose (Figure 7).
Figure 6: Climate normal wind rose for Inukjuak over Julian days 320-350, calculated over the period of 1981-2007.
The climate normal for wind direction frequencies in Inukjuak over the period of
interest show that the NE and W components dominate most often with average counts of
127 and 124 respectively.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
52
Figure 7: 1981 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -2.4°C, IFS = 153 (Long).
The 1981 wind rose shows the second highest count for frequency of NE, and the
absolute lowest for W.
Figure 8: 1982 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -10.5°C, IFS = 133 (Medium).
The 1982 wind rose had the second highest frequency of W winds.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
53
Figure 9: 1983 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -0.2°C, IFS = 137 (Medium).
The 1983 wind rose shows the 3rd highest on record count of NE winds.
Figure 10: 1985 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.6°C
While NE winds were above average in 1985, so were both NW and W, hence
NW+W>NE+E.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
54
Figure 11: 1986 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = 0.0°C, IFS = 130 (Medium).
1986 had the 4th highest NE count on record, but also had an above average
westerly component.
Figure 12: 1988 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.7C, IFS = 147 (Medium).
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
55
The largest component in the 1988 wind rose is the N wind, with below average
W, NW, NE, and E components.
Figure 13: 1990 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -10.3°C, IFS = 144 (Medium).
As with the previous example, the distribution of wind frequencies for 1990 is
roughly equal among all 8 components, with a strong northerly component.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
56
Figure 14: 1991 wind rose for Inukjuak over Julian days 320-250: ∆TMAX = -12.7°C, IFS = 141 (Medium).
1991 saw above average W and SW winds, and below average NE and E winds.
Figure 15: 2000 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.4°C, IFS = 144 (Medium).
2000 saw above average W and NW components, as well as below average NE
components. E winds were above average but to a lesser degree than W and NW.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
57
Figure 16: 2002 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -4.0°C, IFS = 146 (Medium).
2002 had average NE and above average E frequencies.
Figure 17: 2004 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.4°C, IFS = 134 (Medium).
2004 year saw no major anomalies in wind direction frequency.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
58
Figure 18: 2005 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -7.6°C, IFS = 160 (Long).
2005 saw the second highest on record SW count, but also NE and E counts well
above average.
4.4.2 Correlation of Wind Direction Components to IFS
Since the assumption that westerly winds have a strong influence on ∆T has been
shown to have some merit, ∆TMAX was tested for correlation with both NW+W and
NE+E. While NW+W showed a slight positive relationship (R2=0.28972, p=0.08761),
the negative relationship with NE+E proved stronger and statistically significant at the
99% confidence interval (R2=0.37594, p=0.00241).
4.4.3 Classification of ∆TMAX by IFS for Low NE+E Years
The classification of ∆TMAX by IFS was conducted again, this time only including
those years when the NE+E wind component was below average.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
59
Table 7: Classification of ∆TMAX by IFS for years when NE+E wind count is below average.
Short Medium Long -5.1 -8.0 -7.6 -9.2 -8.4 -9.6 -8.4 -9.7 -8.6 -9.7 -10.3 -10.5 -12.7 Mean N/A -9.0 -9.1 Std. Dev. N/A 2.1 2.4 Since the years when NE+E are above average are eliminated from this data set, it
is expected that the overall averages for each category be higher than in the previous
analysis. This is indeed the case for the medium and long categories, but the exclusion of
all short years prevents the determination of a new mean for this category. Furthermore, a
comparison of means by t-test between long and medium categories reveals a p-value of
0.3784, suggesting that the elimination of high NE+E years has not helped in
significantly distinguishing ∆TMAX values between these categories. Due to this shift in
means, new thresholds of ∆TMAX can be identified that minimize misclassification for this
new data set.
60
Table 8: Identification of misclassified years when NE+E winds count is below average.
Short Medium Long -5.1 -8.0 -7.6 -9.2 -8.4 -9.6 -8.4 -9.7 -8.6 -9.7 -10.3 -10.5 -12.7 Threshold N/A -4.5>∆TMAX> -9.0 < -9.0 Misclassified N/A 4 1 Total % Mis 39 The relative proportion of misclassifications has been reduced from 42% to 39%
by eliminating above average NE+E years. However, this slight improvement comes at
the expense of a loss of confidence in the results due to the drastic reduction in the
population of the classification table.
61
4.5 IFS-TF Correlation
Table 9 shows the values calculated for TF, the freeze-up temperatures calculated
over Julian days 260-320 and spatially averaged over Inukjuak and Churchill.
Table 9: Ice-free season lengths and TF for 1972-2011.
Year IFS TF
1972 111 -5.0 1974 124 -3.0 1975 143 -0.2 1976 137 -1.9 1977 149 1.5 1978 122 -3.1 1979 143 -3.1 1980 146 -2.6 1981 153 -0.1 1982 133 -1.6 1983 137 0.1 1984 132 -1.8 1985 131 -1.0 1986 130 -4.2 1987 128 -1.3 1988 147 -0.2 1989 141 -2.3 1990 144 -2.6 1991 141 -2.6 1992 120 -3.2 1993 135 -2.9 1995 147 -2.1 1996 151 -0.6 2000 144 -0.2 2001 164 0.9 2003 158 -1.0 2004 134 -0.4 2005 160 0.9 2006 170 0.1 2007 162 -0.4 2009 159 -0.5 2010 181 2.0 2011 165 1.9
*Note: years when either variable was missing were omitted entirely
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Linear regression between IFS and TF reveals a statistically significant negative
relationship (R2 = 0.59051, p = <0.0001)
4.5.1 Classification of TF by IFS
The classification of TF values by IFS can be found in Table 10. Populations for
each category are the same as those in the ∆TMAX – IFS classification, since both are
based on IFS and derived from the same temperature records.
Table 10: Classification of TF by IFS for all years on record.
Short Medium Long -5.0 -4.2 -1.0 -3.2 -3.1 -0.6 -3.1 -2.9 -0.5 -3.0 -2.6 -0.4 -1.3 -2.6 -0.1 -2.6 0.1 -2.3 0.9 -2.1 0.9 -1.9 1.9 -1.8 2.0 -1.6 -1.0 -0.4 -0.2 -0.2 -0.2 0.1 1.5 Mean -3.1 -1.6 0.3 Std. Dev. 1.3 1.4 1.1
The summary statistics show that the means for each category appear to be
distinct and increasing in magnitude with increasing ice-free season length, as should be
63
expected. A comparison of means by t-test revealed significant differences between all 3
categories (Table 11).
Table 11: P-values obtained from interclass comparison of TF means by one-tailed t-test, adjusted using the Bonferroni correction.
Short Medium Short - 0.05028 Long <0.0001 0.00168
Thresholds of TF were established in the same way as ∆TMAX thresholds by
minimizing overlap between categories.
Table 12: Identification of misclassified years based on TF thresholds (misclassifications in red).
Short Medium Long -5.0 -4.2 -1.0 -3.2 -3.1 -0.6 -3.1 -2.9 -0.5 -3.0 -2.6 -0.4 -1.3 -2.6 -0.1 -2.6 0.1 -2.3 0.9 -2.1 0.9 -1.9 1.9 -1.8 2.0 -1.6 -1.0 -0.4 -0.2 -0.2 -0.2 0.1 1.5 Threshold ≤ -3.0 -3.0<∆TMAX≤ -1.0 > -1.0 Misclassified 1 8 1 Total % Mis 30
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Table 13 puts the performance of the TF approach in the context of the two ∆TMAX
methods.
Table 13: Comparison of temperature variables in terms of coefficients of determination, statistical significance, and percent misclassifications.
R2 p-value % Misclassified ∆TMAX 0.25353 0.00331 42 ∆TMAX (NE+E)* 0.54356 0.00622 39 TF 0.59051 <0.0001 30 *Note: The R2 and p-value listed here are for the linear regression of ∆TMAX and IFS only for those years when NE+E wind count was below average.
4.6 IFS-∆TMAX-TF Multiple Linear Regression
The equation obtained by running a multiple linear regression with IFS as a
dependent variable and both ∆TMAX and TF as independent variables is:
[Eqn. 1] IFS = 144.6224 - 0.9602�∆TMAX + 6.0560�TF
When all ∆TMAX and TF values on record from the period of 1972-2011 are used
as inputs into this equation, predicted values of IFS are produced (Table 14). The
absolute difference between predicted IFS and actual IFS is shown in the |Error| column.
The same process was conducted using the following equation acquired by simple
linear regression with IFS as dependent variable and TF as independent variable:
[Eqn. 2] IFS =152.1479 + 6.9146 � TF
The resulting IFS values and |Error| values are found in Table 15.
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Table 14: IFS results from Eqn. 1 (TF+∆TMAX) compared with actual IFS in terms of absolute error for the period 1972-2011.
Year IFS (Actual) IFS (Eqn.) |Error| 1972 111 118 7 1974 124 128 4 1975 143 156 14 1976 137 138 1 1977 149 161 11 1978 122 128 6 1979 143 128 15 1980 146 136 10 1981 153 146 7 1982 133 145 12 1983 137 145 9 1984 132 138 6 1985 131 147 16 1986 130 119 11 1987 128 140 12 1988 147 152 6 1989 141 138 3 1990 144 139 5 1991 141 141 0 1992 120 127 7 1993 135 134 1 1995 147 137 10 1996 151 150 2 2000 144 152 7 2001 164 159 5 2003 158 148 10 2004 134 150 16 2005 160 157 3 2006 170 155 15 2007 162 150 12 2009 159 148 11 2010 181 167 13 2011 165 164 1
Average 8.1 Std. Dev. 4.7
66
Table 15: IFS results from Eqn. 2 (TF) compared with actual IFS in terms of absolute error for the period of 1972-2011.
Year IFS (Actual)
IFS (Eqn.) |Error|
1972 111 117 6 1974 124 131 7 1975 143 151 8 1976 137 139 2 1977 149 163 14 1978 122 131 9 1979 143 131 12 1980 146 134 12 1981 153 151 2 1982 133 141 8 1983 137 153 16 1984 132 139 7 1985 131 145 14 1986 130 123 7 1987 128 143 15 1988 147 150 4 1989 141 136 5 1990 144 134 10 1991 141 134 7 1992 120 130 10 1993 135 132 2 1995 147 137 10 1996 151 148 3 2000 144 151 7 2001 164 158 6 2003 158 145 13 2004 134 149 15 2005 160 158 2 2006 170 153 17 2007 162 150 13 2009 159 149 10 2010 181 166 14 2011 165 165 0
Average 8.7 Std. Dev 4.7
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Comparing Tables 14 and 15 shows that the multiple regression equation
improves error on average by 0.6 days (1 day when rounded). An updated comparison of
the various temperature indices and their correlation to IFS in terms of R2 and p-value can
be found in Table 16.
Table 16: Comparison of temperature variables in terms of the coefficients of determination and statistical significance of their linear relationships with IFS.
R2 p-value ∆TMAX 0.25353 0.00331 ∆TMAX (NE+E)* 0.54356 0.00622 TF 0.59051 <0.0001 TF + ∆TMAX 0.62863 <0.0001 *Note: The R2 and p-value listed here are for the linear regression of ∆TMAX and IFS only for those years when NE+E wind count was below average.
4.7 Hindcast IFS
By applying Eqn. 1 to the temperature record for all available years prior to 1972,
a hindcast record of IFS values 28 years in length was obtained. The time series for this
new dataset was appended to the time series for actual IFS values, producing a record 68
years in length with 5 missing values (all from the actual dataset).
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Figure 19: Time series of IFS from 1944-2011 constructed using actual observations and data derived by proxy from ∆TMAX and TF [Eqn. 2].
Application of a 5-year moving average resulted in the smoothed curve seen in
Fig. 20. Note that the smoothed data is shown here only for visual interpretation, and that
all trend analyses were done using the original data presented in Fig. 19.
Figure 20: Time series for actual and hindcast IFS smoothed by use of a 5-year moving average.
0
20
40
60
80
100
120
140
160
180
200 Ice-‐free Season Length (days)
Year
Hindcast
Actual
0
20
40
60
80
100
120
140
160
180
Ice-‐free Season Length (days)
Year
Actual
Hindcast
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The Mann-Kendall test conducted on the entire time series (1944-2011) from Fig.
19 showed a weak positive association between time and IFS that is statistically
significant at the 95% confidence interval (τ = 0.208, p = 0.017). Since it is assumed that
this positive trend is being driven by a recent increase in IFS, the test was run for four
different pairs of baseline/trend time series, defined by a division year (Table 17). The
first entry (1972) uses the entire hindcast record as a baseline and the entire actual record
as a trend. The other three entries were arbitrarily selected as intervals of 5 years starting
in 1980 in an effort to isolate the period where there is most likely a trend. As another
example, the second entry in Table 17 (1980) has a baseline τ and p-value that
correspond to the period 1944-1980. That same entry has a trend τ and p-value that
correspond to 1980-2011, and so on.
Of the four pairs of baseline and trend time series presented in Table 17, those
with the division year of 1985 have the greatest contrast. For the period of 1944-1985,
there is no statistically significant trend occurring, while the τ value of 0.607 for the
period of 1986-2011 strongly suggests a statistically significant positive trend in IFS with
time (p<0.0001).
Table 17: Comparison between baseline and trend in terms of τ and statistical significance for different time series divisions.
Division Baseline τ Trend τ Baseline p Trend p 1972 0.177 0.490 0.198 < 0.0001 1980 -0.024 0.484 0.848 0.0004 1985 -0.033 0.607 0.770 < 0.0001 1990 -0.088 0.578 0.399 0.001
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Chapter 5: Discussion
5.1 Interpreting ∆T Climate Normal
The climate normal constructed for ∆T (Figure 2) shows a clear annual cycle,
with daily values spanning from ~+5°C to -8°C. Beginning on day 1, ΔT is in the
negative phase of this cycle, indicating that TINUK>TCHURCH, and that despite being well
into the ice-covered season, there is perhaps some residual heat flux through the ice that
has not yet reached maximum thickness. However, ΔT continues to approach zero and
enters the positive phase between days 30 and 50. From 30-150, temperatures in
Churchill and Inukjuak are similar enough that ∆T is for the most part close to 0°C, as
would be expected under complete ice cover. Following this period, ∆T actually starts to
climb, becoming more positive and ultimately reaching its peak around day 200 at about
5°C. At this point the graph exhibits an interesting feature, whereby ΔT seems to drop
precipitously before climbing back to what appears to be a second peak of ~4°C around
day 230. It is interesting that ∆T appears to undergo this positive phase, reaching as high
as it does, when one might expect the near-0°C values of the previous period to persist
until reverting to the negative phase following breakup. One can speculate that this
represents a period when warmer spring winds arriving in Churchill are subsequently
cooled down upon advecting over the ice that persists on the Bay. Following the
secondary peak, ΔT undergoes a steady decline, surpassing 0°C around days 270 to 280
and re-entering the negative phase. This reversal in ∆T lags by roughly 80-100 days
behind both the average breakup date and average ice-free date for the Bay (~180 and
200 respectively). ∆T continues to trend downwards throughout the ice-free season and
well into the freeze-up season. Maximum |ΔT| is observed late in the year in the range of
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days 330-340 and reaches an average magnitude of approximately 7.5°C. Note that this
maximum temperature difference is occurring in the vicinity of, or shortly after, the
average freeze-up date for the Bay (~330). Again, this demonstrates the degree to which
upward heat flux persists despite growing ice cover. The apex of the ∆T curve marks
some point at which this heat flux is overtaken by the insulating power of the ice,
following some critical threshold in its cover and thickness. Following this point, another
sharp reversal and subsequent positive trend persists until the positive phase is reached
once again around day 40.
The most important conclusions derived from this graph come from placing the
fluctuations in ∆T in the context of seasonal changes in ice cover. As shown above, the
major changes in ∆T lag significantly behind every major milestone in ice cover. Peak
|∆T|, which is theoretically associated with open water conditions, lags so far that it is
actually most likely to occur when the bay is more than 50% ice-covered. Lag owing to
thermal inertia was expected, but the significant length of time between changes in sea
ice and a corresponding asymmetry signal imposes some severe limitations on the
temporal resolution of a proxy based on this relationship.
5.2 SIC-∆TW Relationship
No correlation could be found between the weekly SIC observations and
subsequent weekly ∆T averages. Comparing Figures 4 and 5, it is clear that on average
∆Tw values are lower for SIC observations during freeze-up than breakup, with the vast
majority being above 0°C for breakup and below 0°C for freeze-up. However, despite
accounting for this expected difference, the resulting correlations between ∆TW and SIC
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in both cases reveal no statistically significant trends. In light of the aforementioned lag
between a change in sea ice conditions and resulting ∆T signal, it is not surprising that a
weekly average of ∆T is not necessarily representative of recent SIC. It is clear from
these three graphs that the ∆T-SIC relationship is not strong enough to be of any
predictive value at this fine a resolution.
5.3 IFS-∆TMAX Relationship
The statistically significant negative correlation between IFS and ∆TMAX
(R2=0.25353, p=0.00331) suggests that the length of time the Bay is ice-free has some
effect on the temperature asymmetry following the end of the IFS. More specifically,
shorter IFSs tends to be associated with smaller |∆TMAX| (closer to 0), while the longer
IFSs tend to be associated with greater |∆TMAX| values (Note the use of || bars to avoid
confusion regarding signs – this way a ∆TMAX of -13 for example can be referred to as a
large temperature difference). However, this relationship exhibits a great degree of
variability, such that years with an average or below average IFS can also have a
significantly large |∆TMAX| signal. Indeed, the top 2 years in terms of magnitude of
∆TMAX (-13.4, -12.7) were not coincident with long IFS, but rather from rather average
years (IFS=143 and 141, respectively). The converse of this problem occurs as well, as
there are years with lengthy IFS but very little temperature asymmetry. For example, the
∆TMAX value of -2.4 occurs during a year with an IFS=153. Such examples are less
common however, and in general it seems as though ∆TMAX values closer to 0 are more
reliably associated with shorter IFS, while the larger |∆TMAX| values are not as
consistently associated with the longer IFS. Consider that of the top 10 years in terms of
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|∆TMAX|, only 5 are also top 10 years in terms of IFS. However, of the bottom 10 years in
terms of |∆TMAX| (i.e. closest to 0), 7 are also bottom 10 in terms of IFS. This suggests
that large temperature differences between coasts may arise under a slightly wider range
of IFS, whereas smaller temperature differences are more often constrained to years when
IFS was below average. The classification of ∆TMAX values by IFS aids to highlight how
the inconsistencies in this relationship would affect the results of the proposed proxy
methodology.
When ∆TMAX values are classified into three categories of IFS (Table 4), many of
the characteristics and anomalies of the relationship noted above become more evident.
The fact that ∆TMAX values for the medium class range from 0.0 to -13.4°C reinforces the
above observation that there is considerable variability in ∆TMAX independent of IFS,
particularly in years when the ice-free season is average. The observation of -2.4°C sticks
out among the predominantly higher values of the long class, demonstrating that despite
the tendency towards higher temperature differences following long IFSs, anomalously
lower values may occur. The observation that shorter IFSs are more consistently
associated with ∆TMAXs closer to 0 gets further credence here from the fact that the range
of ∆TMAX for short years is the smallest of all classes, spanning less than 3°C. The range
of ∆TMAX values for the long class is also smaller than that of the medium class
(considerably so if the -2.4 outlier is omitted) suggesting that longer IFS years also
produce a more consistent signal in ∆TMAX. Though both short and long classes have a
smaller range of values, they differ in terms of the degree to which their respective ranges
overlap that of the medium class. While the ranges of the short and medium classes
overlap by only three values (i.e. observations of 0.0, -0.2 and -2.3 in the medium class),
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the entire range of long values is contained within the range of the medium class. Hence,
it is difficult to distinguish between medium/long classes, but easier to distinguish
between short/medium, and short/long. Table 5 provides a quantitative measure of this
distinction between classes via interclass comparison of means. A p-value of 0.70734 for
the medium/long comparison confirms that these populations are not very distinct. The
short-medium comparison yields a p-value of 0.01833, indicating the two classes are
significantly different at the 95% confidence interval. As expected, the most significantly
different classes are short/long, at a 99% confidence interval (p=0.00036). From these
results, we would expect that any proxy method employing ∆TMAX to discriminate
between IFS lengths would be most successful at identifying short years. Conversely,
such a method would be of little use in distinguishing between medium and long years,
owing to the substantial overlap of the actual ∆TMAX values for these two populations.
Despite the substantial interclass overlap, thresholds of ∆TMAX were established
for each class such that they would maximize inclusion of records with corresponding
IFSs (Table 6). These thresholds, when applied to the existing record, provide an
indicator of the expected confidence such a proxy would carry when hindcasting IFS.
When these thresholds were applied to the 33-year record, it resulted in 14
misclassifications (42%). These thresholds were able to successfully identify all actual
short years, albeit while misclassifying three actual mediums and one actual long as
short. The medium year, with its significant overlap and wide range of values, had eleven
misclassifications out of 18. The long category, while only having three of ten
misclassified, contained a year misclassified by two categories (1981, ∆TMAX=-2.4). The
rather dismal misclassification rate (nearly half) reveals the inadequacies of this
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approach, though the fact that all actual short years can be identified may be of some
value in the absence of any preferable method.
5.4 Wind Direction
As hypothesized, wind direction appears to play an important role in determining
the magnitude of the temperature asymmetry on the Bay. A non-significant, positive
relationship exists between westerlies (NW+W) and ∆TMAX (R2=0.28972, p=0.08761).
This is consistent with the assertion that the temperature asymmetry relies upon Inukjuak
winds having advected over the Bay itself, and hints that to some degree ∆TMAX may
actually be proportional to the frequency of such winds over the 320-350 period. In a
complementary approach, the combined count of NE and E wind direction components
(NE+E) was found to be negatively correlated with ∆TMAX (R2=0.37594, p=0.00241). In
this case, the greater the count of winds arriving from the east (having predominantly
advected over land), the smaller the magnitude of the ∆TMAX signal was generally seen.
The strength of these relationships suggests that wind direction may influence ∆TMAX as
much, or perhaps even more so, than does the length of the ice-free season. With that in
mind, two approaches were taken to explain, and isolate for, the effects of wind
frequency: interpreting wind roses from misclassified years, and reclassifying ∆TMAX
values for years when NE+E was below average.
Of the 33 years on record, 14 do not conform to the established thresholds of
∆TMAX (Table 6). A case-by-case interpretation of the wind roses for those 14 years
reveals that at least seven may be partially explained by an anomalous distribution of
wind direction frequencies when compared to the climate normal for the period of 320-
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350 (Fig. 7). These years include 1981, 1982, 1983, 1985, 1991, 2000, and 2002 (See
Figs. 8-11, 15-16). In general, a year where ∆TMAX is higher than expected based on IFS
tends to also be a year when the W, NW, or SW components are above average (often
with concomitantly lower E/NE components). Presumably, this leads to an amplified ∆T
signal as a greater proportion of winds arriving in Inukjuak have been thermally modified
by the Bay. For example, 1982 saw a ∆TMAX of -10.5°C, despite having an IFS of only
133 days. The wind rose for this year clearly shows a prevailing W component, the
second highest on record. In 1991, both W and SW components are above average, which
again may have contributed to the anomalously high |∆TMAX| of 12.7°C when IFS =141.
Similarly, above average W and NW components in 2000 may explain its
misclassification, though that may also be attributed to the fact that its ∆TMAX of -8.4°C is
simply too close to the medium/long threshold of -8.0°C. In the case of the 1985 wind
rose it can be argued that, despite having an above average NE component, the
combination of above average W and NW components and a very small E component
resulted in the westerlies having a dominant effect on the temperature asymmetry.
Furthermore, as with the latter example, this year’s misclassification may have simply
been a result of its ∆TMAX’s proximity to the medium/long threshold.
In the case of years when |∆TMAX| is lower than expected given IFS, E/NE
components tend to be above average (often with concomitantly lower NW/W
components). This may dampen the ∆T signal, as a lesser proportion of winds arriving in
Inukjuak have been thermally modified by the Bay. Such is likely the case in 1981, when
the distribution of wind directions is dominated by the NE component (second highest on
record) and conspicuously devoid of W observations (lowest on record), with a resulting
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temperature difference closer to 0 than would be expected given IFS (∆TMAX = -2.4°C,
IFS =153). The wind rose for 1983 exhibits a similar distribution with an anomalously
high NE component (3rd highest on record), and below average W component (∆TMAX = -
0.2°C, IFS = 137). In the case of 2002 (∆TMAX = -4.0°C, IFS = 146), the W component is
actually above average, but it might be argued that the combined effect of slightly above
average SE, E, and NE components may have tempered the temperature asymmetry this
year as well. Alternatively, or complementary to that observation, one can also point to
the fact that the ∆TMAX in this case is simply too close to the short/medium threshold of -
4.5°C.
Having demonstrated the nullifying effects of easterly winds on temperature
asymmetry, the classification of ∆TMAX for years when NE+E is below average was done
in hopes of clarifying the ∆TMAX-IFS relationship (Table 7). If isolating for wind effects
results in IFS classes more distinct in terms of ∆TMAX, then a multi-proxy hindcasting
method may be theoretically feasible. Unfortunately, the omission of years when NE+E is
above average, combined with the limitations imposed by the wind record (which only
covers 1981-2007), results in a much less populated dataset from which we can draw
conclusions. Hence, any improvement in the results comes at the expense of a loss in
confidence in said results. Regardless, this approach does not seem to have improved
inter-class differentiation, since the means of medium and long classes are not
significantly different (p=0.3784), and the lack of any short entries precludes further
inter-class comparison. It is worth noting that eliminating above average NE+E years also
eliminated many of the outliers whose ∆TMAX was closer to 0 than expected given IFS
(most notably ∆TMAX= 0.0. -0,2, and -2.3°C from the medium class; and ∆TMAX = -2.4, -
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6.2, and -7.6°C from the long class). However, some of these observations were
eliminated due to absence of wind data for that year rather than due to above average
NE+E winds (∆TMAX = -2.3 and -6.2°C). As a result of the elimination of these
observations, the ∆TMAX means have increased relative to the initial classification, both in
the medium class (from -7.2 to -9.0) and in the long class (from -8.1 to -9.1). This again
demonstrates the tendency of strong easterly winds to dampen (or strong westerly winds
to enhance) the ∆T signal.
As a result of the shift in ∆TMAX values, a new threshold was defined between
medium and long classes that would minimize misclassifications when applied to the
existing record (Table 8). The slightly lower percentage of misclassifications suggests a
slight improvement over the method that includes all years of data. Furthermore, the
elimination of outlier low ∆TMAX years noted above has mitigated misclassification of
actual medium/long years as short. However, the marginal improvements afforded by
eliminating anomalous wind years are rendered less meaningful when one considers the
much smaller dataset.
The relative frequency of westerly and easterly wind components in Inukjuak is
likely an important factor in the sea ice/temperature asymmetry relationship. The true
nature of wind’s role in defining the asymmetry may be more complex than represented
here, but the general rule that westerlies amplify ∆TMAX independent of IFS seems to be
supported by the data. Thus, it is fair to say that any potential proxy for sea ice on
Hudson Bay looking to exploit the temperature asymmetry would suffer in terms of
accuracy without the consideration of wind direction in some form. Unfortunately, the
lack of wind data prior to 1982 precludes the possibility of any such multi-proxy.
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5.5 Multiple Variable Approach
The equation produced by multiple regression [Eqn. 1] is revealing of the physical
relationships between each temperature variable and ice-free season length. The
regression coefficient for the explanatory variable TF is approximately 6 times that of the
variable ∆TMAX. This reiterates what was discovered in the classification approach, that
TF is a stronger indicator of IFS. However, the R2 value of 0.62863 obtained in the
multiple variable regression is higher than those obtained using either variable considered
alone. The improvement over the TF-IFS relationship (R2=0.59051) is marginal, though it
again demonstrates that ∆TMAX does add some unique information regarding IFS. As a
sort of “thermal memory” term, whose magnitude is determined by conditions throughout
the entire ice-free season, ∆TMAX inherently contains some information regarding breakup
conditions that cannot be conveyed by TF. Since TF is the stronger explanatory variable,
this approach can be thought of as a tweaked version of the TF regression, where the
addition of the ∆TMAX explanatory variable further hones the prediction. The actual value
added by adopting a multi-variable proxy approach is further quantified below.
5.6 Evaluating Proxies
The temperature variable TF serves here as a benchmark for evaluating the
performance of ∆TMAX as a proxy in two ways. Firstly, TF values are classified by IFS to
assess the performance of ∆TMAX in classifying IFS as short, medium and long. Secondly,
the IFS values produced by the equation obtained by linear regression between TF and
IFS are compared to those produced by the multiple regression equation to again assess
the value of ∆TMAX in such a proxy.
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5.6.1 Classifications
To obtain the TF variable, temperature was averaged over Churchill and Inukjuak,
as well as being averaged over a longer period of time (61 days, compared to 31 for
∆TMAX). As a result, the range of values of TF is much smaller than that of ∆TMAX,
spanning only from -5.0 to 2.0 °C. With this smaller range, it is even more important that
the populations of the three classes be distinct with little overlap in order for this method
to be useful as a predictor for sea ice. When classified (Table 10), the means of each class
increase along with length in IFS. This is to be expected, since colder temperatures
during the 260-320 freeze-up period would tend to expedite sea ice formation leading to a
shorter IFS (with warmer temperatures tending to delay freeze-up for the opposite effect).
A comparison of means reveals that all three classes are significantly different from each
other at the 95% confidence interval (Table 11). More importantly, a comparison of
these p-values to those found in the ∆TMAX –IFS approach (Table 5) shows a marked
improvement in the TF approach in terms of inter-class distinction, particularly between
the medium and long categories. This means that despite the smaller range of TF values,
the differentiation between classes is greater than in either of the two previous methods
using ∆TMAX.
Having established thresholds of TF for each class, applying them to the existing
record provides a measure of how reliably these thresholds can be expected to hindcast
IFS. The misclassification rate for this method was the lowest yet at 30%, though there
are also some important differences in terms of what was misclassified. Most
importantly, there are no misclassifications by two classes, as was the case in the first
∆TMAX method. The one misclassified short year here indicates that this method cannot
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capture all actual short years, the singular advantage of the ∆TMAX method. However, this
method nearly captures all actual long years, with the only misclassification in that
category having a TF straddling the medium-long threshold.
A side-by-side comparison of the three classification proxy methods investigated
makes it clear that the ∆TMAX proxy method does not outperform the TF method in
recreating the existing IFS record (Table 13). As evidenced by the higher R2 value, TF is
much more useful at explaining variability in IFS, and as a result can be used to classify
IFSs more reliably.
5.6.2 Linear Regression
By including both explanatory variables in a multiple regression with IFS, both R2
and p-value were greater than either of the single-variable correlations with IFS (Table
16). This marked improvement presents the opportunity for the use of the multiple
regression equation to predict IFS in lieu of the classification approach. A comparison of
Tables 14 & 15 reveals how much the multiple regression approach improves error in
reproducing the IFS record. The average error using the TF equation is 8.7 days, while the
TF-∆TMAX equation average error is 8.1 days. Thus, including the temperature difference
variable can be expected to improve results on average by 1 day (rounded up). The
multiple regression errors have a standard deviation of 4.7, meaning that 68% of the
predictions for IFS will be accurate to within 4.7 days of actual IFS. This is a fair level of
accuracy when one considers that the breakup and freeze-up dates used to determine IFS
themselves are only measured every 7 days (Gagnon & Gough, 2005). Therefore, for the
purposes of hindcasting IFS to a degree of accuracy that is comparable to the actual
record, the multi-proxy approach employing both TF and ∆TMAX is superior to the TF
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proxy alone. Furthermore, the advantages of the multiple regression equation results over
the classification results in terms of temporal resolution make the TF-∆TMAX multi-proxy
the best candidate to produce a hindcast time series of IFS.
5.7 Trend Analysis of Extended Record
The appended time series shown in Figure 19 provides a longer period of time
over which baseline conditions for IFS can be assessed. In doing so, it also provides a
means of eliminating low frequency climate oscillations as an explanation for the recent
increase in IFS. The high interannual variability of IFS throughout this record is a quality
that should be expected given the inherent variability of sea ice and driving climate
factors. Even considering this variability however, the tendency towards higher IFS in the
latter decades appears to be unprecedented from 1944-1995. Values in this earlier period
generally range from 120-160 days ice-free, with a few exceptions in 1947, 1948, 1968
and 1972. Following 1995, short IFSs appear to be less frequent, with only one year
having an IFS<140 (2004). Conversely, long IFS appear to become more frequent, with 7
years having IFS>160. Applying a five-year moving average leads to a smoothed curve in
which this increasing trend is made more apparent (Figure 20). This graph shows
averages oscillating with a periodicity of approximately 5 years, but maintaining a
relatively steady state over the long term up until about 1995, when an increasing trend
begins to develop.
The observed trends were assessed over different time periods using the Mann-
Kendall test (Table 17). The τ value of 0.208 for the entire time series (1944-2011) hints
at a trend, but this value is likely being diluted by the lengthy period when there is no
trend. When considering only the latter decades of the time series, the trend becomes
83
more apparent and statistically significant. Of the four arbitrarily selected “trend” time
periods, all produce τ values indicative of positive trends that are statistically significant
at the 99% confidence interval. By contrast, none of the accompanying baseline periods
exhibit any significant trends. The period with the greatest evidence for a positive trend
in IFS is that of 1985-2011 (τ = 0.607, p<0.0001).
Appending the hindcast record to the historical record provides context for the
increasing trend in IFS observed in the last few decades. The actual IFS time series on its
own does present compelling evidence for an increase in the duration of the ice-free
season, but the hindcast time series provides greater confidence in that trend by showing
that such long IFS are unprecedented in a 68-year record. Taking temperature as the most
significant source of variability, one can point to many non-anthropogenic oscillations on
various temporal and spatial scales that might account for fluctuations in IFS. Any such
oscillations with a sub-decadal periodicity, such as the El Nino Southern Oscillation
(ENSO) or the North Atlantic Oscillation (NAO), would be resolved by the actual IFS
time series. When considering the extended time series, many of the interdecadal
oscillations, such as the Interdecadal Pacific Oscillation (IPO), would be reflected by a
periodicity in IFS if they were in fact driving the recent increasing trend. However, even
the 68-year record cannot conclusively eliminate all sources of climatic variability in this
manner, as there exist low frequency climate oscillations on larger time scales that this
time series cannot capture (Mahasenan et al., 1997). Thus, the extended time series
provides conclusive evidence that the recent increasing trend in ice-free season on
Hudson Bay is not attributable to low-frequency climate oscillations of a periodicity <68
years.
84
5.8 Complicating Factors in the Sea Ice-∆T Relationship
Despite the fact that sea ice is most certainly influencing ∆T on an annual time
scale, and that interannual variations in ∆TMAX seem at least partially related to variations
in IFS, this study has shown that this relationship on its own is not strong enough to
exploit as a useful proxy. The climate system and its interrelationships with sea ice are
inherently complex with a multitude of interacting variables. Wind direction is one such
variable that was accounted for in this study, though its role may be more nuanced than
presented here. For example, wind velocity, though not taken into consideration here, has
been shown to be an important variable in the exchange of latent heat at the air-water
interface (Sousonis, 1992; Raymond, 1986; DeMaria, 1985). Hence, upward heat flux on
the Bay, and by extension the asymmetrical temperature signal, may differ between two
days that have an identical wind direction distribution but vary in terms of the relative
strength (velocity) of those winds. Furthermore, the binary characterization of wind
direction as strong westerly /strong easterly, though appropriate towards the objective of
developing a simple proxy, ignores the effects of other direction components (particularly
N/S). Wind analysis by vector summation would account for both these issues (Coffin,
1964). Such an approach might help in better explaining years with anomalous ∆TMAX
signals, further elucidating the role of wind in the sea ice-temperature asymmetry
relationship. Beyond wind effects unaccounted for in this study, there remain further
complicating factors that warrant some discussion; namely ice thickness, water
temperature, and spatial scale.
The insulating properties of sea ice have been shown to be highly dependent on
thickness (Dieckman & Hellmer, 2009). This is highlighted by the ∆T climate normal
85
(Figure 2), when the greatest temperature difference seems to be occurring well into the
freeze-up season, and the negative phase persists even after the entire Bay is frozen. This
suggests that the upward flux of heat allowed by immature, thin ice is sufficient to
produce an asymmetric temperature signal. This complicates efforts to accurately
characterize the SIC-∆T relationship, as observations of SIC do not discriminate between
areas of similar concentration but differing thicknesses. This complicating factor may
explain some of the variability in weekly ∆T values, but is not expected to affect the IFS-
∆TMAX analysis, as IFS is serving only as a general indicator of sea ice conditions in a
given year.
As outlined in section 2.6, the temperature asymmetry arises in response to
upward fluxes of sensible and latent heat from open water. Sensible heat flux is in turn a
function of the difference, or gradient, in temperature between the water and the
overlying air. Sea surface temperatures (SST) are continually increasing throughout the
IFS, reaching an average maximum of ~7.5°C in August (Galbraith & Larouche, 2011).
This peak in SST does not coincide with the peak in ∆T. This is likely because as air
temperatures start to drop in the fall, the gradient at the air-water interface will sharply
increase as the heat capacity of the water slows its temperature decrease relative to the
air. Along with this stronger gradient comes a greater upward heat flux, and hence greater
∆T, that persists until the water temperature begins to decline in turn. This relationship
between SST and air temperature is the driving force behind the temperature asymmetry,
but these variables are not used directly in this study. An analysis of how SST and the
temperature in Churchill (the last upwind air temperature observation for westerlies)
86
track throughout the IFS might help clarify the role of sea ice in defining the temperature
asymmetry.
Hudson Bay is a vast body of water exhibiting considerable spatial and temporal
heterogeneity in its sea ice cover. Those few studies demonstrating some success in using
a temperature-lake ice correlation as a predictive tool were done on much smaller scales,
generally lake systems spanning <100 km (Livingstone, 1997; Palecki & Barry, 1986;
Williams, 1971). Unlike with these past studies, the temperature asymmetry in this study
is being shaped by local, regional, and synoptic scale atmospheric forces that conspire to
make a clear signal of sea ice conditions very difficult to detect. Therefore, it is highly
likely that there are limitations to the spatiotemporal resolution of any proxy that attempts
to make generalized predictions on sea ice across the entire Bay. The issue of scale may
also be affecting the temperature signal in a more direct way, by placing an upper limit
on upward heat flux. Lake effect phenomena are often said to be “fetch-limited”, that is
to say that their occurrence or severity is a function of the upwind distance over which
advecting air has the opportunity to be moistened and destabilized (Andreas & Cash,
1999). Once an air mass responding to a new surface has fully developed a thermal
internal boundary layer (TIBL), it is at equilibrium with the new surface and energy flux
ceases until conditions change. Since this typically occurs in the range of 10s of km to a
few 100 km, it is safe to say that the Bay is not fetch-limited (Garratt, 1990). This means
that there may sometimes be an upper limit to the thermal modification of an overlying
air mass, beyond which there ceases to be any energy input and hence any additional
information in the temperature signal. This is particularly important given the spatial
heterogeneities inherent to sea ice on the Bay, as it might be difficult, for example, to
87
distinguish between a ∆T signal for completely open water, and a ∆T signal when all but
the southwestern coast is open water (as is the case toward the end of the breakup
season). This problem would have more of an effect on finer resolution proxies such as
the abandoned weekly ∆T approach, but probably does not present any issues for the IFS
approach.
The preceding are but a few complicating factors that are likely influencing the
sea ice-temperature difference relationship, but there are likely other variables
unaccounted for that may be just as important. Some of these might theoretically be
incorporated into a more complex, multi-variable proxy for sea ice, though only if the
extent of their records allow for it. Regardless, if the aim were to develop a simple proxy
based only on air temperature data, these complicating factors would tend to hinder such
an approach.
5.8 Sources of Error
Since all of the data used in this study was originally obtained from Environment
Canada, and hence subject to their own scrutiny before being made available, it is
unlikely to be the source of any errors (See 3.9 Notes on Data Quality). It is possible that
the variables derived from the source data (IFS, ∆TMAX, TF) were not optimized. For
example, since the ∆TMAX window of 320-350 was informed by the ∆T climate normal,
combined with empirical trial-and-error of alternative windows, it is likely that most
years it does in fact capture the strongest ∆T signal of the year in question. However,
there also may be certain outlier years in IFS when the period of maximum asymmetry is
shifted. If so, there may be some other window that would provide a more representative
88
∆TMAX. Though accounting for this error might help further characterize the IFS-∆TMAX
relationship, it is inconsequential for the purpose of developing a proxy, since a fine-
tuned ∆TMAX window would not be possible in the absence of ice data.
Another source of error likely comes from the simplification of the data set
necessitated by this methodological approach. Reducing 36 spatial points of data into a
single value ignores the heterogeneity of breakup and freeze-up dates on the Bay. This
results in a useful general indicator of sea ice conditions, but perhaps at the expense of a
stronger relationship between predictor and predictand. Likewise, while averaging
temperature data over 31 or 61-day periods reduces noise and ensures the desired signal
is captured, it also may result in a dampening of the signal. While these concessions are
necessary given the nature of the study, their shortcomings should be noted. Additionally,
refining the definition of these variables in light of new information could yield
improvements to the relationship and by extension a proxy method.
5.9 Research Impacts
While this study has elucidated the unique phenomena of seasonal temperature
asymmetry on Hudson Bay, the most tangible impacts of its findings come from: 1)
advancing the knowledge on site-specific sea ice proxies, and in so doing 2) producing a
hindcast time series that allows for a more robust trend analysis of ice-free season.
Although the temperature asymmetry alone was shown to be a weak proxy for sea ice,
combining it with a measure of absolute temperature created a multi-proxy that allowed
the Hudson Bay sea ice record to be extended by 28 years. This extended time series in
turn allows for a superior trend analysis, whereby the recent increase in IFS can more
89
confidently be attributed to anthropogenic climate forcing. These findings contribute to
the existing body of knowledge on climate change, specifically as it relates to sea ice in
Hudson Bay. What it reveals is not new, but rather further evidence that corroborates past
studies showing a decline in various metrics of sea ice on Hudson Bay and the broader
Arctic Ocean (Comiso et al., 2008; Gagnon & Gough, 2005; Gough et al., 2004;
Hochheim et al., 2011; Hochheim & Barber, 2010; Parkinson et al., 1999; Stroeve et al.,
2007; Vinnikov et al., 1999). The implications of a continuing and accelerated decline in
sea ice; economically, socially, and ecologically, would be profound. The sensitivity of
Arctic mammals such as polar bears to declining sea ice has been well documented, and
further declines would most certainly prove detrimental to their population ecology
(Derocher et al., 2004; Stirling et al., 1999; Stirling & Parkinson, 2006). Inuit populations
along the coasts of the Bay may also have to further adapt their subsistence hunting and
travel practices as sea ice patterns continue to change (Tristan et al., 2010). The local
economy will be affected, for better or worse, as the shipping season for routes through
the Hudson Strait to the Port of Churchill depend upon breakup and freeze-up dates
(Prowse et al., 2009; Tivy et al, 2007). The stakeholders in these three issues would all
benefit from a stronger trend analysis that allows for an accurate impact assessment of
future sea ice conditions, while hopefully informing public policy and decision-making
with regard to mitigation and adaptation to these changes
90
Chapter 6: Conclusion
6.1 Research Objectives
In fulfilling Objective 1, the nature of the temperature asymmetry’s response to
changes in sea ice was characterized at both weekly and seasonal time scales. Based on
the results of the weekly SIC-∆TW correlation, it can be concluded that the average SIC
of the Bay does not produce a consistent weekly average temperature difference signal.
The lack of any relationship between these two variables can be attributed in part to
inherent climatic variability at finer temporal scales, but is also likely due to the
significant lag time between a change in sea ice conditions and a thermal response from
the Bay’s water. This lag means that peak temperature differences, the driving agent of
which was open water, are not seen until well into the freeze-up season. This fact makes
the determination of any cause-effect relationship at a weekly temporal resolution wholly
unfeasible.
Based on the IFS-∆TMAX analysis, it can only be concluded that, over the ∆TMAX
period, there is a general tendency toward greater coastal temperature differences in
years when the ice-free season is above average. It can be stated with greater confidence
that during years with anomalously short ice-free seasons (IFS<129), coastal temperature
differences are more likely to be close to zero (∆TMAX >-4.5°C). The hypothesis that wind
direction was a major contributor to the temperature asymmetry proved to have some
merit, with strong westerlies (and/or weak easterlies) tending to be associated with
greater temperature differences.
With regard to Objective 2, this study did propose a proxy method employing the
temperature asymmetry alone, but its utility was determined to be negligible for lack of a
91
strong enough relationship with IFS. Based on the results of applying ∆TMAX thresholds
to the existing record, it can be expected that hindcasting IFS into three classes using this
method would carry with it a 42% error rate. This method can be used to greater effect in
capturing all actual short years, but there would still me misclassifications owing to the
expected inclusion of medium and long years. A multi-proxy method that classifies IFS
based on ∆TMAX only for those years when easterly winds are below average produced
marginally better results. However, the lack of wind data prior to 1982 precludes the use
of such a method to hindcast IFS. Therefore, it can be concluded that the seasonal
temperature asymmetry on Hudson Bay should not be used in isolation as a proxy for sea
ice conditions. In arriving at that conclusion however, the use of absolute temperature as
a benchmark for evaluating proxies demonstrated some potential itself as a tool for
hindcasting ice-free season. A multiple linear regression equation using both TF and
∆TMAX was able to reproduce the existing IFS record with an average error of 8.1 days,
an approximately 1 day improvement over a linear regression equation using TF alone.
This multi-proxy was used to hindcast 28 years of IFS, producing a time series that
totaled 68 years in length. From this lengthened time series, it can be concluded that the
recent increase in IFS is unprecedented during the period of 1944-2011, and hence
unlikely to be a result of climate variability.
6.2 Recommendations for Future Research
Since the sea ice-temperature asymmetry relationship is fundamentally lacking
sufficient strength to allow for a fine-resolution proxy, further research into this particular
approach is not recommended. However, given that the combination of ∆TMAX with TF
92
was able to predict IFS within 8.1 days, further research into this multi-proxy for sea ice
on the Bay is definitely warranted. Experimentation with the TF variable that makes use
of other climate stations, or a focus on different periods of the cryogenic cycle might
yield even better results. In addition, further inquiry into altogether different approaches
than those investigated here is highly advisable. For example, the same contrasts in
energy budgets between land and sea exploited in this study also lead to local circulations
in coastal regions. These local circulations are very different depending on the ice state of
the adjacent sea. The resulting diurnal variability of temperature contains a signal that, if
strong enough, could be predictive of sea ice cover for that location (W. Gough, pers.
comm., 2012). Such local-scale approaches acknowledge the spatial limitations imposed
by the complexity of sea ice-atmosphere interaction and the heterogeneity of sea ice on
the Bay. Furthermore, results from an alternative proxy for Hudson Bay sea ice could be
used to corroborate the conclusions arrived at in this study. With further research, it is
likely that the proposed method for hindcasting sea ice conditions based on temperature
can be honed to provide more accurate results, lending further confidence to the trend
analysis.
93
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Appendix: Wind Roses
Below are the wind roses for those years when the actual IFS were concordant
with the established thresholds of ∆TMAX. Note the omission of years 1992,1993 and
2008-2011for lack of wind direction data, as well as the omission of 1994 for lack of
temperature data, and 1997-1999 for lack of sea ice data.
Figure 21: 1984 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -5.1°C, IFS = 132 (Medium).
The wind rose for 1984 shows the most frequent wind direction as N, and the
frequency count for the N wind is the highest on record. With relatively fewer, W, NW,
NE and E component counts, it is likely that wind direction did not play a role in
accentuating or nullifying IFS effects on ∆TMAX.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
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Figure 22: 1987 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -2.8°C, IFS = 128 (Short).
The 1987 wind rose is dominated by largest frequency count of NE winds on
record. If the IFS had been classified as long this year, it might be expected that this
strong NE component would have had a nullifying effect on the ∆TMAX signal, but since
this year actually had a short IFS the temperature difference could be attributed to sea ice
conditions, strong NE winds, or some combination of both. It might be argued that with
such a lack of westerly winds and a short IFS one would expect the temperature
difference to be even closer to zero, but a difference of 2.8°C could just as easily be
attributed to climatic variability.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
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Figure 23: 1989 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -7.6°C, IFS = 141 (Medium).
The 1989 wind rose shows that W, NW and NE components were all close to
average. The lack of an E component may have allowed for the development of a
medium ∆TMAX signal that is representative of actual IFS conditions.
Figure 24: 1995 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -5.3°C, IFS = 147 (Medium).
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
103
The wind rose for 1995 shows that NE and E components were significantly
stronger than W and NW components. Despite the fact that ∆TMAX falls within the
defined thresholds for medium IFS, dominant E and NE winds could have dampened the
∆TMAX signal such that it would have been closer to the medium-long threshold under
normal wind conditions. If so, the ∆TMAX would have more strongly correlated with the
IFS, as it too is on near the medium-long threshold at 147 days.
Figure 25: 1996 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.0°C, IFS = 151 (Long).
The 1996 wind rose is dominated by an anomalously large E component (largest
on record). Despite this strong E component and relatively weak W/NW components, the
temperature difference signal is one that would be expected given the long IFS. Hence,
this year does not conform to the hypothesis of easterlies dampening temperature
differences, and there may be other climatic variables at work.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
104
Figure 26: 2001 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.2°C, IFS = 164 (Long).
The wind rose for 2001 shows a slightly above-average NW component but an
equally strong N component. The effect of the N component is not known, though it is
presumed to have negligible amplifying or dampening effects on ∆TMAX. Hence, it is
likely that the strong NW component allowed the development of a strong temperature
asymmetry. Again, one can speculate that if the W component were stronger than the N
component that ∆TMAX might be even more significant, given the very lengthy IFS.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
105
Figure 27: 2003 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.6°C, IFS = 158 (Long).
The wind rose for 2003 shows a roughly equal distribution of all components.
Hence, it is likely that the W/NW components was sufficient to produce an asymmetric
temperature signal in line with the long IFS, while no components were dominating
leading to amplification or dampening of that signal.
Figure 28: 2006 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -9.7°C, IFS = 170 (Long).
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW
106
The wind rose for 2006 shows above average W and NW components, average E
component, and below average NE component. There are no major anomalies in the
distribution of direction frequencies that would significantly alter the temperature
asymmetry, while the westerly components are allowing for its development. Hence, the
∆TMAX value alone is representative of the IFS in this case.
Figure 29: 2007 wind rose for Inukjuak over Julian days 320-350: ∆TMAX = -8.0°C, IFS = 162 (Long).
The wind rose for 2007 shows a significant W component (3rd largest on record)
which, combined with an average NW component, dominates over easterly wind
components. Given this year is definitively classified as long in terms of IFS, and the
relative strength of W winds, one might expect the temperature difference signal to be
greater. Despite this perceived anomaly, ∆TMAX still successfully classifies this year as a
long IFS.
0 50 100 150 200 250 300
N
NE
E
SE
S
SW
W
NW