hedonic prices of sulfur in coal under the u.s. so ... · hedonic prices of sulfur in coal under...
TRANSCRIPT
Hedonic Prices of Sulfur in Coal under the
U.S. SO2 Allowance Market
Toshi H. Arimura ∗
Sophia University
May 12, 2002
JEL Classification: Q2,Q28,Q41.
Key Words: Emissions; Marketable Permits, Hedonic Analysis, Coal Market
Abstract
This study investigates the efficiency of pollution permit markets by con-
ducting an empirical study of the U.S. SO2 market. A hedonic model of coal
price is estimated by using the coal price data from 1985 to 1998. The esti-
mation results showed that the sulfur premium was in the same order as the
SO2 allowance prices in the EPA auction. In addition, for 1997 and 1998, the
SO2 allowance prices were in 95% confidence intervals for a relevant range of
sulfur content levels. In 1995, however, the deviation of the SO2 allowance
price from the sulfur premium was found. This deviation may have been
caused by the market power of the coal mine companies in Montana and
Wyoming.
∗I am grateful to Professors Edward Foster and John Geweke for their advice. I wouldalso like to thank Professors Jay Coggins, Steve Polasky and Frances Homans for helpfulcomments. This research has been supported by the Japan Economic Research Foundationand Asahi Glass Foundation. Address: Department of Economics, Sophia University, 7-1Kioi-cho, Chiyoda-ku, Tokyo, 102-8554 Japan. E-mail: [email protected]
1
1 The Link between Coal Market and the
SO2 Allowance Market
The SO2 allowance market is a pollution permit market that the 1990 Clean
Air Act Amendments created to control sulfur dioxide (SO2) emissions from
electric utilities in the United States. There has been concern, however, that
the SO2 allowance market may not be reflecting the true marginal abatement
cost. There are a few reasons for this concern. First, the unexpected low
allowance price is considered to be evidence of a failure of the market. The
allowance price was expected to be around $500 before it started. But the
price dropped to about $ 60 in 1996. Second, Public Utility Commission
(PUC) regulation has been superimposed on the SO2 emission regulation. In
the literature, some analysts argue that this distorts decisions by power plant
managers and, hence, the SO2 market. Third, there is concern about the
auction mechanism run by the Environmental Protection Agency. Cason [5]
has shown that in theory the auction distorts bidders’ incentives; as a result,
the market price of the allowance will not be the true marginal abatement
cost.
In response to these concerns, Joskow et al. [9] studied the allowance
market and claimed that it is efficient. Coggins and Swinton [6], on the
other hand, estimated the marginal abatement cost at power plants in Wis-
consin and found that they are considerably higher than market prices for
allowances. These studies, however, do not directly answer the question of
the efficiency of the nation-wide SO2 allowance market.
Joskow et al. [9] showed that the market has developed well in a short
period by examining the transaction data of SO2 allowances. First, they com-
pared the allowance price from the EPA auction with the prices associated
with private confidential trades, reported from two brokers. The finding is
that those prices were almost identical by late 1994. Second, they examined
the EPA auction and found that almost none of privately offered allowances
were sold in the auctions in 1993 and 1994. In the auction, allowances from
the EPA’s special account are sold first. If there is more demand, privately
provided allowances are sold. In 1993 and 1994, however, very few privately
provided allowances were sold. Thus, the seller side auction bias played no
role in determining the allowance price. They also found that, as time goes
2
by, peculiar bidding prices have been disappearing, i.e., most bids have be-
come closer to the market prices. Finally, Joskow et al. investigated quantity
of the allowance trades and found that the quantity of allowance trades in
the EPA Auction has become a smaller part of the total private transactions.
For example, from April 1996 to March 1997, only 5.5 % of private allowance
trades took place in the auction. This fact implies that most allowance trans-
actions took place outside the EPA and that the number of transaction has
been increasing rapidly. From these observations, they concluded that the
allowance market “had become reasonably efficient.”
Coggins and Swinton [6] proposed an output distance function approach
to investigate the marginal abatement cost of SO2 emission at the plant level
in Wisconsin. On average, their estimate for the marginal abatement cost
was about $292.70 per ton of SO2 in constant 1992 dollars. Since the average
allowance price in the 1993 EPA auction was $156.00 per ton their results
showed a divergence between the allowance price and the marginal abatement
cost. They argued that the difference can be attributed to the stringent local
SO2 emission regulations in Wisconsin.
Other studies also found problems in the allowance market. Carlson et
al.[4] revealed that most trading gains were unrealized in the first two years of
the acid rain program. Arimura [1] investigated electric utility behavior under
the SO2 allowance market in Phase I. The study found that cost recovery
rules promoted high sulfur coal usage for utilities located in states with coal
mines. A comprehensive study of the SO2 allowance market by Ellerman et
al. [8] also pointed out imperfections of the allowance market. Swinton [10]
found that power plants in Florida can save abatement cost by participating
in the national market for allowances.
While these studies give useful information on how the SO2 allowance
market has been working, they do not answer the question of the SO2 al-
lowance market efficiency in view of economic theory. The efficiency of a
pollution permit market is determined by whether or not the marginal abate-
ment costs of polluters are equal to the price of a permit. This is the exact
reason why pollution permit markets are preferred to direct regulations. The
study of the SO2 allowance market by Joskow et al., however, did not ex-
amine whether allowance prices reflect the marginal abatement cost of SO2
emission. In order to estimate the marginal abatement cost, one should study
3
electric power utilities’s behavior such as fuel choices. What Joskow et al.
examined was the SO2 allowance transaction data, not utilities’ fuel choices
or investment in pollution abatement technology. While their study answered
many concerns about the allowance market, it did not reveal the relationship
between marginal abatement cost and the allowance price.
In contrast to Joskow et al., Coggins and Swinton [6] estimated the
marginal abatement cost at the power plant level. Their sample was, however,
taken only from Wisconsin while the allowance market is a nation-wide sys-
tem. Moreover, the sample covers only the years from 1990 to 1992, which
was three years before power utilities had to comply with the regulation.
Swinton [10] calculated the shadow price of emission reductions for power
plants using newer data set. However, the data is taken only from Florida.
Further, the output distance function approach in these studies does not have
a statistical theory as a basis. Thus, one cannot formally test to see if the
estimated marginal abatement costs are different from the allowance price.
No studies have directly investigated the link of the marginal abatement
cost and the allowance price. In the context of the SO2 allowance market,
electric utilities face choices between using SO2 allowances and using coal
with less sulfur content. If the sulfur content is smaller, the SO2 emission
is smaller; therefore, they can save the cost of the SO2 allowance. Thus,
theoretically, the sulfur premium should be reflected in the SO2 allowance
market. Thus, one solution to this question is to investigate the coal market
by examining sulfur premiums in coal prices. In this paper, the sulfur pre-
mium is defined as an additional cost that power plant managers have to pay
in order to purchase coal with less sulfur content. By statistically analyzing
this premium from a coal transaction data set, one can investigate whether
or not the SO2 allowance market reflects the true marginal abatement cost.
2 Data
All the transactions of fossil fuels at power plants are reported to the Energy
Information Administration (EIA) and are kept as EIA423. I have obtained
the data for the period of 1985-1998 from EIA. The data contain coal prices,
sulfur content, ash content, heat content (mmBtu), quantity, month, year
and plant code.
4
The EIA423 data set includes contract type for each purchase as well.
Table 1 compares the number of spot purchases and total purchases in the
years of 1985 and 1995. How coal prices are determined in contract is a
dynamic decision. Therefore, the econometric study below focuses on coal
prices in the spot market.
Table 1: Number of Transactions by Contract Type
Number of Coal Transaction in Each Year
Contract Type 1985 1995
Spot Purchase 7773 7970
Total Purchase 19605 20222
The EIA423 contains coal type that has five categories: bituminous, sub-
bituminous, anthracite, lignite and bitumen. Table 2 reports the number
of purchases for each coal type in 1985 and 1995. Bituminous and sub-
bituminous accounts for 95 % of coal purchase in both years. Sub-bituminous
coal purchases have almost doubled in ten years while purchases of bitumi-
nous coal decreased. This is consistent with the literature ([3] and [7]).
Table 2: Number of Transactions by Coal Type
Both
(Spot & Contract) Spot
Coal Type 1985 1995 1985 1995
Bituminous 17733 16798 7166 6646
Sub-Bituminous 1416 2827 170 770
Lignite Coal 223 272 1 0
Anthracite Coal 176 86 101 34
5
3 Model
3.1 Theoretical Model
This study focuses on spot purchases since contract purchase is a complex
dynamic decision. Given capacity sizes, plant managers face K types of coal
and choose coal purchase qk, measured in heat, for each type (k = 1, ·, K).
Sulfur content for each type of coal is denoted by sk. The SO2 emission from
the plant at time t is given as:
Et ≡ cK∑
k=1
skqk (1)
where c is a conversion unit from sulfur to sulfur dioxides.
Each coal type differs in other characteristics such as weight per heat
(wk) or ash content (ak). In this section, Xk is used to refer to k type coal
characteristics where Xk = ak, wh, ... Coal type is also included in Xk. Thus,
the production technology is assumed as follows:
y = f(∑
qk,∑
qkXk) (2)
where y is an exogenously given output level. According to an EPA report
[11], the production technology is not a function of sulfur content. Thus, it
is assumed that sulfur content does not enter the production function as an
element while the sulfur content affects SO2 emissions.
Let pkt and pa
t denote the price of coal type k and the allowance price at
time t, respectively. Then, the plant manager’s problem is to choose quantity
of coal purchase for each level of sulfur, q(s), such that
minqkk
K∑
k=1
pkt q
k + pat Et (3)
subject to (2).
Plugging (1) into (3), the problem is equivalent to the following:
minqkk
K∑
k=1
pkqk + pat
K∑k=1
skqk (4)
6
subject to (2).
Claim: Coal price pk is a linear function of sulfur content under the SO2
allowance market.
Proof: The Lagrangian for the cost minimization problem is given as:
L = K∑
k=1
pkqk + pat
K∑k=1
skqk
+λy − f(∑
qk,∑
qkXk). (5)
Thus, the first order condition for a purchase coal qk > 0 is
∂L/∂qk = pk + pat s
k − λf1 +∑
1,·,Mfm+1(
∑qk,
∑qkXk)Xk
m = 0. (6)
where fm is the first derivative of the production function with respect to
element no. m. Thus, if coal type k is purchased, the price in an equilibrium
is given as follows:
pk = −pat s
k + λf1 +∑
1,·,Mfm+1(
∑qk,
∑qkXk)Xk
m. (7)
This proves that the coal price is linear in sulfur content under the SO2
allowance market.
To understand the model, let us look at Figure 6, which shows relation-
ships between coal prices and sulfur contents of coal purchase for two different
plants. The manager of plant A faces various coal prices denoted by ‘∗’ and‘x’. Among all the possibility, the manager is willing to purchase the lowest
price coal including SO2 emission cost. The slope of solid line is given by the
allowance price. Consequently, the manager chooses to purchase the coal on
the plain line, which is denoted by ‘∗’.If the plant is in a different location, the manger faces different potential
coal prices as shown in the Figure as Plant B. In this case, Plant B is
located more distant from coal mines. This is captured by the intercepts,
which are different across plants. As a result, the managers pays more for
coal. However, the sulfur premium given by the slope of the brake line should
7
be the same with Plant A because the allowance price is the same for both
managers. The price of purchased coal are denoted by ‘o’; the un-purchased
coal is given by ‘.’.
The model assumes that plant managers are price takers and they have
no influence on coal prices. This point may need to be taken care of when
estimation results are discussed.
3.2 Econometric Model
The following model is examined:
Pitj = β1 +1998∑
year=1985
θ1,yearsijt + θ2,year(sitj)2 + θ3,year(sitj)
3Dyear,ijt
+β2aitj + Σβcoaltype3 Dcoaltype
itj + β4BTUitj + uitj (8)
where i, t and j denote plant, time (month) and j th purchase of coal at
plant i at time t, respectively. Dummy variable Dyear,ijt is used to capture
sulfur premium year by year. Price of j th coal at plant i and at time t (cents
per mmBtus) is Pitj . Sulfur content, sitj, and ash content, aitj, are measured
in pounds per mmBtu. BTUitj captures heat content measured in btu per
pound.
Dummy variables for each coal type are Dcoaltypeitj where there are five
categories as stated in the preceding section: bituminous, sub-bituminous,
lignite, anthracite and bitumen. Parameters to be estimated are θm,yearyaer
(m=1,2,3) and β. The term uitj is to capture unobservable part of the cost
structure.
The coefficient of sulfur content, θ1,year, is expected to be negative if the
sulfur premium is captured by coal prices. Once the allowance market started
(year ≥ 1995), the size of θ1,year should be equal to the allowance price for
each year. Moreover, if the model in the previous section holds, it must hold
that θ2,year = θ3,year = 0 after the year of 1995.
The coefficient of ash, β2, is expected to be negative since ash requires
some treatment in combustion. The sign of β4 is expected to be positive
since the larger heat content implies less cost per heat for moving the coal in
plant.
8
4 Specifications
4.1 Tests for the Specifications
In order to implement statistical tests on estimated parameters, the variance
covariance structure of error terms in (8) must be correctly specified. Several
specification tests are conducted to capture error structures. However, im-
plementing these tests are difficult for unbalanced data sets. Therefore, using
the original data set, a balanced panel data set is constructed by selecting
observations of plants that have coal purchase information for all the months
in 1995. Thus,
pit = Xitβ + uit (9)
where i = 1, ..., N and t = 1, ...., T . For the balanced data set, N = 92 and
T = 12. The regressors are
Xit = 1, sit, s2it, s
3it, ait, D
SUBit , BTUit. (10)
First, it is tested whether there is an individual effect at the plant. Thus,
the following error structure is examined:
uit = µi + νit (11)
where µi and νit are normally distributed with variance σ2µ and σ2
ν respec-
tively. The test is conducted to examine
Ho : σµ = 0
versus
Ha : σµ = 0.
Breush and Pagan [2] showed that the Lagrangian Multiplier statistics for
the test is given by:
LM =NT
2(T − 1)[u′(IN
⊗eTe
′T )u
u′u− 1]2 (12)
where the statistic is distributed as χ2(1) under the null hypothesis.
Using the balanced panel data set, the test statistic is found to be 10.928.
Thus, the null hypothesis is rejected at the 1.0 % level.
9
Next, the Hausman test is conducted to examine orthogonality of the
random effects. Namely, the hypothesis are:
Ho : E[µi|X] = 0
versus
Ha : E[µi|X] = 0.
Under the null, the test statistic is distributed as χ2 with 6 degrees of freedom.
For the panel data set, the statistic is 6.5054. The null hypothesis is not
rejected at the 1 % significance level. This provides evidence in favor of a
random effect model over a fixed effect model. Therefore, the random effect
model is examined in the following.
Finally, the time component of the error is tested. The following error
structure is considered:
uit = λt + νit (13)
where λt and νit are normally distributed with variance σ2λ and σ2
ν respec-
tively. The test is conducted to examine
Ho : σλ = 0
versus
Ha : σλ = 0.
Breush and Pagan [2] showed that the Lagrangian Multiplier statistics for
the test is given by:
LM =NT
2(N − 1)[u′(eNe′N
⊗IT )u
u′u− 1]2 (14)
where LM is distributed as χ2(1) under the null hypothesis. Since the value
of the test statistic is 554.36, the null hypothesis is rejected at the 1% level.
4.2 Error Specifications
The specification tests above reveals that the model to be examined is given
as follows:
pitj = Xitjβ + uitj (15)
10
where
Xitj = sitj, s2itj, s
3itj, aitj, D
SUBitj , DBIT
itj , BTUitj. (16)
and
uitj = µi + λt + νitj . (17)
Estimating this model by GLS is not straightforward since the original
data is an unbalanced panel. On the other hand, many observations are lost
if the balanced panel is used. One can eliminate individual effect and time
effect by taking the first difference of (15). The first difference equation is
given as follows:
pitj+1 − pitj = Xitj+1β + uitj+1 − Xitjβ + uitj= (Xitj+1 −Xitj)β + νitj+1 − νitj (18)
when the plant identification number and purchased month for itj and
itj + 1 are equal. Under this first difference model, the sample size for
1995 is 5232. Thus, this estimation method provides a much larger sample.
Let us reparametrize the error term of the first difference equation as
εitj = νitj+1 − νitj. Then, E[εε′] = σ2νΩ where the diagonal element of Ω is
2 and where the first off-diagonal element is −1 for each plant in the same
month. The rest of elements of Ω are zero. Even though this is a relatively
simple variance-covariance matrix, the estimation is not straightforward since
the panel data is unbalanced and since the sample size is large.
5 Results and Discussion
5.1 OLS Results with the First Difference Equation
The OLS estimation is conducted using equation (18). The sample consists of
the observations from 1985 to 1998 and the size is 138808. After taking first
differences, the sample size for the estimation is 104707. The OLS estimates
are consistent even though hypothesis testing cannot be conducted without
the correction of the variance covariance matrix. The estimation results are
reported in Table 6 in Appendix. The standard errors are computed using
the correct variance-covariance structure. In a later section, using dummy
11
variables for states of origin of coal is discussed to capture some unobservable
coal characteristics. The regression results for this case are also reported in
the Appendix.
5.2 Sulfur Premium
Once the parameters are estimated in the linear model (8), one can derive
the sulfur premium (−∂Pitj/∂sitj) in the coal market as follows:
SulfurPremium = −θ1,year + 2θ2,year(sitj) + 3θ3,year(sitj)2 (19)
where Pitj is the coal price measured in cents, sitj is the sulfur content mea-
sured in pounds per mmBtu, and θ1,year, θ2,year, θ3,year are the estimated
parameters. Thus, the sulfur premium can be computed as a function of the
sulfur content. If the theory holds, one expects the sulfur premium to be
approximately equal to the SO2 allowance price for all sulfur content levels
once the allowance market started (θ2 = θ3 = 0). On the other hand, before
the allowance market was introduced in 1995, sulfur premiums do not have
to be constant for the whole sulfur content range since plant managers did
not have to hold SO2 allowances.
The 95 percent confidence intervals for the sulfur premium are computed
for each year. The results are shown in Fig. 6, 6, 6 and 6. In order to
investigate the relation between the allowance market and the coal market,
let us examine the allowance price. In the EPA auction, the allowance was
$130 per ton in 1995. With units converted, the price is equivalent to 13
centss per SO2 kg, which is equivalent to about 14 cents per sulfur pound.
The allowance prices from the spot market are shown in the dotted lines for
each year after the allowance market had started. The sulfur premium and
allowance prices are in the same order even though the allowance prices from
the EPA auction are not necessarily in the 95% confidence interval of sulfur
premium. The coal market seems to reflect the allowance price as the sulfur
premium.
Figure 3, 4 and 5 show that positive sulfur premium was found even
before he SO2 allowance market was introduced. This is an expected result
since coal power plants were often subject to various local SO2 regulations.
To deal with local air pollition problems, EPA enforced local governments to
12
take policies toward SO2 emission contorls. In many cases, local regulatory
authourities put some restrictions on coal type usage, meaured by sulfur or
sulfur dioxide per mmBtu. Although these regulations were not as tight
as the acid rain program requirements, this is considered to cause sulfur
premium before the SO2 allowance market.
5.3 Issue of Choice of Regressors
Unobservable coal characteristics such as moisture content or volatility may
affect the efficiency of electricity generation. These characteristics can be
considered to depend on the location of coal mines. There are 16 states
with coal mines in the sample. In order to capture these effects, dummy
variables DMineStateitj t are constructed to refers to each state where the coal
is from. The random effect model is not considered due to complication
from the unbalanced panel.The OLS results with the dummy DMineStateitj
are reported in the Appendix. The estimates do not seem to change to a
great degree in spite of the addition of the dummy variables.
Using these estimates, 95 percent confidence intervals for the sulfur pre-
mium are computed for each year. The results are shown in Appendix (Fig.
6). Fig. 6 presents the 95 % confidence intervals of sulfur premium after the
SO2 regulation of the acid rain program started. The allowance price in EPA
auction for each year is drawn by dot lines. For 1997 and 1998, the allowance
price is in the range of 95% confidence intervals for sulfur premium from 0 to
1 pound per mmBtu. This suggests that the allowance prices in the auction
reflect the sulfur premium of coal for low sulfur coal.
In 1995, the sulfur preimum was higher for lower sulfur coal. Specifically,
the premium was hihger than the allowance price in the EPA auction for
the range of sulfur from 0 to 0.6 pound. This suggests that plant mangers
paid more than necessary high price for the lower sulfur coal within that
range. Most subbituminous coal from the West are in that range. Therefore,
this result may provide evidence that coal mine company in the West took
advantage of the introduction of the SO2 market by exploiting rent from the
higher coal price.
13
5.4 Linear Hypothesis Testing
The cost minimizing model in a previous section implies that sulfur premium
is linear in sulfur content. Wald tests are conducted in order to test this
linear hypotheses (θ2 = θ3 = 0) for each year. Test statistic are computed for
both estimations: 1) regression with Eq. (8) and 2) regression with dummy
variables for states of mine data. The statistics are reported in Table 3.
Under the null hypotheses, the test statistics has a chi-squared distribu-
tion with 2 degrees of freedom. The critical value of the chi-squared distri-
bution is 9.21 at the 1 % significance level. Therefore, the hypotheses are
not rejected for 1998 and 1991 in both estimations. However, the hypothesis
are rejected for other years.
5.5 Discussion
The statistical analysis in the previous subsections showed that the allowance
price did not reflect marginal abatement cost in the first two years. How-
ever, in 1997 and 1998, for lower range of sulfur content, coal price reflected
allowance prices. Further, the linear hypothesis, which is expected to hold
in the market, was accepted in 1998.
These results are consistet with Carlson et al.[4]. They found that the
advantage of pollution-permit market was not realized in the first two years.
The analysis in the previous sections provide evidence from another aspect:
the deviation between sulfur premium in the coal and the allowance price.
However, the analysis above found that the market is becoming efficient
in 1997 and 1998 in the sense that the deviation vanished for lower range
of sulfur coal. This is an supporting evidence that the market “had become
reasonably efficient(Joskow et al.[9]).”
6 Conclusion
In this study, the efficiency of the U.S. SO2 allowance market was examined.
Specifically, hedonic analysis was conducted in order to find the link between
14
Table 3: Wald Test Statistics
Year Without With
Mine Dummies Mine Dummies
1998 3.288 6.757
1997 70.380 88.780
1996 89.125 104.089
1995 161.976 178.690
1994 24.299 25.148
1993 33.237 34.000
1992 47.246 76.168
1991 5.283 8.263
1990 39.753 61.850
1989 91.767 105.706
1988 84.642 96.285
1987 131.793 177.228
1986 55.159 65.476
1985 157.777 182.130
sulfur premium in coal and the allowance price. Though the sulfur premium
was in the same order with the SO2 allowance prices in the EPA auction,
the deviation of the SO2 allowance price from the sulfur premium was found
in 1995. This may have been caused by the market power of the coal mine
companies in Montana and Wyoming.
However, for 1997 and 1998, the SO2 allowance prices were in 95 % confi-
dence intervals for the certain range of the sulfur content level. In addition,
the linear analysis was not rejected in 1998. These results provide another
evidence that the allowance market had become reasonably efficient(Joskow
et al.[9]).”
Sulfur premium was estimated for each year in this study. Since coal
price and allowance price data are available on monthly basis, it is possible
to estimate the sulfur premium month by month and to compare with the
allowance price. Moreover, Phase II regulation of the SO2 allowance market,
which covers more power plants, started in 2000. Therefore, it is desirable
to extend this research by incorporating the new data set of the recent years
15
References
[1] T. H. Arimura. An empirical study of the SO2 allowance market: Ef-
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254, 1980.
[3] D. Burtraw. Cost savings sans allowance trades? Evaluating the SO2
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17
[11] US Energy Information Administration. Acid Rain Compliance Strate-
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18
Appendix
Table 4: Descriptive Statistics for Fuel 1985 Coal Spot Purchase
Variables Means Std.Dev. Max Min
Price 142.1035 29.5968 399.000 21.900
D10 0.0922 0.2893 1.000 0.000
D11 0.0914 0.2882 1.000 0.000
D12 0.0948 0.2929 1.000 0.000
Sulfur 1.3880 0.8439 6.214 0.017
Sulfur2 2.6387 3.3617 38.614 0.000
Sulfur3 6.3862 12.8713 239.946 0.000
Ash 9.3424 4.9132 62.139 0.142
Surface 0.7155 0.4512 1.000 0.000
BIT 0.9509 0.2160 1.000 0.000
SUB 0.0220 0.1467 1.000 0.000
ANT 0.0210 0.1433 1.000 0.000
LIG 0.0009 0.0300 1.000 0.000
The sample size is 7767
19
Table 5: Descriptive Statistics for Fuel 1995 Coal Spot Purchase
Variables Means Std.Dev. Max Min
Price 118.2756 27.4035 224.100 0.100
Sulfur 1.2216 0.8883 8.411 0.024
Sulfur2 2.2812 3.5984 70.745 0.001
Sulfur3 5.8058 15.6039 595.036 0.000
Ash 9.7844 19.8779 1032.218 0.064
quantity 20065.2593 33661.0046 484000.000 10.000
Surface 0.5909 0.4917 1.000 0.000
BIT 0.8644 0.3424 1.000 0.000
SUB 0.1014 0.3018 1.000 0.000
ANT 0.0108 0.1034 1.000 0.000
The sample size is 7951
0 1 2 3 4 5 650
100
150
200
250
300Coal Prices in Different Plants
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Plant APlant B
Figure 1: Illustration
20
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1998
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)0 0.5 1 1.5 2 2.5
0
5
10
15
20
25 1997
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1996
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Point EstimatesUpper BoundLower BoundAllowance Price
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1995
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Figure 2: Sulfur Premium and 95 Percent Confidence Intervals(1)
21
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1994
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Point EstimatesUpper BoundLower Bound
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1993
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1992
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)0 0.5 1 1.5 2 2.5
0
5
10
15
20
25 1991
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Figure 3: Sulfur Premium and 95 Percent Confidence Intervals (2)
22
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1990
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Point EstimatesUpper BoundLower Bound
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1989
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1988
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)0 0.5 1 1.5 2 2.5
0
5
10
15
20
25 1987
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Figure 4: Sulfur Premium and 95 Percent Confidence Intervals (3)
23
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1986
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Point EstimatesUpper BoundLower Bound
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1985
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Figure 5: Sulfur Premium and 95 Percent Confidence Intervals (4)
24
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1998
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)0 0.5 1 1.5 2 2.5
0
5
10
15
20
25 1997
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1996
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Point EstimatesUpper BoundLower BoundAllowance Price
0 0.5 1 1.5 2 2.50
5
10
15
20
25 1995
Cen
ts p
er S
ulfu
r P
ound
Sulfur (Pounds per mmBtu)
Figure 6: Sulfur Premium and 95 Percent Confidence Intervals (with Mine
Dummies)
25
Table 6: Estimation Results (Base Case)
Variable Estimates Stndard Error T-stat
1 Sulfur (98) -12.587933 2.079761 -6.052587
2 Sulfur2 (98) 1.417530 1.083731 1.308010
3 Sulfur3 (98) -.161802 .165737 -.976256
4 Sulfur (97) -7.477197 1.761134 -4.245671
5 Sulfur2 (97) -2.153476 .848371 -2.538365
6 Sulfur3 (97) .533309 .120507 4.425551
7 Sulfur (96) -11.260122 1.863324 -6.043031
8 Sulfur2 (96) -.699862 .877983 -.797126
9 Sulfur3 (96) .359874 .120473 2.987178
10 Sulfur (95) -20.300269 1.542118 -13.163885
11 Sulfur2 (95) 2.761473 .614573 4.493324
12 Sulfur3 (95) -.057394 .068863 -.833453
13 Sulfur (94) -5.870551 1.199665 -4.893493
14 Sulfur2 (94) -1.977855 .578028 -3.421732
15 Sulfur3 (94) .337382 .079651 4.235780
16 Sulfur (93) -2.182387 1.699797 -1.283910
17 Sulfur2 (93) -3.209560 .836452 -3.837111
18 Sulfur3 (93) .578603 .119549 4.839868
19 Sulfur (92) -23.121464 2.338582 -9.886958
20 Sulfur2 (92) 7.998534 1.246987 6.414289
21 Sulfur3 (92) -1.103417 .196685 -5.610069
22 Sulfur (91) -9.184796 2.228721 -4.121107
23 Sulfur2 (91) 1.307608 1.186220 1.102332
24 Sulfur3 (91) -.119046 .186631 -.637870
25 Sulfur (90) -13.719007 1.719104 -7.980323
26 Sulfur2 (90) 3.248646 .842976 3.853784
27 Sulfur3 (90) -.321594 .123009 -2.614397
28 Sulfur (89) -6.588620 1.720730 -3.828969
29 Sulfur2 (89) -1.254617 .838181 -1.496834
30 Sulfur3 (89) .445460 .122013 3.650906
26
31 Sulfur (88) -15.230936 2.239322 -6.801585
32 Sulfur2 (88) 3.042403 1.156172 2.631445
33 Sulfur3 (88) -.145468 .177023 -.821745
34 Sulfur (87) -11.135169 1.727345 -6.446406
35 Sulfur2 (87) .639999 .854623 .748867
36 Sulfur3 (87) .220607 .123468 1.786759
37 Sulfur (86) -11.353569 1.898160 -5.981355
38 Sulfur2 (86) 1.917056 .948533 2.021075
39 Sulfur3 (86) -.056413 .140143 -.402537
40 Sulfur (85) -11.708061 .775795 -15.091702
41 Sulfur2 (85) 2.254226 .197395 11.419872
42 Sulfur3 (85) -.061021 .005658 -10.784806
43 ait -.932625 .012762 -73.077667
44 BTUit .000895 .000057 15.688016
45 DSUBit -12.385462 .931442 -13.297089
46 DBITit 16.626406 .854020 19.468407
The sample size is 104707. The numbers in parenthesis stand for year.
27
Table 7: Estimation Results WITH Dummy Variables for the States of Mines
Variable Estimates Stndard Error T-stat
1 Sulfur (98) -14.230603 2.071054 -6.871188
2 Sulfur2 (98) 2.336998 1.078291 2.167316
3 Sulfur3 (98) -0.297811 0.164819 -1.806901
4 Sulfur (97) -8.778301 1.753308 -5.006709
5 Sulfur2 (97) -1.530924 0.844126 -1.813620
6 Sulfur3 (97) 0.448089 0.119850 3.738762
7 Sulfur (96) -11.782801 1.854559 -6.353425
8 Sulfur2 (96) -0.458673 0.873697 -0.524980
9 Sulfur3 (96) 0.326068 0.119882 2.719909
10 Sulfur (95) -20.252391 1.536153 -13.183836
11 Sulfur2 (95) 2.747248 0.611836 4.490168
12 Sulfur3 (95) -0.058503 0.068513 -0.853897
13 Sulfur (94) -6.331514 1.207831 -5.242055
14 Sulfur2 (94) -1.729314 0.580749 -2.977732
15 Sulfur3 (94) 0.296552 0.080079 3.703243
16 Sulfur (93) -3.741093 1.699915 -2.200753
17 Sulfur2 (93) -2.411349 0.835909 -2.884703
18 Sulfur3 (93) 0.461298 0.119495 3.860400
19 Sulfur (92) -25.945832 2.330486 -11.133226
20 Sulfur2 (92) 9.569481 1.242160 7.703901
21 Sulfur3 (92) -1.336462 0.195811 -6.825253
22 Sulfur (91) -10.543833 2.221325 -4.746641
23 Sulfur2 (91) 2.104743 1.181766 1.781015
24 Sulfur3 (91) -0.244133 0.185795 -1.313988
25 Sulfur (90) -15.656613 1.712005 -9.145189
26 Sulfur2 (90) 4.338807 0.840438 5.162555
27 Sulfur3 (90) -0.472971 0.122569 -3.858832
28 Sulfur (89) -7.546403 1.713282 -4.404648
29 Sulfur2 (89) -0.708121 0.834765 -0.848288
30 Sulfur3 (89) 0.363865 0.121525 2.994161
The sample size is 104707. The numbers in parenthesis stand for year.
28
31 Sulfur (88) -14.242994 2.228039 -6.392616
32 Sulfur2 (88) 2.909887 1.150252 2.529782
33 Sulfur3 (88) -0.145915 0.176087 -0.828654
34 Sulfur (87) -7.663754 1.731235 -4.426756
35 Sulfur2 (87) -0.946981 0.856696 -1.105387
36 Sulfur3 (87) 0.453574 0.123906 3.660640
37 Sulfur (86) -9.626904 1.891027 -5.090834
38 Sulfur2 (86) 1.184617 0.944477 1.254258
39 Sulfur3 (86) 0.041124 0.139529 0.294734
40 Sulfur (85) -10.755476 0.775104 -13.876171
41 Sulfur2 (85) 2.067937 0.196693 10.513511
42 Sulfur3 (85) -0.055969 0.005636 -9.929863
43 ait -0.986072 0.012930 -76.259885
44 BTUit 0.000547 0.000059 9.330582
45 DSUBit -8.320185 1.280496 -6.497625
46 DBITit 16.478676 0.849360 19.401292
47 MineDummy 4.085223 1.151351 3.548198
48 MineDummy 1.710040 1.127164 1.517118
49 MineDummy 5.380586 0.993149 5.417701
50 MineDummy 4.463889 1.002088 4.454589
51 MineDummy 12.605195 1.640985 7.681479
52 MineDummy 9.703054 0.976151 9.940113
53 MineDummy 8.411331 1.050975 8.003362
54 MineDummy 7.940339 1.478095 5.372008
55 MineDummy 10.565247 0.787229 13.420810
56 MineDummy 14.529588 2.302449 6.310492
57 MineDummy 8.429100 0.996229 8.461010
58 MineDummy 29.096258 1.481557 19.638979
59 MineDummy 7.140652 0.996259 7.167465
60 MineDummy 8.710647 1.012596 8.602290
61 MineDummy 6.290799 1.300778 4.836182
62 MineDummy 11.074658 1.001066 11.062864
63 MineDummy 14.748194 3.485712 4.231042
64 MineDummy 8.085596 0.979354 8.256049
The sample size is 104707. The numbers in parenthesis stand for year.
29