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Exchange Rate Effect on Carbon Credit Price via Energy Markets
by
Jongmin Yu, Ph.D Candidate
University of Illinois at Urbana-Champaign, Mumford Hall, MC-710, 1301West Gregory Drive,
Urbana, IL 61801, United States
Phone: 1-217-417-2216/ Email: [email protected]
Mindy L. Mallory, Assistant Professor
University of Illinois at Urbana-Champaign, Mumford Hall, MC-710, 1301West Gregory Drive,
Urbana, IL 61801, United States
Phone: 1-217-372-4163/ Email: [email protected]
Abstract
This paper discusses the effect of currency exchange rates on the carbon market. We illustrate this
effect using the European Union Emission Trading Scheme (EU-ETS), which primarily uses two
substitutable energy inputs for the generation of electricity: coal and natural gas. The European coal
market is directly driven by global coal markets that are denominated in USD, whereas, natural gas is
mainly imported from Russia and is denominated in Euro. The impulse response functions of a Structural
Vector Autoregression (SVAR) model demonstrates that a shock in the EU/USD exchange rate is
delivered through the channel of energy substitution between coal and natural gas, and therefore,
produces influences on the carbon credit market.
Introduction
This paper shows the effect of a currency exchange rate on the carbon prices when substitutable
energies are denominated in different currencies. We illustrate this effect in the European Union Emission
Trading Scheme (EU-ETS) because this carbon market has the longest history and the largest trading
volume among carbon credit markets. The European Union primarily uses two substitutable fossil energy
inputs to generate electricity: coal and natural gas.1 The power generation industry has been the main
player in the EU-ETS because it consumes around 60% of the total credit allocation. Electricity
generators can substitute back and forth from coal to natural gas relatively easily, depending on the
relative prices of coal and natural gas and the demand for electricity. Burning coal generates almost twice
as much carbon dioxide emissions compared as natural gas in producing the same amount of energy. So,
making CO2 emissions more costly can influence the decision between fuels at the margin. Since the EU
ETS was introduced, power generators always select the fuels they are going to use by considering the
cost of using each fuel plus buying emission credits each day. This has been called fuel-switching, and it
affects the carbon emission allowance market. It is therefore reasonable to assume that electricity
producers decide their position in either the OTC or the emissions exchange markets by reacting to
changes in the relative prices of two competing fossil fuels. Theoretically, this selection decision can be
made on a daily basis because daily changes in fuel and carbon prices change the relative electricity
generation cost benefit by comparing marginal generation costs (Koenig, 2010), and power generators
also have traded in the carbon market on a daily basis (Bunn and Fezzi, 2007). This effect of relative
energy prices to the demand of the EU carbon market has been confirmed in numerous previous studies.
(Delarue, Voorspools and D’haeseleer, 2007; McGuinness and Ellerman, 2008; Alberola, Chevallier and
Chèze, 2008)
The European coal market is directly driven by global coal markets that are denominated in USD;
whereas, natural gas is denominated in Euro (Polański and Winkler, 2008; Timera Energy, 2011; Monthly
Bulletin of BlueNext ). Also, we know that the substitution between coal and natural gas affects the price
of carbon credits because coal generates more CO2 emissions than natural gas. Therefore, asymmetric
exposure to exchange rate risk of the two energy inputs changes the Euro denominated price spread
between coal and natural gas. Since exchange rate risk influences the relative price of coal to natural gas,
the substitution between the clean and dirty inputs affects the price of carbon. For example, if the Euro
depreciates against the USD, ceteris paribus, this increases the price of coal relative to the price of natural
gas in Euro. This causes energy substitution away from coal and toward natural gas thereby lowering
CO2 emissions; hence, carbon credit prices would fall.
To date, most studies of the carbon market in the European Union (EU) discuss how supply and
demand are affected by various factors such as temperature, emission cap policy, other energy markets,
and market regulations (Chevallier, 2009). Chevallier (2009; 2010 a,b,c) are the exceptions, and these
consider macro factors like the bond market, the stock market, and business cycle indices to understand
the EU carbon market using time-series models. However, Chevallier did not consider the effect of
international energy markets through currency exchange rates. On the other hand, Frank and Garcia (2010)
identified currency exchange rates as indicators of commodity prices. Their result shows that agricultural
1 According to the EU energy report (2009), 29.4% of electricity was generated from coal, and 22.6% was generated
from natural gas in 2007. (27.8% from nuclear, 15.6% from renewable, and 3.3% from oil)
goods are becoming more dependent on exchange rates. Thus, we propose a research to identify the effect
of exchange rate on the carbon credit price through the fuel switching process.
Data
In this paper we use spot EU/USD exchange rates, European Emission Allowances (EUAs)
carbon credit prices, natural gas and coal prices. Our price data are nominal and weekly starting from
January 2007. The EU/USD currency exchange rates are spot rates from European Central Bank (ECB);
the carbon credit price (€/ton of CO2) is the nearby futures price of EUAs obtained from the
Intercontinental Exchange; the natural gas price (€/MMBtu) is obtained from the Zeebrugge Hub spot
price, which is the major short-term natural gas trading market in continental Europe, and the coal price
(€/ton) is from the ARA spot price, which is the major imported coal in northwest Europe.
Figure 1. Nominal prices of coal, natural gas and carbon credit prices in Euro
Figure 1 shows recent prices of EUA, natural gas, and coal in Euro. It is intuitive that these two
energy markets help us understand the carbon market because the relative prices of coal and natural gas
have been identified as a driver of EUA prices. Commonly, besides the price spread between coal and
natural gas, the overall price level of the two energy prices also affects EUA prices. Since higher energy
prices represent higher energy demand, higher energy consumption also indicates higher carbon dioxide
emissions and EUA prices, and vice versa. Figure 1 shows this standard co-movement of prices in EUA,
natural gas and coal; until mid-2008, there was an overall increase of those commodity market prices.
However, after mid-2008 and beginning in 2009, the prices dropped together steeply because of the
recession triggered by the default of Goldman Socks in U.S.
0
5
10
15
20
25
30
35
0
20
40
60
80
100
120
140
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/10
/20
06
4/2
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7
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/14
/20
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6/1
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/18
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7/6
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12
Gas Coal EUA
Pri
ce o
f C
oal
an
d G
as
(un
it: E
uro
)
Pri
ce o
f EU
A (
un
it: E
uro
)
However, we may be able to identify different patterns of the carbon and energy markets’ co-
movement since 2009. The prices of energy are gradually recovering as time goes, but the price of EUA is
not catching up the other energy prices. Even between the energy markets, the price of natural gas
increases more slowly than the price of coal, which is an also different phenomenon compared to the
common idea of a highly correlated movement between energy markets before financial crisis. Since
there has been a consensus that energy market trends are the most important price driver because of
carbon emission demand, it would be worthwhile to look for other reasons why only the carbon market
has been decreasing compared to other energy market.
Figure2. Exchange rates
In figure 2, before mid-2008, the Euro appreciates against USD, which corresponds with the
bullish trend in energy sectors in figure 1; there was high demand for energy with the economy boom and
the Euro currency appreciates along with strong economic activities. After mid-2008, the Goldman
Sock’s bankruptcy and the European government’s budget deficit impacted the global financial markets,
which kept the Euro/USD exchange rate relatively high and unstable. Correspondingly, energy markets in
figure 1 also show a bearish trend compared to the period before mid-2008. The descriptive statistics for
all time-series data used in this paper are summarized in Table 1.
Table 1. Descriptive statistics
EU/USD Coal Natural gas EUA
Mean 0.72 96.46 48.23 18.06
Median 0.72 93.75 46.60 16.03
Maximum 0.84 192.50 95.00 31.42
Minimum 0.63 51.60 17.40 9.43
Std. Dev 0.04 30.35 16.15 4.98
Skewness -0.02 0.61 0.62 0.79
0.6
0.65
0.7
0.75
0.8
0.85
10
/10
/20
06
4/2
8/2
00
7
11
/14
/20
07
6/1
/20
08
12
/18
/20
08
7/6
/20
09
1/2
2/2
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0
8/1
0/2
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0
2/2
6/2
01
1
9/1
4/2
01
1
4/1
/20
12
Lehman bro. files for bankruptcy (15.Sept.2008)
Request for financial support - Greece (23.Apr.2010) - Ireland (21.Nov.2010)
Portugal (6.Apr.2011)
Kurtosis -0.43 -0.11 0.01 -0.46
Observation 249 249 249 249
Table 2 contains results of the Augmented Dickey Fuller test for stationarity, and we conclude
that each data series is I(1). Because all series are integrated of the same order, 1, it is possible to have
cointegration among those non-stationary variables. Here we determine whether a vector error correction
model or a vector autoregression model is appropriate. In table 3, we perform the Johansen trace test on
the system of 5 variables, but we did not find any cointegrating relationships among the 5 variables.
Table 2. Augmented Dickey Fuller unit root test
Model Lags 5% statistics Result
EUA CNT 0 -3.41 -2.14 Non-stationary
Coal CNT 2 -2.86 -2.01 Non-stationary
Natural gas NCNT 1 -1.94 0.02 Non-stationary
EU/USD CNT 0 -2.86 -2.19 Non-stationary
d. EUA NCNT 0 -1.94 -9.50 Stationary
d. Coal NCNT 2 -1.94 -5.27 Stationary
d. Natural gas NCNT 0 -1.94 -8.93 Stationary
d. EU/USD NCNT 0 -1.94 -14.95 Stationary
CT: constant and trend, CNT: constant and no trend, NCNT: no constant and no trend.
We start estimating the VAR model with 3 lags. Once the full model is estimated with a given
number of lags, we applied the sequential parameter elimination is applied based on Top-Down procedure
with AIC criteria. With the regressors that have survived from the sequential elimination process, the
model is estimated again with only selected regressors. Then, we finally get the information criteria
indexes as we could see in table 3 for given number of lags. We repeat this process for various numbers
of lags and compared those to get the optimal model.
Table 3. Johansen trace test
Rank Trace statistic 5% critical Value
0* 34.28 53.94
1 19.63 35.07
2 8.04 20.16
3 2.49 9.14
Table 4 shows the somewhat perplexing results: the more lags we have, the lower the AIC and the
higher the SIC. Both AIC and BIC have pro and cons. Having too small a number of lags based on SIC is
likely to result in autocorrelation of the estimated VAR model, and having large number of lags based on
the AIC steeply increases the number of estimated coefficients of the model. Furthermore, this paper
seeks to examine the effect of short-term macro shock within a couple of months, so we limit our trial to
up to 5 lags. In short, we choose to use the Hannan-Quinn criterion which indicates 4 lags in the
differenced VAR model, which is optimal.
Table 4.
# of lags of endogenous various AIC SIC HQ
5 -9.071854e+00* -8.496865e+00 -8.840254e+00
4 -9.011207e+00 -8.638558e+00 -8.861125e+00*
3 -8.981066e+00 -8.652377e+00 -8.848703e+00
2 -8.940307e+00 -8.711654e+00 -8.848229e+00
1 -8.871413e+00 -8.714214e+00* -8.808109e+00
Model Specification
We will use a structural VAR model since we want to look at the interdependency of exchange
rates and other energy commodities across time, and the structural VAR model has been used to identify
the market linkage in many previous studies. We estimate a first differenced VAR model to test the
hypotheses developed earlier. In this paper, we need to estimate a structural VAR after estimating reduced
VAR because the energy substitution occurs at a daily frequency; the instantaneous effect found in
weekly data (that encompasses 5 trading days) will represent the daily energy substitution of the industry.
We can identify the instantaneous causality by estimating the matrix B below by estimating the structural
VAR model.
More explicitly,
[
⁄
] [
]
[
]
[
]
[
] ( ) ( )
Here, the number of lags, J, to include in this model will be determined based on AIC, BIC or HQC. We
repeat this process until we get the optimal number of lags, which minimizes the information criteria.
Then, we apply sequential parameter elimination based on Top-Down procedure with AIC criteria. With
the regressors that have survived from the sequential elimination process, the model is estimated again
with only selected regressors. As diagnostic tests, we will perform Jarque-Bera tests to ensure normality,
ARCH-LM for heteroscedasticity, and the Portmanteau test for autocorrelation.
As proposed by Sims (1980), VAR model estimation has routinely orthogonalized shocks by
using a lower triangular matrix B. Since the Choleski decomposition of the matrix B imposes an ordering
restriction of the variables, we identify the instantaneous interdependencies among the carbon market,
energy markets, and exchange rates in the VAR model.
[
] [
]
The terms in matrix represent the unrestricted parameters values and 0 terms enforce the
contemporaneous effect of endogenous variable to be zero. In terms of ordering, the 1st row means the
exchange rates are not affected by any other endogenous terms at least contemporaneously. This setup
follows Akram (2009) since usually macro variables reflect the overall economy of a certain country so
that those would work more independently from energy markets and carbon market. Thus, the energy
markets from the 2nd
to 3rd
row of matrix are subject to the effects of exchange rate shocks. The 4th row,
the carbon credit market, is the last term after the energies since the scale of the energy markets are bigger
than the carbon credit market; the price transmission from energy to carbon market would be more
acceptable than the other way around. Hence, the carbon market is the last of the ordering. Between the
coal and natural gas markets in the EU, the coal market has been regarded more susceptible to
international shocks since the main currency in coal trading is U.S. dollar. However, the natural gas
market is based on the domestic currency, i.e. Euro, so that the market has been regarded to be isolated
from currency markets. We will see later in this paper how this different exposure of energy markets to
international currency markets affects to the carbon credit price determination.
Empirical Results
(1) Impulse response function
In the following, we run impulse response functions based on the previously described differenced
SVAR model. 95% confidence intervals were estimated with respect to the impulse response to different
shocks. Even though the size of the data is not small (n=249), we used the bootstrapping of 1500
iterations suggested by Hall (1992) to obtain the more reliable confidence interval. The impulse response
which describes effects of macro policy variables on energy and carbon markets appear in figure 3.
Figure 4 shows the accumulative effects on impulse response. Both figures demonstrate the effect of
energy substitution. Figure 3 shows the marginal impulse response of coal, natural gas, and carbon market
to a shock of one positive standard deviation of the exchange rate (depreciated Euro against USD), and
figure 4 shows the accumulative response, respectively.
Figure 3. Impulse to Euro/USD exchange rate; response to coal (1st row), natural gas (2
nd row), and
carbon credit (3rd
row).
Figure 4. Accumulative impulse to Euro/USD exchange rate; response to coal (1st row), natural gas (2
nd
row), and carbon credit (3rd
row).
In the coal market, the first row of figure 3 and figure 4, a depreciated Euro against the USD leads to an
initial increase in the coal price. Currently, the European coal market has been dominated by global
markets which use the USD. Since the Euro/USD exchange rate impacts the purchasing power of coal, the
depreciated Euro drives increases the domestic coal price in Euro increases, even though the price based
on the USD is at a standstill. Figure 3 shows the marginal positive effect and figure 4 confirms that the
positive accumulative effects also persist.
In the natural gas market, the second rows of figure 3 and figure 4 show unclear results. There is no
immediate response from the Euro/USD exchange rate shock, and the accumulative effect is also not
critically different from the mean of 0. The reason is that the European natural gas market is not exposed
to the Euro/USD exchange risk. The biggest supplier of natural gas to the EU has been Russia, and this
constitutes 41% of total imports (EU-energy report, 2010). Based on the agreement between the EU and
Russia, natural gas supply contract has opted for the Euro currency instead of the USD (Occasional paper
series, European Central Bank, 93-2008).
In the carbon market, the third row of figure 3 and figure 4, a depreciated Euro against the USD decreases
carbon credit prices. Figure 3 shows the marginal negative effect and figure 4 also confirms that the
negative accumulative effects also persist. This occurs due to the energy substitution effect resulting from
relative energy price changes. A depreciated Euro increases the price of coal relative to natural gas, which
induces less consumption of coal. Since natural gas is a less carbon-intensive fossil fuel than is the case
for coal, the depreciated Euro again the USD would lower both the demand for carbon dioxide emission
and the demand for emission credit.
Now let us examine the interactions among coal, natural gas and the carbon market. Again, the
substitution effect from the relative price difference between coal and natural gas has been regarded as the
main price driver of carbon pricing. There would be more energy demand for the cheaper fossil fuel
source. For example, if coal price in Euro increases due to the depreciated Euro, coal would be consumed
less than would be the case for natural gas. Less consumption of coal leads to less CO2 emissions so that
the demand on CO2 emission credit would decrease, which would lower the price of carbon credits. On
the contrary, if natural gas prices increase due to use of the appreciated Euro, coal would be consumed
more than natural gas. More consumption on coal increases CO2 emissions so that the demand for CO2
emission credits would rise, which would increase the price of carbon credits. Figure 5 shows the
marginal impulse responses and figure 6 shows the accumulative effects in a comparative manner.
Figure 5. Impulse to coal (1st column), natural gas (2
nd column) and carbon credit (3
rd column); response
to coal (1st row), natural gas (2
nd row) and carbon credit (3
rd row)
Figure 6. Accumulative Impulse to coal (1st column), natural gas (2
nd column) and carbon credit (3
rd
column); response to coal (1st row), natural gas (2
nd row) and carbon credit (3
rd row)
The first columns of figure 5 and figure 6 show the effect of coal price shock and subsequent
responses of the natural gas market and the carbon market. A shock of one positive standard deviation of
the coal price leads to an initial increase in the natural gas price. Energy prices are highly correlated, so
the positive response of natural gas to the shock of coal is not surprising. However, the response of the
carbon credit price is not critically different from 0. This is the case because energy users can mitigate the
effect of a coal price shock on the carbon market by shifting their energy demand, so the total demand
effect on emissions is not certain. For example, the rise in coal price is not directly transmitted to the
carbon price because energy users may replace expensive coal with cheaper natural gas with less CO2
emission demands. In an opposite manner, a decrease in coal price is not directly transmitted to the
carbon price because energy users may choose to use cheaper coal instead of expensive natural gas, which
induces more CO2 emissions.
However, the second column regarding the effect of a natural gas price shock contrasts the effect
of the price shock on coal. A shock of one positive standard deviation in the coal price leads to an
increase in the natural gas price, which also can be explained as energy prices correlation. In a manner
that is contrary to the effect of the coal price shock on carbon price, a price shock in natural gas generates
a response in carbon credit prices that is significantly different than zero. A natural gas price shock makes
energy users replace natural gas with coal, which inspires more emissions needs and increases the carbon
price. In this case, the energy substitution effect makes the price of carbon credit correlate in a positive
manner with the price of natural gas. For example, an increase in natural gas prices increases carbon
prices because energy users may replace expensive gas with cheaper coal that have more CO2 emission
demands. Likewise, a decrease in the price of natural gas lowers the carbon price because energy users
may use cheaper gas instead of expensive coal, which has less CO2 emission needs.
The third column shows the effect of the carbon market on the other energy markets. A shock of one
positive standard deviation in the carbon price does not result in a significant price change in coal, but
leads to a significant price increase for natural gas. In principle, high emissions costs proxies for high
emissions demand, which is expected to increase both energy prices. However, it is more likely to
produce a higher demand effect on natural gas than coal because energy users can save on compliance
costs by using less carbon-intensive energy.
(2) Forecast error variance decomposition of shocks
The following figures decompose the contribution of different structural shocks to price fluctuations
over the course of 50 weeks. The forecast error variance decomposition (FEVD) displays the percentile
contribution of four different sources of shocks: exchange rates, coal prices, natural gas prices and carbon
prices. Each row shows the coal, natural gas and carbon market, respectively.
The FEVD generally confirms the causality result obtained from the IRF analysis. The EU/USD
exchange rate has the highest explanatory power regarding the price of coal, the second highest
explanatory power regarding the price of carbon credits, and almost negligible explanatory power
regarding the price of natural gas. This is because the price of coal is converted from USDs to Euro when
purchased from the international coal market. Thus the nominal coal price in Euro is directly affected by
the Euro/USD exchange rate. In the case of the carbon market, the Euro/USD exchange rate indirectly
affects carbon prices via coal market because the price spread between coal and natural gas affects the
carbon price. On the other hand, European natural gas market is unglued from the international energy
market so the exchange rate has little impact on natural gas prices.
With regard to interactions between the carbon market and the different types of energy, the FEVD
results remain consistent with the IRF, which demonstrates the energy substitution effect and the positive
correlation between substitutable energies. These results allow us to ascertain that coal is more relatively
exogenous than natural gas and carbon credits, and about 20% of the forecast error in natural gas is
explained by coal. On the other hand, carbon credit is the most endogenous variable in the sense that it is
explained by all of the other variables. Natural gas explains about 25% of the forecast error in carbon
credit as the most important price driver. These results are consistent with the assumption of the ordering
restriction in Choleski decomposition.
Figure 7. FEVD based on SVAR model with coal(1st row), natural gas(2
nd row) and carbon(3
rd row).
Conclusion
This paper discusses the link between carbon pricing and exchange rates. Our paper verifies that
depreciated (appreciated) local currencies can cause low (high) carbon prices through the energy
substitution mechanism. The exchange rate depreciation shock on the carbon market is due to non-
homogeneous effects on three commodities. Our empirical analysis shows that the depreciation in Euro
leads to a price increase for coal, a neutral price change for natural gas, and a price decrease for carbon
credits. This occurs because all three commodities have different degrees of exposure to exchange rate
risks. Coal has been traded in USDs, natural gas has been imported mainly from Russia and contracted in
Euro, and carbon price has been determined by the price spread between coal and natural gas. Then, the
substitutability between coal and natural gas serves as the key component that determines the carbon price
in an asymmetric manner.
If the European debt crisis persists and the contagion spreads to other European countries, we can
expect the Euro currency to become weaker and for exchange rate Dollars to again increase. This makes it
more probable that the spread between coal and natural gas in Europe market will increase, and this
makes industries prefer natural gas to coal along with their demand for carbon dioxide emission. If
exchange rates increase due to the potential risk of bankruptcies or moratoriums in many European firms,
then this may magnify the slump of carbon markets. In conclusion, the carbon market may show bearish
movements because of the effect of depreciated Euro, although energy markets are recovering. This
monetary policy aspect may explain the de-trending of carbon markets away from energy markets.
Furthermore, we can generalize our results such that the different types of energy dependency in
the international markets may characterize the effects of exchange rate on carbon market in different
ways. If the European coal market is also separated from the international market and not denominated in
USDs, this may invalidate the effect of exchange rate shocks on the carbon market.
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