Abstract
This chapter considers first the risk factors impacting jointly the Clean Development Mechanism and the European Union Emissions Trading Scheme. Second, it provides an econometric modelling exercise of risk premia in CO2 allowance spot and futures prices under the EU ETS (based on Bessembinder and Lemmon, J. Finance 57:1347–1382, 2002), which takes into account the specificities of carbon allowances in terms of storage. Third, carbon price risks in the power sector are identified econometrically by analyzing the factors that influence fuel-switching. Fourth, a stylized portfolio management exercise is proposed by using mean-variance optimization in a broadly diversified portfolio composed of stocks, bonds, weather, energy and carbon assets. The Appendix details how to compute implied volatility series from options, which can then be used to represent the risk-neutral probability distribution of carbon prices.
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Notes
- 1.
Note CERs traded on exchanges are precisely guaranteed secondary CERs (sCERs), but for simplicity we use the common denomination term of CERs throughout this chapter.
- 2.
- 3.
See Chap. 1 for the detailed calendar.
- 4.
CDM credits can be issued by destroying HFC-23 (trifluoromethane), which is 11,700 times more potent as a greenhouse gas than CO2. It can be removed by installing gas scrubbers for instance.
- 5.
Recall that each ton of HFC abated delivers 11,700 CERs.
- 6.
The N2O global warming potential is 310 times higher than CO2.
- 7.
For a more detailed time-series modeling of the convenience yield (especially by using intraday data) in the carbon market, see the analysis by Chevallier (2009, [17]).
- 8.
- 9.
- 10.
The interested reader may refer to Chap. 2 for a full description of the fuel-switching mechanism in the power sector, in presence of carbon costs.
- 11.
The data used for this section is not available for download.
- 12.
1 therm=0.10550559 GJ.
- 13.
The coal calorific value is equal to 24.9 MJ/kg.
- 14.
Now, it is called the UK Department for Business, Innovation and Skills.
- 15.
Note that we not include in the analysis the capital and operations and maintenance costs of coal vs. natural gas which may result in the unusually low spreads noted in Fig. 5.8. Hence we aim at capturing the short-term effect of introducing emissions trading on power producers’ fuel-switching behaviour (see Delarue et al. (2010, [24])). A longer term analysis of fuel substitution with additional costs associated with a retro-fit is not possible in this setting.
- 16.
See Chap. 2 for structural break tests.
- 17.
Note that the negative sign found in subsample #1 for the coefficient of the carbon price may be explained by confusing price signals sent to power producers during 2005–2007, as the carbon spot price geared towards zero due to the presence of banking restrictions between 2007 and 2008 (Alberola and Chevallier (2009, [1])).
- 18.
Demand is negatively linked with Combined Cycle Gas Turbines (CCGT), and positively with coal. This is consistent with the fact that increasing demand would yield to a decrease in the number of gas-fired plants and in the fuel-switching opportunity. If the carbon price increases, the use of CCGT is encouraged and the use of coal is lower. The decrease in the use of coal is met partly with the use of gas, but it also encourages the use of other low-carbon technologies (such as nuclear or renewable energy).
- 19.
This data is not reproduced for this chapter.
- 20.
- 21.
At the market equilibrium, demand equals supply and the tangent portfolio coincides with the market portfolio.
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Appendix: Computing Implied Volatility from Option Prices
Appendix: Computing Implied Volatility from Option Prices
In the financial economics literature, risk-hedging strategies may also be designed by resorting to option prices (see [20] for an application to EUAs by using a dataset of plain vanilla European option prices at-the-money). We briefly recall here how to derive implied volatility measures from option pricing.
Let C(τ,K) obs be the observed call option price, and C(τ,K,σ) BS the Black-Scholes (BS) price computed using the implied volatility σ. By definition, we have C(τ,K) obs =C(τ,K,σ) BS . The implied volatility of the strike price is obtained by numerically inverting the BS formula, which can be done by solving:
Reference [20] shows that option prices on the carbon market lead to pricing errors that are usual for commodity or equity markets (see also [5]). Implied volatility series can then be used to represent the risk-neutral probability distribution of a given asset in financial economics.
5.1.1 Problems
Problem 5.1
(Calibrating GARCH Models for Carbon Prices)
-
(a)
Consider the descriptive statistics for the CO2 price series in Table 5.9: how well do they seem to fit the GARCH(p,q) models specifications?
-
(b)
Following the Box-Jenkins methodology, we configure the ARMA(p,q) processes that provide the best fit to the CO2 time-series. Then, we estimate the corresponding GARCH(p,q) model for the CO2 price series:
$${{Y}_{t}}=\theta {{{X}'}_{t}}+{{\varepsilon }_{t}}$$(5.14)$$\sigma _{t}^{2}=\omega +\sum\limits_{i=1}^{p}{{{\alpha }_{i}}\varepsilon _{t-i}^{2}}+\sum\limits_{j=1}^{q}{{{\beta }_{j}}\sigma _{t-j}^{2}}$$(5.15)with \(\sigma_{t}^{2}\) the conditional variance, which is function of a constant term ω, the ARCH term \(\varepsilon^{2}_{t-i}\), and the GARCH term \(\sigma^{2}_{t-j}\).
In Table 5.10, comment on:
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the statistical significance of the parameters obtained in the mean and variance equations;
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the value of the Ljung-Box test;
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the value of the ARCH test.
In Fig. 5.10, comment on:
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the plot of the standardized innovations of the GARCH(p,q) model;
-
the plot of the conditional standard deviations of the GARCH(p,q) model.
-
-
(c)
We consider other models than the standard GARCH(p,q) model with a Gaussian conditional probability distribution. First, we use the specification for the conditional variance proposed by Nelson (1991, [36]):
$$\log(\sigma_t^2)=\omega+\sum_{i=1}^p \alpha_i \left|\frac{\varepsilon _{t-i}}{\sigma_{t-i}}\right|+\sum_{j=1}^q \beta_j \log (\sigma_{t-j}^2)+ \sum_{k=1}^r \gamma_k \frac{\varepsilon_{t-k}}{\sigma_{t-k}} $$(5.16)where γ tests for the presence of the leverage effect. Recall that the leverage effect implies a higher level of volatility associated to decreasing prices in the financial economics literature. The EGARCH model is estimated with a Student t distribution.
Second, we use the asymmetric TGARCH model by Zakoian (1994, [45]):
$$\sigma_t^{2}=\omega+ \sum_{i=1}^p \alpha_i \varepsilon_{t-i}^2+ \sum _{j=1}^q \beta_j \sigma_{t-j}^2 + \sum_{k=1}^r \gamma_k \varepsilon _{t-k}^2 \varGamma_{t-k} $$(5.17)where Γ t =1 if ε t <0, and 0 otherwise. ε t−i >0 and ε t−i <0 denote, respectively, good and bad news. The TGARCH model is estimated with a Generalized Error Distribution (GED).
Consider the Tables 5.11 and 5.12: do you observe any improvement with the alternative specification structures in the variance equation?
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Chevallier, J. (2012). Risk-Hedging Strategies and Portfolio Management. In: Econometric Analysis of Carbon Markets. Springer, Dordrecht. https://doi.org/10.1007/978-94-007-2412-9_5
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