Abstract
Understanding the properties of \(\text {CO}_{2}\) emissions is crucial in designing and implementing policies in the battle against climate change and global warming. One of the main characteristics of the \(\text {CO}_{2}\) emissions that needs to be examined is the degree of persistence of the emissions. This study examines the degree of persistence in aggregated and disaggregated \(\hbox {CO}_{2}\) emissions at the global and regional levels. The results from the subsampling confidence intervals show that the \(\text {CO}_{2}\) emissions, regardless of aggregation level, are highly persistent and non-stationary. Therefore, even a transitory shock will have a permanent effect on the emission of \(\text {CO}_{2}.\) The same is true for \(\text {CO}_{2}\) emissions due to cement production and fuel consumption (gas, liquid, and solid). On the other hand, emissions from gas flaring appear to be stationary in most cases. In addition, the results show that emissions in the Middle East exhibit higher degrees of persistence compared to global emissions and emissions in Western Europe.
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Notes
In principle, these shocks could result from the policies that change the fuel efficiency, the combination of fuels, the prices of energy carriers, the environmental law, and so on.
Note that \(\alpha \) is the coefficient of the lagged dependent variable in the augmented Dickey–Fuller regression.
The cumulative impulse response is a tool that summarizes the information of the impulse response function into a scalar.
It is necessary to know the properties of the global and regional emissions to make sure that regulatory markets such as the Kyoto Protocol and the EU ETS (the EU emissions trading system) can result in a significant and prolonged effect.
Brazil, Russia, India, China, and South Africa.
Canada, France, Germany, Great Britain, Italy, Japan, and the USA.
In other words, the confidence interval will have a size distortion and the actual size will not match the nominal size (Patterson 2011).
Note that these approaches, by resampling blocks or subsamples of data, retain the possible dependence structure of the observed data.
See Politis et al. (1999) for details.
\(\alpha \) measures the closeness of the process to non-stationarity (Andrews and Chen 1994).
It has shown by Romano and Wolf (2001) that the appropriate value for this normalization constant is \(T^{0.5}\), where T is the sample size.
They have used historical energy statistics to estimate the global, regional, and national fossil fuel \(\text {CO}_{2}\) emissions back to 1751. The data can be downloaded from http://cdiac.ess-dive.lbl.gov/trends/emis/overview.html. In this paper, we use the global and regional data.
These are the five main components of the aggregate \(\text {CO}_{2}\) emissions.
It is worth noting that these two groups of countries differ from each other in different aspects. Western European countries have the most extensive environmental laws and mechanisms, such as the European Union Emissions Trading System, while many of Middle Eastern countries do not have well-established or effective environmental laws (see Camarero et al. 2014 for details). In addition, while Western European countries have a high dependency on energy imports, most Middle Eastern countries are energy exporters. All of this can affect the degree of persistence in \(\text {CO}_{2}\) emissions.
Data on global \(\text {CO}_{2}\) emission and \(\text {CO}_{2}\) emission in Western Europe were available from 1751, but the data for the Middle East are only available from 1865; therefore, we used a common sample for the total \(\text {CO}_{2}\) from 1865 to 2013.
The first decline possibly corresponds to the energy crises in the 1970s, and the decline in 2006 could be the result of economic crises and decline in GDP.
Gas flaring can be reduced in different ways, such as liquefying to natural gas and re-injecting into the ground (Bassey 2008).
We use the results from these standard unit root tests only as a benchmark, as our main intention is to gain insight into the persistence using confidence intervals. Hence, we do not consider other unit root tests available in the literature.
The same lag lengths are used in the unit root tests.
As per recommendation of Romano and Wolf (2001) we set \(c_{1}=1,\)\(c_{2}=3\), and \(\eta =0.5\).
It is important to note that the presence of structural breaks in the series does not affect the results from subsampling confidence intervals, because in the subsampling methods we take several blocks from the whole sample and estimate a confidence interval for every single block. The presence of break points will affect only a few of the constructed CIs. These few CIs will only affect the lower and upper ends of the approximated distribution, which will be discarded in the final stage of constructing the 95% confidence intervals.
The only exceptions are flaring in North America and Oceania, which now appear to be stationary with roots close to one.
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Fallahi, F. Persistence and unit root in \(\text {CO}_{2}\) emissions: evidence from disaggregated global and regional data. Empir Econ 58, 2155–2179 (2020). https://doi.org/10.1007/s00181-018-1608-3
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DOI: https://doi.org/10.1007/s00181-018-1608-3