Abstract
The relationship between wealth and climate change concern has been a focus of several studies. In this article, we hypothesize that richer households (and countries) are less concerned about climate change because wealth provides a buffer against some of the related risks. This leads people in wealthier countries and households to perceive a greater sense of control over climate change impacts, which in turn results in lower levels of concern. We tested this hypothesis using a unique household survey encompassing 11 OECD countries and over 10,000 households and applying mixed multi-level regression models. Our results confirmed a statistically significant negative relationship between country and household wealth and individuals’ perceptions of the seriousness of climate change. This study contributes to current literature by showing that this relationship is mediated through sense of control, measured at the country level by the country’s readiness index and at the individual household level by the extent of adoption of energy efficiency improvements. These findings raise the question of how best to incentivize action on climate change amongst those with the ability—but not necessarily the motivation—to respond.





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Notes
For example, those households who can afford to build a floating house (i.e., a house that rises with the water levels) are likely to feel less anxious about future risks of flooding.
The publication from the OECD can be found here: https://www.oecd.org/env/consumption-innovation/greening-household-behaviour-2014.htm. The questionnaire can be shared upon request.
The OECD survey data are not publicly available and requires permission to use the data. We are not aware of any other publicly available household survey data with such wide coverage in terms of countries and environmental domains.
The score is set to missing if installation of the equipment was not possible (e.g. because the household was renting and only the landlord could install the equipment).
Unfortunately our dataset does not include information on race or political ideology. These characteristics could be important omitted variables since there is consistent evidence that older white men, living in rural areas, identify as a Christian, and who hold conservative political views care less about climate change issues (Hornsey et al. 2016; Lee et al. 2015; van der Linden 2017).
The identification of a pure mediating effect requires strong assumptions, which are likely not to be satisfied apart from very specific settings where X features a randomized intervention. These assumptions include: the exogeneity of X; no reverse causality (i.e., Y should not cause X); no omitted variable; X and M do not interact to cause X; and usual assumptions on the error term. The identification of mediating effects becomes even more difficult when the model involves multiple independent variables, as is the case in our study. In such cases it is difficult to know with certainty whether the hypothesized mediating variable is a “real” mediator, a covariate, a moderator, or a confounding variable (MacKinnon, Fairchild and Fritz 2007). M would be called a confounding variable if: M causes both X and Y and ignoring M leads to incorrect inference about the relationship between X and Y. M would be called a covariate if: M improves the prediction of Y by X but does not substantially alter the relation of X to Y when Z is included. Finally M would be called a moderator if the relationship between X and Y differs at different values of M.
The models were estimated using the mixed command in Stata.
In each country the number of regions/states includes: Australia: 8; Canada: 11; Chile: 15; France: 22; Israel: 6; Japan: 8; Korea: 16; Netherlands: 12; Spain: 17; Sweden: 21; and Switzerland: 26.
The country-level mediation (through the readiness score) is less convincing when regional-level rather than when household-level data are used. That is, GNI per capita is not a statistically significant negative predictor in the models that use regional-level household data (i.e., Models 3 and 4). The readiness score is negative and statistically significant in Model 4, similar to the findings of Model 2.
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Acknowledgements
The data upon which this study is based were collected as part of the OECD’s project “Household Behaviour and Environmental Policy.” This work is published on the responsibility of the authors. The opinions expressed and arguments employed herein do not necessarily reflect the official views of the OECD and/or of the governments of its member countries. The authors are grateful to the OECD for providing the data. The authors are also grateful for the comments of four anonymous reviewers that improved this manuscript. Finally, funding from the French National Research Agency (ANR) under the Investments for the Future (Investissements d’Avenir) program, grant ANR-17-EURE-0010 and Australian Research Council FT140100773 is acknowledged.
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Appendices
Appendix A
Appendix B
The final specification of Model 1 is the following:
\({\text{CCbelief}}_{i,c} = \beta_{0,c} + \beta X_{1,i} + \beta_{c} X_{2,i} + \gamma X_{3,c} + \varepsilon_{i,c}\), with i, the index for the respondent or household, and c, the country index. The dependent variable, \({\text{CCbelief}}_{i,c}\), measures respondents’ level of climate change concern on a scale from 0 to 10. The best specification (as shown in Table 2) features a random intercept (\(\beta_{0,c}\)); fixed effects (\(\beta\)) for variables in the \(X_{1,i}\)-vector of respondent/household characteristics; random effects (\(\beta_{c}\)) for variables in the \(X_{2,i}\)-vector of respondent/household characteristics, and fixed effects (\(\gamma\)) for the country-specific characteristics gathered in the \(X_{3,c}\)-vector. We have:
\(X_{1,i}\) = (male, age, higher education, personal safety ranking, local environment satisfaction, children, and energy use monitored);
\(X_{2,i}\) = (trust experts, charity giving, conservative ideology, income, urban location); \(X_{3,c}\) = (gross national income, environmental performance index, extreme climate %, floods, mean temperature − 5 years previous-), mean temperature ratio − 100 years previous-), right party ruling).
Model 2 is the same as Model 1 except that it includes the mediating variable (overall readiness score) in \(X_{3,c}\).
Models 3 and 4 feature fixed effects only and include both regional and country-specific variables (see complete list in Table 3).
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Nauges, C., Wheeler, S.A. & Fielding, K.S. The relationship between country and individual household wealth and climate change concern: the mediating role of control. Environ Dev Sustain 23, 16481–16503 (2021). https://doi.org/10.1007/s10668-021-01327-x
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DOI: https://doi.org/10.1007/s10668-021-01327-x


