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1
Time-varying betas of sectoral returns to market returns and
exchange rate movements
Hyunjoo Kim and R. Scott Hacker
Department of Economics
Jönköping International Business School (JIBS)
P.O.Box 1026 SE-551 Jönköping, Sweden
Abstract
The time-varying behavior of the market and exchange risk sensitivities of the U.S. sectoral
returns are estimated using random walk process in connection with the Kalman filter. As a
whole, it is observable that the market risks shrink over longer time-horizons. As regards
exchange risk, the findings are consistent with the notion that high US returns will induce a
greater capital inflow into the US stock market and thereby cause an appreciation of the US
dollar. The exchange rate risks appear to be declining with longer time horizons, in some cases
resulting ultimately in a negative relationship between the US dollar and the industry returns.
This is consistent with the idea that the effect of a US dollar appreciation on competitiveness of
US exports becomes stronger with the larger time horizons.
1. Introduction
The objective of this paper is to investigate the time-varying behavior of beta of the industry
returns in the U.S. stock market to market returns and to exchange rate movements. An
empirical beta pricing model, where industry-specific conditional betas measure sensitivity to
market and the global risk factors, is formulated. From here and onwards, betas and sensitivities
are used interchangeably. These sensitivities are measured for various industries at the
supersectoral level for the 1995 – 2010 period and are measured at different time horizons. This
investigation allows us to consider various relevant issues, as listed below.
The first issue is how exchange rate movements are associated with industry returns after
controlling for movements in the market premium (the market return minus the risk-free return).
The returns performance in reaction to exchange rate change should be different in different
industries, with one expectation being that industries with substantial US production and heavy
involvement in exports should be negatively affected by appreciation of the US dollar due to loss
of competitiveness. For industries with substantial multinational involvement the opposite is true
due to the gain in competitiveness for subsidiaries outside the US, although the appreciation
causes foreign revenues in dollar terms to diminish for the same amount sold, which could then
be reflected in lower returns in dollar terms. The value of intermediate goods from abroad also
has an impact on how the exchange rate affects industry returns, with industries relying more
heavily on non-US intermediate goods being positively affected by a dollar appreciation as
foreign inputs appear cheaper in US dollars.
2
Exchange rate relationships with industry returns get further complicated by a causal relationship
opposite to that considered in the previous paragraph. For example if an industry‘s stock prices
show a strong upward trend while those in other industries are flat, investors from outside the
US will be induced to invest in the industry with the growing returns, putting upward pressure
on the dollar. By this means, a positive relationship between an industry‘s returns and the value
of the dollar may be observed.
If exchange rate movements are associated with industry returns after controlling for movements
in the market premium, then this foreign currency risk would have direct implication for hedging
strategies if the currency risk is a priced factor in international financial markets. This is the case
because any source of risk that is not compensated in terms of returns should be hedged. (Santis
and Gerard, 1998).1
The second issue is which industries become more sensitive to the market premium and to
exchange rate movements, during a financial crisis and after a financial crisis. Typically
―defensive‖ stocks, i.e. those with low betas, are expected to fare better than other stocks during
a financial crisis as investors flee from riskier alternatives. Another relevant point when focusing
on US data is that international financial crises tend to put downward pressure on returns and
can put upward pressure on the dollar as investors consider it a safe-haven—even if the US is at
the center of the financial crisis.
A third issue is whether findings relevant for the first issues vary by the time horizon over which
returns and exchange rate movements are measured. One may expect that at short time horizons
stock price movements are highly influenced by technical factors, with speculators reacting solely
to stock price movements throughout the market due the lack of information (or cost of
collection that information) as to what is the fundamental reason behind the movements. This
arguably creates higher market betas at shorter time horizons than at longer time horizons, at
which point fundamentals become more relevant in stock valuation. On the other hand, Gensay,
Whitcher, and Selcuk (2005) claim that since macroeconomic variables are harder to predict over
longer time horizons, beta estimates should be higher at those longer time horizons. They
investigate this claim with results from wavelet analysis, which dissects time series into different
layers without losing original information. They reported that beta indeed becomes stronger as
the wavelet scale increases and that predictions of the CAPM are more relevant at medium- to
long-run horizons as compared to short time horizons.
Similar arguments arise when considering the relationship of returns to exchange rate
movements. At short time horizons investors may overestimate the impact of exchange rate
movements and can consider such movements as part of a longer trend which may not occur.
1 Empirical studies on exchange rate exposure point out that the effect of exchange rate shock is made very complex
because firms often hedge some of their foreign exchange exposures. Those empirical studies, therefore, had only
limited success in finding statistically significant exposures for most firms, which was called ‗exposure puzzle.‘ Two-
types of hedging activities of firms were presented to explain the puzzle: 1) financial hedging activities which reduce
exposure by using foreign currency derivatives or other type of financial instruments; 2) operational hedging which
is geared toward reducing long-run exchange rate exposure by pricing practices or marketing decisions in response
to exchange rate movements (Bartram and Bodnar, 2007).
3
Due to this we may find stronger relationships between returns and exchange rates at shorter
time horizons rather than at longer ones. However, Bartov and Bodnar (1994) note that
prediction of the firms value from the changes in exchange rate would be reflected in stock
returns only when information about the effects of exchange rate changes on future cash flows is
revealed over time. Using long-horizon exchange rates and stock returns, therefore, may be more
informative compared to utilizing short-horizon exchange rates. Building on this insight, we
suggest also that at short time horizons the impact of exchange rate changes on investment
decisions will not be strong, but the effect of investment decisions across various international
asset markets will affect the exchange rate rather strongly at short time horizons. Thus we expect
at short time horizons a rise in expected US returns to positively affect the value of the US dollar,
but as the time horizon expands, a lower positive or even negative relationship between the US
dollar and US returns may arise. This relationship at the longer time horizon may come about as
the profitability in many US industries decline with a loss in international competitiveness of US
products due to US dollar appreciation.
To investigate these various issues, this paper presents time-varying coefficient estimates from an
industry-level international CAPM model, which includes exchange rate changes as an additional
explanatory variable in a CAPM-type model. A Kalman filter is used in the estimation of these
coefficients, and the estimates are performed at different time horizons for the data: daily, weekly,
monthly, quarterly, and yearly.
The paper is organized as follows. In the next section a background discussion is provided, and
in the section following that data used in this study is described along with methodology adopted
in this paper. In section 4 the empirical findings are presented, then in section 5 the conclusions
drawn are summarized.
2. Background
Estimating a beta of a stock to the overall market can be done in the single factor capital asset
pricing model (CAPM) developed by Sharpe (1964), Lintner (1965) and Black (1972). Beta
measures the systematic risk, i.e. the sensitivity of a stock to the market index, which determines
the required rate of return on equity (i.e. the cost of equity for the firm). The CAPM set a corner
stone of modern finance with beta representing one of the most widely used concepts in finance
and there is controversy about how serious the evidence against it really is (Campbell, Lo and
Mackinlay (1997). The CAPM has been questioned by several empirical studies, which are
presented in table 1. While the early literature on CAPM is included in the cell (1) where one
factor―the rate of return on the market portfolio―is linearly related to the security rates of
return, empirical studies in the categories of the cells (2)-(4) found that the one constant beta
does not explain much of the cross-section variations of average returns.
Table 1. Categories of literatures in asset pricing models
Constant Time-varying
One-β (1) (3)
Multiple- β (2) (4)
4
One line of empirical studies of the CAPM was done for its theoretical extensions.2 One of such
an extension is international CAPM which considers an additional source of risk, exposure to
exchange rate risks, in the asset pricing models (Solnik, 1974; Stulz, 1981; and Adler and Dumas,
1983).3 Dumas and Solnik (1995) was supportive of the existence of a foreign exchange risk by
using a conditional approach that allows for time variation in the returns for exchange rate risk in
international asset markets. Consistent with the results of Dumas and Solnik (1995), Santis and
Gerard (1998) and Santis et al. (2003) also support a model which includes both the market and
exchange risks in a conditional version of the international CAPM. 4 As regards multifactor
models, Fama and French (1992), in particular, has received a lot of attention and led
propagation of multifactor models including Fama-French type factors, which belongs to the cell
(2).
The other line of empirical studies, which belong to the cell (3), questioned the validity of beta
stability assumption (Fabozzi and Francis, 1978; Sunder, 1980; Bos and Newbold, 1984; Collins
et al., 1987). This area of empirical study is known as conditional-CAPM testing which updates
expected returns or volatility conditioned on the most recent past information. Researchers in
this area of study have used different methodologies including GARCH, GARCH-in-means,
Kalman filter for studying time-varying systematic risks(Fernandez, 2006). Allowing for betas to
vary over time not only removes the assumption on linearity in asset price modeling but also
accounts for possible effect of omitted variables (Gonzalez-Rivera, 1997).
Given the results of the previous studies in the subject area, the Kalman filter (KF) is employed
in this paper as an empirical methodology to consider time-varying beta (sensitivities) in studying
sectoral returns. In so doing, this paper lends itself to an understanding of the time-varying
relationship with the two given variables―a market portfolio return and a rate of change in
exchange rate. This paper, thus, can be categorized in the cell (4) of table 1 in asset pricing
models. Additionally, tests results are compared by using different frequency of data observation
to see whether the results hinge on using certain frequency of the data.
The Kalman filter(KF) is a recursive algorithm for numerical estimation of state space models
where the observed dependent variables are parameterized as function of unobserved state
2 The theoretical extensions of the CAPM include 1) after-tax CAPM in which investors must be compensated with
higher pre-tax returns due to higher taxes imposed on high dividend-yield stocks; 2) the inter-temporal CAPM in
which investors are concerned not only with their end-of-period payoff, but also their wealth at time t ,which might
vary depending on labor income, the prices of consumption goods, and expectations about them; 3) the
consumption CAPM (C-CAPM) in which the risk in future consumption is the only one risk. 3 If purchasing power parity (PPP) does not hold continuously in an international context, any investment in a
foreign asset entails the performance of the domestic currency relative to the foreign currency along with the
performance in an investment of the foreign asset and. Investing in foreign markets, thus, is combined with
exposure to exchange rate risks (Dumas, 1983). Stulz (1995) includes a survey of empirical studies which are limited
to unconditional version of the international CAPM model. The results are inconclusive. 4 The existing literature on the relationship between stock prices and exchange rates, however, provides inconclusive
results or only weak evidence of systematic exchange rate exposure. Overall, evidences of the empirical studies on
exchange rate risk suggest that it is marginally larger in open, exports-oriented economies (Bartram and Bodnar,
2007).
5
variables. The unobserved state variables in this paper are sensitivities to market excess returns
and exchange rate movements, both of which are modeled as following a random walk process.
This framework was chosen given the latest finding by Mergner and Bulla (2008) where different
modeling techniques were compared to analyze the time-varying behavior of the systematic risk.
By comparing ex-ante forecast performances (the mean absolute error (MAE) and the mean
squared error (MSE)) of the six models―a bivariate t-GARCH (1.1) model, two Kalman filter
(KF)-based approaches, a bivariate stochastic volatility model estimated via the efficient Monte
Carlo likelihood techniques and two Markov switching models―the Kalman filter approach with
the random walk process is preferred to other models to describe and forecast the time-varying
behavior of the beta.5
Time-varying sensitivities in this paper are focused on the US industry portfolio. The
macroeconomic and industry analysis are two of major aspects in the process of security analysis.
It is necessary to examine sensitivities of industry groups since the investment advice of portfolio
managers are tied to the macroeconomic forecasts, however, not all industries are equally
sensitive to the macroeconomic conditions (Yao and Gao, 2004). Industries are also related with
the world economy with varying degrees of returns in response to the exchange rate fluctuations
(Bodnar and Gentry, 1993; Griffin and Stulz, 2001; Doidge et al., 2003). Therefore, by
comparing exchange risk sensitivities of different industries, this paper explores whether they
display varying sensitivities to the exchange risk
Additionally, time-varying sensitivities of each sector are compared at different frequencies of
data observation to examine the impact of time horizons on the beta estimates. Studies on the
return interval of beta estimate provided evidence that time scale is an important issue in beta
estimation. One study on this issue, that by Gensay, Whitcher, and Selcuk (2005), was already
discussed in the introduction. Another study, by Brailsford and Faff (1997), documented that
greater support for CAPM with a GARCH-M specification was found using weekly return than
using monthly interval returns, while the daily return interval in that study did not support the
CAPM.
3. Empirical methodology and data description 3.1. Data description
The nominal exchange rate variable used in this paper is the foreign currency value of a U.S.
dollar (nominal effective exchange rate, NEER),6 i.e. an increase in the exchange rate implies an
5 Brooks, Faff, and Mckenzie (1998) compared three different techniques for the estimation of conditional time-
varying betas, where the Kalman filter approach was more supportive than the others based on in-sample forecast
errors. Different papers which used each of the modeling techniques are well summarized in Mergner and Bulla
(2008). 6 Many studies on foreign exchange exposure use nominal effective exchange rate for a relevant exchange rate.
However, using trade-weighted exchange rate bears a shortcoming of lacking power if a firm or an industry is
exposed only to a small number of currencies. Creating a firm- or industry-specific exchange rate could mitigate this
problem, yet this approach lacks of basis on which these bilateral exchange rates should be chosen (Williamson,
2001). Other than the nominal effective exchange rates used and reported in the following empirical section, USD
against major currencies, USD against G10 economies were also used in empirical test.
6
appreciation of the U.S. dollar and a depreciation of the foreign currency. The foreign currency is
the multilateral trade-weighted currencies of a large group of major U.S. trading partners, which
is computed with the following weights: Japan (30.29%), Canada (25.09%), Germany (11.50%),
United Kingdom (8.91%), and France (5.84%). The EU accounts for 41.19% and euro area
countries for 29.80%. The nominal effective exchange rate is used instead of real effective
exchange rate for the following two reasons (Bodnar and Gentry, 1993). One is that the real
exchange rate is based on the assumption that financial markets instantaneously observe inflation.
The other is that nominal and real effective exchange rates are highly correlated during the
sample period. The correlation between them is 0.876.
For the market returns, the total return (i.e. dividends are reinvested) series of the MSCI ACWI
(All Country World Index) Index are used.7 The MSCI ACWI is a free float-adjusted market
capitalization weighted index that is constructed by gathering equity market performance of
developed and emerging markets.8
7 Other than MSCI ACWI, MSCI Asia (standard, large), MSCI Europe (standard, large), FTSE World index, and
Dow Jones US total market index were also used for the market portfolio. Mckenzie et al. (2000) reported that the
domestic index generates considerably higher risk estimates than using world index for market risk of the Australian
industry portfolio. For US industry portfolio, US domestic index generates lower risk estimates compared to the
world index. Results are available upon requests. 8 As of May 27, 2010 the MSCI ACWI consisted of 45 country indices comprising 24 developed and 21 emerging
market country indices. The developed market country indices included are: Australia, Austria, Belgium, Canada,
Denmark, Finland, France, Germany, Greece, Hong Kong, Ireland, Israel, Italy, Japan, Netherlands, New Zealand,
Norway, Portugal, Singapore, Spain, Sweden, Switzerland, the United Kingdom and the United States. The emerging
market country indices included are: Brazil, Chile, China, Colombia, Czech Republic, Egypt, Hungary, India,
Indonesia, Korea, Malaysia, Mexico, Morocco, Peru, Philippines, Poland, Russia, South Africa, Taiwan, Thailand,
and Turkey. Data of the market capitalization with different sizes (such as large cap, mid cap, standard cap
(large+mid cap), and small cap) are available, among which large cap series are used in this paper.
7
Figure 1. Monthly MSCI ACWI, Dow Jones US and the nominal effective exchange rate (NEER)
For the easiness of presenting the MSCI ACWI and the nominal effective exchange rate of the
U.S. dollar during the sample period, time plots of the monthly level series were drawn in figure
1. The MSCI ACWI was on an increasing trend since the early 1995 to the early 2000. With the
dot-com bubble bust, the index takes a downturn during the year 2000, which lasts until the
beginning of the year 2003. Stock markets in the world continued to rally until the subprime
mortgage crisis hit the financial market with the failure of Lehman brothers and other major
institutions during the year 2008. As of October, 2010, the index recovered its level of before the
crisis. The U.S. dollar, in general, shows an opposite movement to the MSCI ACWI. The
nominal effective exchange rate has been decreasing (i.e. dollar depreciation) between the year
2002 and early 2008, while the exchange rate rose sharply (i.e. dollar appreciation) during the year
2008-9.
The data used for sectoral return series in this paper are Dow Jones U.S. industry indexes of
total return indices for 19 American industry portfolios covering the period from January 3, 1995
to November 4, 2010. Dow Jones Sector Index is classified into Industry Classification
Benchmark (IBC) which contains four classification levels: Industries (10), Supersectors (19),
Sectors (41), and Subsectors (114).9 Among those classification levels, supersectors were adopted
for this paper as is listed in table 1. Supersectors and sector fall on different categories within
ICB classification, however, the term ‗sectors‘ would be used in place of ‗supersectors‘ hereafter
in this paper due to the former‘s familiarity as a general term than the latter. In order to use
excess returns from the total return indices, the riskless rate is approximated by the return
9 Numbers in parenthesis of each classification level stand for how many are included in each level.
0
20
40
60
80
100
120
140
0
200
400
600
800
1000
1200MSCI ACWI
Dow Jones US
NEER
8
(interest rate) on 3-month treasury bills. All the return series are observed at the daily, weekly,
monthly, quarterly and annual intervals. All the indices are expressed in U.S. dollars and are
obtained from Thomson Financial Datatream. All returns are expressed in percentage.
Table 2. Dow Jones U.S. industry index at supersectoral level (Abbreviations)
Industry Supersectors*
Oil & Gas Oil & Gas (Oil)
Basic Materials Basic Resources (Basic)
Chemicals (Chemicals)
Industrials Construction and Materials (Construction)
Industrial Goods & Services (Industrial)
Consumer Goods
Automobiles & Parts (Auto)
Food and Beverages (Food)
Personal and Household Goods (Households)
Health Care Health care (Health)
Consumer Services
Retail (Retail)
Media (Media)
Travel & Leisure (Travel)
Telecommunications Telecommunications (Telecom)
Utilities Utilities (Utilities)
Financials
Banks (Banks)
Insurance (Insurance)
Financial services (Financials)
Technology Technology (Tech.) * Abbreviations are in parenthesis.
The descriptive statistics of the daily, weekly, monthly and quarterly excess returns of each sector
are provided in table 3. In most cases the index of kurtosis and the Bera–Jarque test statistic
reject the hypothesis of normally distributed returns. The two statistics are particularly large for
daily and weekly interval series.
Table 3. Descriptive statistics of sectoral excess returns
Sectors Freq. Mean S.D. Skew. Kurt. J-B
Auto Daily ,021386 1,8606469 ,007 4,725 3687.376
Weekly ,097479 4,1715156 -,055 5,146 929.1259
Monthly ,439826 8,5938580 ,074 4,717 164.9446
Quarterly ,866326 14,9957517 -,172 1,617 5.423960
Yearly 5,327851 39,3190583 ,809 2,088 2.043485
Banks Daily ,036483 2,2351684 ,860 19,057 60493.57
Weekly ,157202 4,6834040 1,282 20,268 14543.96
Monthly ,520055 7,3726742 -,482 2,944 70.89168
Quarterly 1,371427 13,0487204 -,617 1,997 11.82884
Yearly 6,714960 39,3190583 ,809 2,088 0.300256
Basic Daily ,035315 2,0573889 -,277 9,456 14721,55
Weekly .152939 4,2926115 -,084 5,309 936.8892
Monthly ,622797 8,0258151 -,710 3,670 115.0932
Quarterly 1,632124 14,5909365 -,991 1,628 15.02707
9
Yearly 8,413478 33,6814069 ,181 1,815 0.559854
Chemicals Daily ,035198 1,5898460 -,112 5,412 4845.144
Weekly ,160675 3,3460465 -,123 3,117 285.6166
Monthly ,675491 6,3112341 ,214 2,758 57.22735
Quarterly 1,696295 11,2361662 -,562 1,404 6.941371
Yearly 7,340541 24,6457170 -,117 1,690 0.429305
Construction Daily ,027424 1,6127530 -,212 6,807 7683.455
Weekly ,129469 3,6305112 ,403 7,475 1916.049
Monthly ,520286 6,5172710 -,630 3,182 86.87423
Quarterly 1,213704 11,2442696 -,474 ,119 2.248044
Yearly 6,098594 22,3235169 -,951 1,242 1.969733
Financials Daily ,043141 1,9624610 ,484 15,512 39910.94
Weekly ,182605 3,8399159 ,475 7,019 1793.399
Monthly ,708728 6,3967114 -,395 1,643 24.36309
Quarterly 1,885236 11,7500868 -,870 1,699 13.27965
Yearly 12,081843 31,3600523 -,856 1,249 1.625658
Food Daily ,028003 1,0702670 ,091 5,436 4885.745
Weekly ,132029 2,2818371 -,514 4,661 799.2701
Monthly .581009 4,3820049 -,361 1,560 21.58576
Quarterly 1,432205 7,9296440 -,806 ,983 8.232744
Yearly 6,889809 16,8333484 -,573 -,302 0.874527
Health Daily ,034484 1,2362945 -,076 6,248 6451.813
Weekly ,159998 2,5683519 -,460 4,702 864.1315
Monthly ,671579 4,3524742 -,297 ,600 5.171561
Quarterly 1,709998 7,5795903 -,404 ,981 3.356479
Yearly 9,684959 22,6472212 -,039 -,613 0.404636
Households Daily ,031042 1,0864892 -,295 7,251 8741.461
Weekly ,144797 2,3230435 -,736 4,993 1592.968
Monthly ,628182 4,2864407 -,571 1,389 24.00181
Quarterly 1,597263 8,2521312 -,519 ,522 3.085632
Yearly 6,941767 16,1126016 -,722 ,324 1.045023
Industrial Daily ,028130 1,3875476 -,186 5,353 4755.255
Weekly ,128272 2,9539756 -,311 3,889 474.9801
Monthly ,541615 5,4422081 -,628 1,405 26.44462
Quarterly 1,352190 10,2209125 -,480 ,347 2.434452
Yearly 6,513566 22,2700778 -1,035 ,756 2.169904
Insurance Daily ,028446 1,6901163 ,358 14,289 33817.96
Weekly ,121482 3,4133397 -,225 8,708 2734.399
Monthly ,487041 6,1161958 -,408 4,069 127.5209
Quarterly 1,095754 10,1202024 -,380 ,929 2.975087
Yearly 6,122713 24,0619066 -1,042 1,684 2.583865
Media Daily ,025279 1,5419636 ,012 7,597 9533.826
Weekly ,112495 3,1763139 -,338 5,584 1069.442
Monthly ,478423 6,0295132 -,767 2,082 49.86374
Quarterly 1,118258 11,3852314 -,216 1,380 4.119966
Yearly 7,282198 32,7961161 -,160 -1,168 0.934235
Retail Daily ,032420 1,4112105 ,026 4,558 3431.126
Weekly -,037 3,036 -,126 2,936 260.7884
Monthly ,621736 5,4054400 -,202 ,528 3.117013
Quarterly 1,576929 10,1112659 ,590 1,437 7.469588
Yearly 8,541496 26,5715368 ,126 ,254 0.056677
Oil Daily ,049883 1,7062396 -,001 10,808 19298.69
Weekly ,221088 2,3230435 -,807 6,449 914.2290
Monthly ,925925 6,1129610 -,225 1,602 20.08544
Quarterly 2,263968 9,0428151 -1,118 2,034 20.83804
Yearly 11,970384 21,8166491 -1,394 1,453 4.165648
Technology Daily ,044971 2,0405885 ,298 4,271 3071.223
Weekly ,201687 4,2161373 -,308 2,504 65.40886
10
Monthly ,897492 8,7629716 -,185 ,268 1.478472
Quarterly 2,474971 16,0241481 -,451 ,536 2.454630
Yearly 13,840117 42,2096179 ,043 -1,089 0.807098
Telecom Daily ,014685 1,5389709 ,305 7,291 8842.458
Weekly ,057084 4,2161373 -,088 4,290 634.3648
Monthly ,267545 6,3531483 -,161 1,358 14.00879
Quarterly ,524785 11,6782233 ,186 ,446 0.612541
Yearly 3,897197 28,4623434 -,368 -,662 0.710200
Travel Daily ,037230 1,4059328 -,042 3,826 2418.281
Weekly ,133937 2,9202825 -,181 1,735 109.8778
Monthly ,671681 5,8021607 -,427 1,154 15.13145
Quarterly 1,621095 10,6540234 -,265 -,157 0.575271
Yearly 6,571538 22,5330050 -,265 -,004 0.230961
Utilities Daily ,024976 1,1829485 ,181 11,068 20260.15
Weekly ,115302 2,4663454 -1,042 7,621 2089.972
Monthly ,511844 4,8715467 -,734 2,104 49.00493
Quarterly 1,230856 8,7872784 ,040 1,897 7.216619
Yearly 7,238245 23,8734188 -,435 -,331 0.609167
MSCI World Daily ,017655 1,0491412 ,017 11,884 22347,51
Weekly ,083639 2,4323846 -,774 7,843 2205.217
Monthly ,526924 4,7542560 -,758 1,652 37.58005
Quarterly 1,275129 8,7799404 -,710 1,195 7.711073
Yearly 5,373939 23,0003383 -,878 ,305 1.568316
3.2 Empirical model and methodology
The market and exchange rate risk are included in the two-factor model specification with time
varying betas in the following form10
(1)
where is the return on industry i, is the risk-free rate, is the return on the market
portfolio, and is a rate of change in the nominal effective exchange rate of the U.S. dollar.11
Eq. (1) is referred to as signal or observation equation. The state equations are:
The observation error and the state equation errors, and , are assumed to be Gaussian and are taken to be serially uncorrelated. The Kalman filter is an algorithm employed to estimate equation (1) is an optimum recursive estimation method for the signal. Throughout this recursive
10 An intercept term is not included in the specification eq. (1) due to the fact that a singular variance-covariance
matrix is generated with a time-varying constant term in eq. (1). Including a none-time-varying constant term turned
out not to be significantly different from zero. 11 The theoretical formation of both CAPM and APT model is based on expectations or ex ante form. To empirically
tests the models, expectations are transformed into a form that uses observed data by assuming that the rate of
return on any asset is a fair game ― i.e. realized return on any asset is equal to the expected rate of return (Copeland
et al., 2003).
11
estimation algorithm, a new estimate is obtained by adding a correction term to the previous estimate, where the new information has a weight on 1/T. This process consists of two steps, prediction and updates, which calculates the parameters of the distributions.
A problem in estimating eq. (1) arose from diagnostic checking which shows that the market
return and exchange movements were correlated.12 Following the approach of Elton and Gruber
(1991), a side regression of the rate of changes in exchange rate on the market return were run to
orthogonalize the exchange risk factor, i.e. residuals of the side regression were used as an
orthogonalized exchange risk factor. Instead of including a size factor, a two-factor model is
used in this paper because the market returns from MSCI covers large capitalization only.
Including a size factor along with an index of large capitalization would not allow a meaningful
size effect to be captured (Banz, 1981; Heston, Rouwenhorst and Wessels, 1995; Fama and
French, 1998).
Tests for unit root were performed for all the series using Augmented Dickey Fuller test,
indicating all the series are stationary process. The coefficients estimates of the ordinary least
squares of the eq.(1) were given as initial values of the state equations. CUSUM tests were
performed for the recursive residuals in the observation equation of all sectors at all the
frequencies of data observation. Daily and weekly series indicate instability of betas, while the
recursive residuals of the monthly, quarterly and yearly series tend to fail to exceed the 5%
bound of significance, indicating beta stability.
and are called beta, factor loading or sensitivity within a factor-model framework.
measures sensitivity of the sector i to the market. This market beta is the covariance between
returns on a risky asset divided by the variance of the market portfolio―an asset covaries with
the economy―which quantifies risk of the asset. is interpreted as exchange rate exposure. 13
It reflects the change in returns, which can be explained by exchange rates movements after
conditioning on the market return. Exchange rate exposure in this context is marginal since each
sector‘s exposure is measure relative to the market average (Dominguez and Tesar, 2006). The
betas for the market and foreign exchange rate risks presented in figures and tables in the
following section is based on Kalman smoothing. The Kalman smoother calculates recursively
the state posterior distributions for the linear filtering model, eq. (1). The posterior distribution
calculated by Kalman filter is different from that of the Kalman smoother in the sense that the
former are conditional only to the measurements obtained before and at the time step, k, while
the latter are conditioned to all the measurement data.
12 The pearson correlation coefficients between the market factor and the exchange risk factor during the sample
period are -0,198, -0,246, -0,420 -0,341 ,and -0,503 for daily, weekly, monthly, quarterly and yearly frequencies of the
data observation, respectively. All are statistically significant at 0.05 level. Estimations were done with both with and
without orthogonalization. The results were similar. 13 Exchange rate exposure is defined following the literature defining exchange rate exposure as a statistically
significant (ex post) relationship between excess returns at the firm-or industry- level and foreign exchange returns
(Dominguez and Tesar, 2006).
12
4. Empirical findings 4.1. Time-varying risks with industry comparisons 4.1.1 Market sensitivity
Market systematic (sensitivity) risk measures how each industry covaries with the economy, the higher the sensitivity to the market, the more sensitive the industry is to the market. Figure 2 presents plots of the time-varying market risk series by using daily return series during the sample period. Due to limitation of space, the time plots of the figures are presented at the industry level which includes relevant sectors. Bank and technology are the two sectors with wider ranges of the market sensitivities over the sample period compared to those of other sectors. The market sensitivities of all the three sectors within financial industry (banks, financials services, and insurance) soared during the house bubble and credit crisis when the market sensitivities top 4.52 (bank), 2.56 (financial services), and 1.96 (insurance), respectively. The market sensitivity of technology sector also increased during this crisis period, however, drastic changes of market sensitivity of technology sector are observed during dot-com bubble bust when it rose up to 3.67. A quite similar pattern of a change in market sensitivity is also detected in telecom industry during the dot-com bubble bust.
At the onset of the credit crisis, market sensitivities of the basic resources (2,25), construction
and material (1.79) and auto (2.02) sectors surged, whereas the movements of the market
sensitivities for all the other sectors, which are not mentioned so far, are not noticeable under
the times of crisis. Among the three crisis periods, market sensitivities of the US sectoral returns
were not as responsive in the Asian financial crisis as the other two crisis periods.
The inspection of the time-varying sensitivities of the sectoral returns the market shows that the
time-varying beta of sectors generally rise due to the financial crisis. Such time-varying market
sensitivities may be affected by both microeconomic and macroeconomic factors (Bos and
Newbold, 1984). During those three crisis periods―financial crisis, dot-com bubble bust, and
housing bubble and credit crisis―increases in volatility of the financial markets and capital flows
around the world were observed (Chen and So, 2002; Ofek and Richarson, 2003; Gotham, 2009).
A rise in the stock market volatility, therefore, make investors perceive it as an increase in risk of
equity investment (Choudhry, 2005). However, the effects of the crisis on the market sensitivities
of industries are different, i.e. the larger the market risk of an industry, the more it greater the
exposure to the source of risk, which is what is exactly observable in figure 2.
4.1.2 Exchange rate exposure
Since the trade-weighted nominal effective exchange rate is constructed as foreign currencies per
dollar, a negative exchange risk sensitivity implies that an unexpected appreciation of the U.S.
dollar makes the U.S. industries worse off relative to the market. The point estimates of the
foreign exchange risk using daily return series, however, are staying positive for almost all the
sectors during the whole sample period as shown in figure 3. This means that for most of the US
industries, US dollar appreciation improves daily returns. One thing also to note from figure 3 is
the movement of the exchange risk beta during the period of US dollar depreciation (from the
year 2002 to the end of the year 2007). During this time period, the exchange risks are on the
13
rise, which is clearly noticeable for the oil, consumer goods (auto, food, household goods),
consumer services (retail, media, travel), telecom, and financial (banks, insurance, financial
services) industries. Exchange risks of these industries took a downturn at the start of the US
dollar appreciation from the year 2008.
Taken as a whole, the exchange risks are larger for the sectors such as construction, auto, travel,
telecom, bank and technology sectors which involve more international activity compared to the
other sectors. The determinants of the varying exchange rate exposure, however, is not clear to
identify because the co-movements of exchange rates and excess returns incorporate the effects
of any hedging activities taken by firms (Dominguez and Tesar, 2006). The finding from the
figure 3 would suggest that the firms belong to each industries or sectors dynamically adjust their
behavior to exchange rate risks over time.
4.2 Econometric Issues The fact that betas are estimated with a Kalman filter raises three methodological issues,
which are not present in standard time-series empirical tests of the asset price models. One
concern is that the prediction residuals in the Equation (1) were found to have autocorrelation
and conditional heteroskedasticity. This is not unexpected since market returns tend to go
through periods of volatility leading to heteroscedasticity, and randomness in the explanatory
variables in combination with randomness in their coefficients can lead to autocorrelation in the
residuals even if the assumptions of the model are true [needs further verification]. A second
concern is that estimation of equation (1) with an additional time-varying constant results in a
singular variance-covariance matrix. In order to check whether the time-varying beta over the
sample period is a statistical artifact generated by the specification of the model, ordinary least
squares estimator for four different subperiods―Asian financial crisis (Jul.1997-Dec.1999), dot-
com bubble bust (Jan.2000-Dec.2001), inter-crisis period (Jan. 2003-Dec.2006), and housing
bubble and credit crisis (Jul. 2007-Jun.2009)―were used.. The point estimates from these
additional regressions indicate patterns broadly similar to the ones presented above using the
Kalman Filter, albeit in a blunt step-function manner with four steps. A third issue is that
confidence intervals for point estimates, which are valid in case of OLS estimates, cannot be
applied.[ Extend this section]
14
Figure 2. The time-varying market risk for industries (using daily interval returns).
15
Figure 3. The time-varying foreign exchange risk for industries (using daily interval returns)
16
4.3. Time horizons and sensitivities
Market risks (sensitivities) using Kalman filter with different return intervals are presented in
table 4. There is a general tendency of a market risk decline, judging from the medians of all the
time-varying risks, as the return intervals gets larger. There are some exceptions to the general
tendency (for example, the market risk of the media sector for the yearly interval series is larger
than that for the daily). As a whole, however, it is observable that the market risks shrink over
longer time-horizons.
Table 4. Market risk (sensitivities) using Kalman filter with different return intervals
Sectors Daily median
(High/Low) Weekly median
(High/Low) Monthly median
(High/Low) Quarterly median
(High/Low) Yearly median (High/Low)
Oil 0,941877 (1,701538/-0,07924)
0,879271 (1,461538/0,128835)
0,772712 (0,927033/0,580222)
0.640030 (0.832501/0.373368)
0.709022 (0.794777/ 0.648436)
Chemicals 1,095583 (1,546959/0,282551)
0,979974 (1,25026/0,68581)
0,824203 (1,232064/0,519125 )
0.830427 (1.115398/ 0.747824)
0.659328 ( 1.341539/0.399531)
Basic 1,126876 (2,252905/0,099949)
1,121088 (1,732528/0,66244)
1,212561 (1,677944/0,382758 )
1.097863 ( 1.340188/0.876047)
0.975993 (1.927711/0.323441)
Construction 1,06392 (1,796565/0,206542)
0,990323 (1,608159/0,417845)
0,989904 ( 1,37242/0,345977)
1.023057 ( 1.423526/0.361682)
1.049196 (2.109813/-0.725244)
Industrial 1,112129 (1,720969/0,384358 )
1,106897 (1,373876/0,63736)
0,983205 (1,000455/0,973045)
1.041460a 0.980697 (2.422790/0.216774)
Auto 1,137936 (2,02954/0,299071 )
1,185925 (1,894686/0,487387)
1,003554 (1,712592/0,651976 )
1.240272 (1.795683/ 0.820447)
1.053556 (2.038295/0.794094)
Food 0,583771 (1,455414/-0,25517 )
0,529264 (1,307315/-0,29061)
0,523121 ( 0,92225/-0,45088)
0.538528 ( 0.706083/0.280216)
0.451469 (3.199617/-1.037888)
Households 0,737398 (1,245407/0,232621)
0,68603 (0,903825/0,368147)
0,695798 (0,894051/0,076743)
0.660452a 0.595870 (2.837570/-0.580889)
Health 0,841336 (1,65096/0,074355 )
0,705951 (1,334419/-0,03624)
0,614205 (0,696156/0,233771)
0.505123 (0.534356/ 0.487373)
0.375884 (0.526186/0.375884)
Retail 0,97933 (1,015893/0,270598 )
0,904728 (1,320605/0,675794)
0,794209
0.822655 ( 1.304934/ 0.602688)
0.970380 (1.281005/0.731490)
Media 1,068827 (1,558115/0,289924 )
0,917319 (1,381074/0,313267)
0,987042 (1,121026/0,641382 )
1.074015a 1.255822 (1.319284/1.186723)
Travel 0,961985 (1,587345/0,326064)
0,942366 (1,268553/0,361962)
0,867056 ( 1,006543/0,491919)
0.858547
0.934302 ( 1.777917/-0.056074)
Telecom 0,921731 (1,716674/0,399317)
0,837209 (1,323844/0,443838)
0,768064 (1,586352/0,239985 )
0.847520 (0.903721/0.658189)
1.034644 (1.414146/ 0.684696)
Utilities 0,6087 (1,323949/-0,12821)
0,630293 (0,832292/-0,02845)
0,553094 (1,146329/-0,30285)
0.613965 (0.964144/-0.113835)
0.948809 (1.596269/-1.744177)
Banks 1,088966 (4,524682/0,176108)
0,9823 (3,646238/0,381098)
0,780874 (1,918307/-0,1321 )
0.653843 (1.122145/0.457596)
0.598857 (2.960831/-0.424662)
Insurance 1,007155 (1,908474/0,460005 )
0,991047 (1,624234/-0,00339)
0,883563 ( 1,423523/-0,24117)
0.788055
0.562416 (2.945138/-1.390253)
Financials 1,263331 (2,561842/0,549397)
1,18116 (1,836656/0,889041)
1,050091 (1,23045/0,78799 )
1.015944 (1.335889/0.621709)
Tech. 1,419746 (3,670405/0,438647 )
1,267035 (1,993415/0,860204)
1,335441 (1,834191/1,020775 )
1.333361 (1.844434/1.092687)
aOLS estimates based on the specification of the eq.(1), but without state-space modeling.
Exchange rate risks show similar patterns to those of the market risks over different time
horizons. Two things are noticeable in table 5. First, the exchange rate risks at daily intervals are
all positive across sectors. It means that a US dollar appreciation is associated with an increase in
returns, which is counter to the general notion of losing competitiveness for exports caused by a
strong domestic currency, which would negatively affect returns. However the findings are
consistent with the notion that high US returns will induce a greater capital inflow into the US
17
stock market and thereby cause an appreciation of the US dollar. Second the exchange rate risks
appear to be declining with longer time horizons, in some cases resulting ultimately in a negative
relationship between the US dollar and the industry returns. This is consistent with the idea that
the effect of a US dollar appreciation on competitiveness of US exports becomes stronger with
the larger time horizons.
Our finding in the empirical section in general stand in contrast to the results of the previous
studies which examined the size of the beta at different time horizons. The market and foreign
exchange risks tend to decrease at longer time-horizons.
Table 5. Exchange risk (sensitivities) using Kalman filter with different return intervals
Sectors Daily median.
(High/Low) Weekly median.
(High/Low) Monthly median.
(High/Low) Quarterly median
(High/Low) yearly median (High/Low)
Oil 0,191006 (0,529834/-0,00028 )
-0,10928
-0,06757
0.208675 0.434271
Chemicals 0,405647 (0,729224/0,093259)
0,250109
0,045821
-0.129417 -0.299066
Basic 0,105488 (0,717302/-0,31422 )
-0,14071
-0,39912
-0.329838 -0.325546
Construction 0,377523
(0,851141/0,269514) 0,358929
(1,035824/0,044063)
0,088842 (0,828277/-
0,40256)
-0.196349 -0.225854
Industrial 0,484523 (1,089218/0,325583 )
0,491009 (0,58254/0,473923)
0,261427
0.194570a -0.051033
Auto 0,500831 (1,144882/0,330579)
0,662274
0,588254
0.655536 -0.296557
Food 0,281376
(0,737532/-0,15302) 0,306047
(1,441769/-1,01306 )
-0,14538 (0,633996/-
0,73964)
-0.092111 0.162290
Households 0,449817 (0,903593/0,055023)
0,422827 (0,849092/0,15468)
0,088621
-0.011217a 0.014412
Health 0,457656 (0,818755/-0,10098)
0,369703 (1,193302/-0,37529 )
0,26461
0.276072 0.162290
Retail 0,510489 (1,015893/0,409744)
0,629242 (0,921122/0,515055 )
0,512928
0.627618 0.557557
Media 0,413571 (1,222223/0,199701)
0,386356 (1,108885/0,068936)
0,383287
0.592566a 0.999701
Travel 0,499242 (1,333853/0,243698 )
0,511204 (1,046427/0,238567)
0,239398
0.089999 -0.111578
Telecom 0,407672 (0,920785/-0,00246
0,388399 (0,573157/0,238893 )
0,407081
0.046713 0.275630
Utilities 0,206825 (1,08254/-0,82761 )
0,182687 (0,303675/0,001633)
-0,01965
-0.027937 0.277119
Banks 0,48536
(3,112313/-0,03748) 0,631582
(1,512973/0,18665 )
0,083652 (0,565539/-
0,24471)
0.350113 0.843399
Insurance 0,501781 (1,704297/0,14476)
0,588202
0,264304
0.397000 1.122979
Financials 0,675933 (2,343678/0,037962 )
0,87672 (1,338372/0,206309)
0,475833
0.742483
Tech. 0,683265
(1,525932/0,163008) 0,49531
0,741378
0.705538 (0.927482/-
.062683)
OLS estimates based on the specification of the eq.(1), but without state-space modeling.
18
Figure 4. The time-varying market risk for industries (Monthly)
19
Figure 5. The time-varying foreign exchange risk for industries (Monthly)
20
5. Conclusion
In this paper, an approach to estimate the time varying risks, or sensitivities (beta), of US industry portfolio was adopted. The method is based on an recursive algorithm known as Kalman filter in state space models.
As a whole, however, it is observable that the market risks shrink over longer time-horizons. However the findings are consistent with the notion that high US returns will induce a
greater capital inflow into the US stock market and thereby cause an appreciation of the US
dollar. Second the exchange rate risks appear to be declining with longer time horizons, in some
cases resulting ultimately in a negative relationship between the US dollar and the industry
returns. This is consistent with the idea that the effect of a US dollar appreciation on
competitiveness of US exports becomes stronger with the larger time horizons.
Our finding in the empirical section in general stand in contrast to the results of the previous
studies which examined the size of the beta at different time horizons. The market and foreign
exchange risks tend to decrease at longer time-horizons.
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