It is well understood that adding to the population increases CO2 emissions. At the same time, having children is a transformative experience, such that it might profoundly change adult (i.e., parents’) preferences and consumption. How it might change is, however, unknown. Depending on if becoming a parent makes a person “greener” or “browner,” parents may either balance or exacerbate the added CO2 emissions from their children. Parents might think more about the future, compared to childless adults, including risks posed to their children from environmental events like climate change. But parenthood also adds needs and more intensive competition on your scarce time. Carbon-intensive goods can add convenience and help save time, e.g., driving may facilitate being in more places in one day, compared to public transportation or biking. Pre-prepared food that contain red meat may save time and satisfy more household preferences, relative to vegetarian food. We provide the first rigorous test of whether parents are greener or browner than other adults. We create a unique dataset by combining detailed micro data on household expenditures of all expenditure groups particularly important for CO2 emissions (transportation, food, and heating/electricity) with CO2 emissions, and compare emissions from Swedish adults with and without children. We find that parents emit more CO2 than childless adults. Only a small fraction of adults permanently choose not to have children, which means any meaningful self-selection into parenthood based on green preferences is unlikely. Our findings suggest that having children might increase CO2 emissions both by adding to the population and by increasing CO2 emissions from those choosing to have children.
Citation: Nordström J, Shogren JF, Thunström L (2020) Do parents counter-balance the carbon emissions of their children? PLoS ONE 15(4): e0231105. https://doi.org/10.1371/journal.pone.0231105
Editor: Francisco X. Aguilar, Sveriges landbruksuniversitet - Campus Umea, SWEDEN
Received: November 8, 2019; Accepted: March 16, 2020; Published: April 15, 2020
Copyright: © 2020 Nordström et al. This is an open access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Data Availability: The household expenditure data (from the Household budget survey 2008 and 2009) that is used for this article is provided by Statistics Sweden. In Sweden, data for individual respondents (microdata) are protected by the Secrecy Act. Researchers can apply for access to microdata for use in specified research projects. The system for researchers’ access to microdata stored at Statistics Sweden is called Microdata Online Access (MONA). Users who receive deliveries via MONA can process the data over an internet connection without microdata ever leaving Statistics Sweden. Contact information to apply for access to (MONA) microdata: e-mail firstname.lastname@example.org, phone +46 10 479 50 00, website: www.scb.se/en/services/guidance-for-researchers-and-universities/ The authors had no special access to data that other researchers would not be able to obtain.
Funding: The author(s) received no specific funding for this work.
Competing interests: The authors have declared that no competing interests exist.
Population growth increases CO2 emissions, and the decision to reproduce has been found to have the largest impact on the climate, amongst any types of consumer behavior [1, 2]. Naturally, adding more people to the planet increases CO2 emissions at the extensive margin. The open question we explore herein is whether increased CO2 emissions will also occur at the intensive margin–the parents themselves. Will parents change their consumption as a result of their reproduction choice? If so, will they attenuate or accentuate the increased emissions of their children?
Parenthood has the potential to significantly affect climate change. While other consumer decisions might also affect CO2 emissions, it might be of particular interest to study the effect on the climate from parenthood. First, as opposed to most other consumer decisions, having a child changes people–it changes people’s “core preferences” , therefore potentially also people’s green preferences. Second, most people become parents, such that any altered green behavior due to parenthood has the potential to significantly affect total CO2 emissions. Third, it seems entirely feasible to design policies that could mitigate any increased CO2 emissions from parenthood, by targeting the unique situation of parents.
Whether parents mitigate or accentuate the increased emissions of their children is a priori ambiguous. Two countervailing forces are at work. First, the transformational experience of having a child. On having children, Paul (2015), pp.156, clarifies: “a personally transformative experience radically changes what it is like to be you, perhaps by replacing your core preferences with very different ones” . Particularly relevant to our context, parenthood makes people worry more about the future [4,5], and increases the strength of preferences for environmental goods , which may suggest using less carbon-intensive goods and services to reduce future risks of climate change [3, 7–12]. But the flip side is that time constraints now become more binding and convenience may become more important–parents may need to be in more places in one day. They also need to feed more people. Eating more pre-prepared, red meat carbon-intensive meals may add convenience and save time. Parents’ environmental behavior may also be motivated by other factors, such as health and income [6,13–15].
Studies provide mixed evidence on whether parenthood changes environmental preferences and attitudes [16–19]. Previous research based on the Understanding Society Survey finds some support that having a child reduces a selection of self-reported environmental behaviors . Similarly, a study based on the World Value Survey finds that parents are less willing to spend money on improving the environment than non-parents . Although providing valuable insights, previous studies have only examined a sub-set of behaviors that relate to environmental concern, and have not addressed the net environmental impact from parenthood.
In this paper, we empirically examine if parents leave a smaller carbon footprint, compared to non-parent adults. To perform our analysis, we combine detailed data on household expenditures with CO2 emissions, generating a uniquely detailed micro level dataset that spans all major household expenditure groups associated with CO2 emissions. Our data allows us to quantify and compare CO2 emissions from Swedish adults with and without children.
Our analysis relies on cross-sectional observational data. While the benefits of our data are the level of detail and the wide range of consumption types included in the data set, the drawback is that we cannot control for any potential self-selection into parenthood that is based on green preferences, which undermines our ability to suggest any causal effect between parenthood and green behavior. In theory, such self-selection could exist, i.e., people who are less “green” might self-select into parenthood, which in turn might bias our results. However, empirical evidence suggests self-selection into parenthood in general (i.e., not only as a result of any potential environmental concerns) is uncommon, and self-selection based on reasons that affect CO2 emissions is even more unlikely.
Some of the childless households in our data will likely have children later in life, some are involuntarily childless (just like some households with children likely did not plan to have children), while some actively chose to remain childless. Any self-selection affecting our results only pertains to the latter group–those choosing never to have children. This is, however, a small group–of childless households age 20–40, only five percent state they do not want to have children . The average young Swedish childless two adult-household plans to have children in the future. Further, over 50 percent of older childless households said they tried, but failed to have children. Of particular relevance to our analysis, not all willingly childless households (i.e., all of the five percent of 20–40 year old childless households) choose to abstain from having children due to reasons that might affect CO2 emissions, which is the kind of selection we would worry about for our study. In fact, the main reasons against having children have been found to be emotional stress from having a child, career interference, and not wanting the responsibility of bringing up a child, while environmental concern (e.g., concern for overpopulation), or variables that might correlate with CO2 emissions (e.g., travel preferences), have not been found to significantly affect the decision to be childless . Still, a cautionary note is granted. Although unlikely, self-selection into parenthood in our data that is based on, or correlates with, green preferences cannot be ruled out, meaning that we can say with confidence that our analysis succeeds in comparing CO2 emissions between parents and non-parents, while there is some uncertainty surrounding its success at identifying the effect of CO2 emissions on becoming a parent.
This paper provides the first rigorous test of whether parents themselves are “greener”, e.g., have a smaller carbon footprint. We find that being a parent means a Swedish person leaves a larger carbon footprint, mainly driven by higher CO2 emissions from transportation and food consumption. A potential explanation for our results may be that Swedish parents use carbon-based consumption as a substitute for their tighter time constraints. A comprehensive report on time usage by Swedish households, shows that out of all people, parents with small children have the least leisure time, defined as time not spent working, paid or in the household . Mothers and fathers of children 7 years and younger have around four hours of daily leisure time, while daily leisure time of a childless woman age 20–44 is around five hours, and that of a childless man of the same age is about six hours.
Altruistic parents’ consumption may also be impacted by the child’s immediate preferences for carbon-intense consumption, such as a taste for red meat, flights to family friendly resorts, and so on [25–27]. Children may of course also be concerned about the environment, which in turn may affect household consumption. Even though children in the Nordic countries have been found to be more environmentally concerned than their parents [28,29], there is a substantial gap between their attitudes and actions [30,31].
Our results suggest that parents emit more CO2 than non-parents, and that the greenest adult Swede is childless and lives alone. Our results may be particularly striking, given Sweden is our focus. If the transformation from parenthood causes parents to focus more on the environment, we might expect this behavior to be particularly pronounced in Sweden relative to other developed countries. Most Swedes believe climate change is real and have accepted sizable CO2 taxes–both suggest that reducing one’s carbon footprint for their off-springs matters. In addition, households with children are subsidized, which helps to alleviate some of the time crunch for parents. Sweden has generous parental leave, subsidized daycare, and parents have a legal right to reduced work hours [32,33]. But Sweden also has one of the world’s highest female labor participation rates (69.5 percent in 2015, as compared 51.4 percent in the European Union and 56.7 percent in the US), which may add to the time constraint of household with children .
2. Data and econometric specification
We summarize our unique data below, and S1 Appendix provides more specific details, including how to access the data. Our data contained household expenditures on goods and services from a set of 4,000 households surveyed by Statistics Sweden for 2008–2009. However, the sample used in our analysis is smaller (N = 2,692), given we limit our data in a few key ways–we focus on households with a positive disposable income, that have a maximum of two adults (if a household has three or more adults, we lack the necessary information to determine if all adults are parents, or some are adult children). Further, we exclude households in which at least one household member is retired. The last limitation is imposed given we want to minimize the amount of households in our sample consisting of adults who once lived with children but not now, since our analysis builds on the assumption that all households in our analysis that are currently childless also never had children. We explore the sensitivity of our results to even stricter age limits for the households included in our analysis (see S2 Appendix), and find results are robust.
Household characteristics include number of adults, number of children, age of household members, disposable income level, type of housing (apartment, house, ranch), and size of housing (in square meters). Tables 1 and 2 show descriptive statistics on household characteristics, for all households in our sample and sub-groups of households.
Next, we calculate quantities consumed by dividing expenditures by 2009 prices for all expenditure items that constitute the vast majority of household CO2 emissions. (We use prices for 2009 for the sample since we have reliable price data for 2009 and the price changes were minor in Sweden between 2008 and 2009 –the change in the consumer price index (CPI) was -0.3 percent). Third, we match the detailed consumption data with the corresponding CO2 emissions per unit. Classified according to the international COICOP classification system on a four-digit level, we capture detailed data on four expenditure groups: (a) food and non-alcoholic beverages, (b) transportation, (c) clothing, including shoes, and (d) housing. Tables 3 and 4 summarize the expenditure groups and associated levels of CO2 emissions (S1 Appendix provides the specific matching numbers and sources). These four expenditure groups account for about 85 percent of the households’ total CO2 emissions. For some expenditure groups, we need to use various sources of price and CO2 emissions data, which might create uncertainty in some of our consumption and emissions data. We therefore perform numerous robustness checks where we vary price and emission assumptions (see S2 Appendix).
Now consider our econometric specification. We examine the effect on adult CO2 emissions from adding children to a two-adult household. Using Ordinary Least Squares (OLS) regression, with heteroscedasticity-consistent (Huber-White) standard errors, we estimate the following model:
Total CO2 emissions per household (kg) = constant + b1* Number of children 0–6 years
+ b2*Number of children 7–12 years
+ b3* Number of children 13–17 years
+ b4* Number of children 18–19 years
+ b5* Two adults without children
+ b6* One adult without children
+ b7* One adult with one or more children
+ b8* Age of the oldest person in the household
+ b9* Disposable income
+ b10* Disposable income squared + error term
Our coefficient of prime interest is b5 –two adults without children. Given that we control for the impact on CO2 emissions (from children) in the household, b5 represents the difference in CO2 emissions from the two adults in a households, caused by adding children to the household. If b5 is negative, two adults emit less when childless than with children, implying that parents are browner.
Since consumption by children likely depends on the age of the child we divide children into different age groups and construct a variable that defines the number of children in each age group, on the household level. For instance, a household with two children aged 5 and 8 years, will have one child in age group 0–6 years, and one child in age group 7–12 years. Given the children within a household are divided into different age groups, the age group variables mostly consist of zeros and ones (see note in Table 2).
In the regression model we control for age of parent, given that age has been found to affect environmental preferences–older people will not live long enough to benefit from climate protection [36,37]. We also control for income since income has been shown to impact CO2 emissions . We include income both linearly and squared in the model, for two reasons. First, consumer demand studies based on cross sectional data note the importance of allowing the Engel curves to be non-linear [38,39]. Second, the hypothesis behind the Environmental Kuznets Curve (EKC) suggests that there is a non-linear relationship between environmental degradation and income [40,41]. Although empirical evidence on the existence of an EKC is mixed, several studies find an inverted U-shaped relationship between income and CO2 emissions [41–43]. Our data enables us to contribute new and valuable information to the literature exploring the existence of the EKC. Most previous studies are based on aggregate time series or panel data for countries or regions and not on cross sectional data at the household level. Our data, in contrast, allows us to explore the relationship between income and CO2 emissions (the EKC) based on substantially more detailed data.
We proceed by first using the above model to examine observed differences in total CO2 emissions for adults with and without children. Using the same regression model, we thereafter explore how CO2 emissions differ over consumption subgroups known to contribute heavily to CO2 emissions–including food consumption (e.g., meat and milk products), transportation, and heating/electricity.
For estimation purposes we use a Least Squares estimator, i.e., an estimator that is unbiased, even if the residuals or the dependent variable are not normally distributed. We tested the dependent variable total CO2 emissions from consumption for normality using a Kolmogorov-Smirnov test, and find that it is not normally distributed (test statistic = 0.039; P-value < 0.001).
Note that since we assume prices are the same for all households, our model might over or under estimated CO2 emissions for a specific household. However, there is no systematic difference in prices across parents and non-parents. We therefore expect our econometric models presented below to generate an unbiased point estimate of the difference in CO2 emissions between parents and non-parents.
Three key results emerge. First, we find that two Swedish adults in a household with children emit more carbon than two Swedish adults in a household without children. Table 5 shows the specifics–we see 719.21 kg less CO2 emissions for the household without children. This coefficient is substantial in magnitude and statistically significant (P-value = 0.001). The average couple of adults in households with children emitted 3,513.80 kg CO2 annually, the childless household emitted 3,513.80–717.98 = 2,795.82. This means parents’ CO2 emissions are 26 percent higher than emissions by non-parent adults, which suggests that parents are browner than non-parents.
Table 5 further suggests that a household consisting of only one adult without children, annually emits 3,512.07–2,331.52 = 1,180.55, which is less than half of emissions of the two-adult household without children. The adult Swede with the smallest carbon footprint therefore appears to be someone who lives alone and has never had children.
Second, focusing now on children, our results suggest that each child (ages 7–17) contributes substantially to household CO2 emissions, as suggested by the large coefficients with high statistical significance (P-value < 0.001). This confirms previous findings on the increase in CO2 emissions resulting from children . The impact on household CO2 emissions from children age 0–6, however, is both smaller in magnitude and less statistically significant (P-value = 0.094). For most of the expenditure groups in our data, children of ages 7–17 seem to have the largest impact on CO2 emissions, compared to younger (ages 0–6) or older children (ages 18–19). The exception is electricity and heating (see Table 10). Small children positively affect CO2 emissions from electricity and heating, while older children either have no, or possibly a negative impact, on CO2 emissions from this expenditure group. Both variables age of the oldest person in the household and disposable income have the expected positive impact on household CO2 emissions, including both overall emissions and emissions from sub-groups of consumption.
Third, we find that the two major sources of consumption that explain the higher CO2 emissions for adults with children are food and transportation. For food, Table 6 shows that two adults without children annually emit 303.97 kg less of CO2 from food than do two adults with children (P-value = 0.001). Higher CO2 emissions from food therefore seem to correspond to 303.97/719.21*100 = 42 percent of the total difference in CO2 emissions between adults with and without children. The large share of emissions from food consumption is consistent with previous studies that demonstrate the importance of food choice to the environment [44–47].
Table 6 also shows that the two adults in a household with children annually emit 1,028.39 kg CO2 from food consumption, while a corresponding household without children emits 1,028.39–303.97 = 724.42. This suggests adult CO2 emissions from food is as much as 42 percent higher for parents than for adults without children. Table 7 shows that higher meat consumption explains a large part of the higher CO2 emissions from food. A two-adult household without children emits 121.90 kg less of CO2 from meat consumption than do two adults with children (P-value = 0.043).
Compared to adults, children have weaker preferences for food that generates low CO2 emissions, such as vegetables and fish . Our data show that households with children have a lower budget share for fish than households without children. A potential explanation for this result might be that households converge to eating food that is agreeable to both adults and children. Previous studies find that Swedish children mostly eat breaded fish (fish sticks), , and that parents tend to avoid the stress associated with repeatedly offering their children foods that they are likely to reject .
Although regression results are not reported here, we also examined if some of higher adult CO2 emissions from parents, compared to non-parent adults, could be due to higher CO2 emissions from milk and cheese consumption. We found weak evidence that adult emissions from milk are higher for parents–an annual difference of 23 kg CO2 (P-value = 0.080), while we could not reject the null that adult CO2 emissions from cheese consumption are the same for parents and non-parent adults (P-value = 0.292).
For transportation, Table 8 shows that a two-adult household without children annually emits 397.55 kg less of CO2 compared to two adults with children. This corresponds to 55 percent of the total difference in CO2 emissions (= 397.55/719.21*100). A two-adult household with children annually emits 1,376.32 kg CO2 from transportation, while a corresponding household without children emits 1,376.32–397.55 = 978.77. This suggests adult CO2 emissions from transportation are 41 percent higher for parents than for non-parent adults. Table 9 shows that most of CO2 emissions from transportation, and differences between parents and non-parents in two-adult households, result from CO2 emissions from gasoline.
For electricity and heating, Table 10 shows we cannot reject the hypothesis that adult CO2 emissions are the same for parents and non-parent (P-value = 0.774). More generally, our model fails to explain much of variations in electricity and heating, as implied by the low adjusted R-squared value (0.008). Further, this is lower than for the other models. The adjusted R-squared values suggest that the regression models for total CO2 emissions and emissions from food have the highest explanatory power, with adjusted R-squared values of 0.33. The models for emissions from meat, transportation and gasoline have adjusted R-squared values of around 0.17, suggesting there is more heterogeneity in emissions from these goods.
Our results remain unchanged if we exclude clothes and footwear, suggesting this expenditure group both has a minor impact on overall CO2 emissions, and that parents’ CO2 emissions from clothes and footwear in two-adult households do not differ from those of non-parents.
In all regression models we also find a statistically significant inverted U-shaped relation between income and CO2 emissions, which supports the EKC hypothesis. The only exception is the model for CO2 emissions from electricity and heating, where the point estimates for the income variables are insignificant. We also estimated all regression models including higher order polynomials of disposable income, which, however, turned out to be statistically insignificant at any commonly used significance level. Our unique micro level data set therefore confirms the previous finding of an Environmental Kuznets Curve for Swedish total CO2 emissions [37, 50].
We considered the robustness of our main results by addressing three aspects of sensitivity–age of household, significance uncertainty as measured by four sources of variability, and expenditures on package trips. For age, we exclude retired subjects to reduce ‘contamination’ of our data for households without children from childless households with adult children. In the robustness checks we lower the age of the oldest adult in the household to 65, 55 and 45 year. Although our total sample size drops when reducing the age, we see no change in our basic result that parents have a larger carbon footprint. S2 Appendix provides the details.
For uncertainty, we examine four potential sources of variability: (a) CO2 emissions from boat trips (emissions from a cruise Stockholm-Helsinki), (b) energy usage from district heating (15 percent of rental costs), (c) CO2 emissions from gasoline (2.24 kg/liter gasoline), and (d) the price of public transportation (calculated as long-distance trips, suggesting the price may be on the lower end). Overall, we find no substantial effect on our main results in any of the four sources of uncertainty–again our results remain robust (see S2 Appendix for specifics).
For expenditures on package trips, Table 11 shows that a two-adult household without children spends SEK 3,356.52 more on international package trips annually compared to two adults in a household with children (P-value = 0.043). The expenditure data entails no information on the content of international package trips. However, travel surveys indicate that about one third of household expenditures on domestic trips are spent on transportation . If the same proportion is spent on transportation for international package trips, this suggests that a two-adult household without children emits 207.6 kg more of CO2 compared to two-adults in a household with children, if making the assumption that all travel related expenditures are spent on gasoline. This implies our main results hold even if parents may emit less from international trips, compared to non-parents. S2 Appendix provides more information about the data and assumptions for Swedes’ international trips and CO2 emissions.
4. Concluding remarks
Becoming a parent can transform a person–he or she thinks more about the future and worries about future risks imposed on their children and progeny. The open question that we explore is whether this transformation might imply a person will be greener. Do parents have a smaller carbon footprint? Using a unique data set that allows us to compare CO2 emissions from Swedish two-adult households with and without children, we find that two adults in households with children increase CO2 emissions by more than 25 percent relative to two adults in households without children. Parents’ CO2 emissions are higher due to increased transportation and changed food consumption. Although having children might be transformational, our results suggest parents’ “new” preferences do not cause them to be greener than non-parent adults.
We speculate that our Swedish household results may represent a lower bound on the parental carbon footprint relative to most other Western countries. Most Swedes believe climate change is a reality such that becoming more forward looking should entail caring more about climate change, and the Swedish government subsidizes childrearing to help reduce stress and increased time constraints from parenthood.
While the benefits of our data are their level of detail and the broad range of consumption types covered, a drawback is that the cross-sectional nature of the data disables analysis of causality between parenthood and the observed higher carbon emissions. That being said, self-selection into parenthood based on preference greenness is unlikely: self-selection into parenthood itself is rare , and self-selection based on green preferences even more so, to the extent that previous studies fail to detect any effect of the decision to become a parent from factors either directly or indirectly affecting CO2 emissions . It is therefore not unreasonable to imagine that our results imply a causal link–parenthood makes people browner. The larger footprint from parenthood arises mainly from higher transportation emissions and browner food.
What causes parents to emit more of CO2? The higher CO2 emissions from parenthood could be the net outcome of two previously documented counter-veiling effects: parents care more for the future [4,5], while being more pressed to satisfy immediate needs under tighter time constraints . In this study, we cannot directly observe these underlying consumption motivations. While our study suggests the difference in CO2 emissions between parents and non-parents is substantial, and therefore warrants policy makers’ attention, we encourage future research to examine the strength of the underlying factors that might cause the consumption differences. Such knowledge might be important in identifying policies that effectively reduce the carbon footprint from parents, e.g., policies that alleviate their time crunch–increased access to child care, increased work hour flexibility for parents, and so on.
Further, the differences in food consumption between parents and non-parents might be helped by recent innovations in developing meat substitutes that “taste like meat,” and hence might appeal to everyone in the family . Such meat substitutes are still relatively expensive—government subsidies of meat substitutes could help speed up the transition from meat to vegetarian proteins, especially for families with children, given they might be particularly constrained by satisfying heterogonous food preferences within the family.
Finally, our results might also imply that there could be distributional effects from the Swedish carbon tax across families with and families without children, when controlling for the number and age of people in the family. A follow-up study might determine the incidence of carbon taxes across households with and without children.
- 1. Murtaugh P. A., and Schlax M. G. (2009) Reproduction and the carbon legacies of individuals. Global Environmental Change, 19(1), 14–20.
- 2. Wynes S., and Nicholas K. A. (2017) The climate mitigation gap: education and government recommendations miss the most effective individual actions. Environmental Research Letters, 12(7).
- 3. Paul L. A. (2015). What you can’t expect when you’re expecting. Res Philosophica, 92(2), 149–170.
- 4. Sundblad E. L., Biel A., and Gärling T. (2007) Cognitive and affective risk judgements related to climate change. Journal of Environmental Psychology, 27(2), 97–106.
- 5. McCright A. M., and Dunlap R. E. (2013) Bringing ideology in: the conservative white male effect on worry about environmental problems in the USA. Journal of Risk Research, 16(2), 211–226.
- 6. Dupont D. P. (2004) Do children matter? An examination of gender differences in environmental valuation. Ecological Economics, 49(3), 273–286.
- 7. Bain P. G., Milfont T. L., Kashima Y., Bilewicz M., Doron G., Garðarsdóttir R. B., et al.(2016) Co-benefits of addressing climate change can motivate action around the world. Nature Climate Change, 6(2), 154–157.
- 8. Dresner S., McGeevor K., and Tomei J. (2007) Public Understanding Synthesis Report: A report to the Department for Environment, Food and Rural Affairs. Policy Studies Institute. Defra, London
- 9. Milfont T. L., and Demarque C. (2015) Understanding environmental issues with temporal lenses: Issues of temporality and individual differences. In Stolarski M., Fieulaine N.,and VanBeek W. (Eds.), Time perspective theory, research and application. Essays in honor of Philip Zimbardo (pp. 371–384). New York: Springer.
- 10. Milfont T. L., Wilson J., and Diniz P. (2012). Time perspective and environmental engagement: A meta‐analysis. International Journal of Psychology, 47(5), 325–334. pmid:22452746
- 11. Teal G., and Loomis J. B., (2000). Effects of gender and parental status on the economic valuation of increasing wetlands, reducing wildlife contamination and increasing salmon population. Society and Natural Resources, 13(1), 1–14.
- 12. Verplanken B. (2010) By force of habit. In Steptoe A., Freedland K. E., Jennings J. R., Llabre M. M., Manuck S. B. and Susman E. J., (Eds.), Handbook of behavioral medicine (pp. 73–82). New York, NY: Springer.
- 13. De Young R. (2000). New ways to promote proenvironmental behavior: expanding and evaluating motives for environmentally responsible behavior. Journal of Social Issues, 56(3), 509–526.
- 14. Whitmarsh L. (2009) Behavioural responses to climate change: Asymmetry of intentions and impacts. Journal of environmental psychology, 29(1), 13–23.
- 15. Richmond A. K., and Kaufmann R. K. (2006) Is there a turning point in the relationship between income and energy use and/or carbon emissions?. Ecological economics, 56(2), 176–189.
- 16. Blocker T. J., and Eckberg D. L. (1997) Gender and environmentalism: Results from the 1993 general social survey. Social Science Quarterly, 78(4), 841–858.
- 17. Ekholm S., and Olofsson A. (2017) Parenthood and Worrying About Climate Change: The Limitations of Previous Approaches. Risk Analysis, 37(2), 305–314. pmid:27164412
- 18. McCright A. M. (2010) The effects of gender on climate change knowledge and concern in the American public. Population and Environment, 32(1), 66–87.
- 19. Torgler B., García Valiñas M. A., and Macintyre A. (2008) Differences in preferences towards the environment: the impact of a gender, age and parental effect (No. 2008, 18). Nota di lavoro//Fondazione Eni Enrico Mattei: CCMP, Climate change modeling and policy.
- 20. Thomas G. O., Fisher R., Whitmarsh L., Milfont T. L., and Poortinga W. (2017) The impact of parenthood on environmental attitudes and behaviour: a longitudinal investigation of the legacy hypothesis, Population and Environment, 1–16.
- 21. Migheli M. (2018) Brown parents, green dads: Gender, children and environmental taxes, Journal of Cleaner Production, 180, 183–197.
- 22. Statistics Sweden, Demographic reports 2009:2, Having children or not? Results from a questionnaire survey about women´s and men´s attitudes towards having children, Stockholm.
- 23. Langdridge D., Sheeran P., and Connolly K. (2005) Understanding the reasons for parenthood. Journal of Reproductive and Infant Psychology, 23(2), 121–133.
- 24. Statistics Sweden, Living Conditions, Report 123. Swedish Time Use Survey 2010/11, Stockholm.
- 25. Gunter B. and Furnham A. (1998) Children as Consumers. London: Routledge.
- 26. Howard D.R. and Madrigal R. (1990) Who Makes the Decision: The Parent or the Child? The Perceived Influence of Parents and Children on the Purchase of Recreation Services. Journal of Leisure Research, 22(3), 244–58.
- 27. Wilson G. and Wood K. (2004) The Influence of Children on Parental Purchases during Supermarket Shopping, International Journal of Consumer Studies, 28(4), 329–36.
- 28. Autio M. and Heinonen V. (2004) To Consume or Not to Consume. Young People’s Environmentalism in the Affluent Finnish Society, Young 12(2): 137–53.
- 29. Carle J. (2000) Opinion och aktion. Göteborg: Göteborgs universitet.
- 30. Ojala M. (2007) Hope and Worry. Örebro: Örebro universitet.
- 31. SOU–Kommittén för utbildning för hållbar utveckling (2004:104) Att lära för hållbar utveckling. Stockholm: Fritzes.
- 32. Anxo D. (2009). Working time policy in Sweden. Working time: In search of new research territories beyond flexibility debates, 55–70.
- 33. Ray R., Gornick J. C., and Schmitt J. (2010) Who cares? Assessing generosity and gender equality in parental leave policy designs in 21 countries. Journal of European Social Policy, 20(3), 196–216.
- 34. http://data.worldbank.org.
- 35. Carlsson A., Palm V., and Wadeskog A. (2006) Energy use and CO2-emissions for consumed products and services. IPP-indicators for private and public consumption based on environmental accounts. Environmental Accounts, Statistics Sweden.
- 36. Whitehead J.C. (1991) Environmental interest group behaviour and self-selection bias in contingent valuation mail surveys. Growth and Change, 22, 10–21.
- 37. Carlsson F. and Johansson-Stenman O. (2000) Willingness to pay for improved air quality in Sweden. Applied Economics, 32, 661–669.
- 38. Banks J., Blundell R., Lewbel A. (1997) Quadratic Engel curves and consumer demand. The Review of Economics and Statistics, 79 (4), 527–539.
- 39. Brännlund R. and Nordström J. (2004) Carbon Tax Simulations Using a Household Demand Model, European Economic Review, 48, 211–233.
- 40. World Bank, (1992). World Development Report 1992: development and the environment. The World Bank, Washington, DC.
- 41. Kriström B., and Lundgren T. (2005). Swedish CO2 emissions 1900–2010: An exploratory note. Energy Policy, 33, 1223–1230.
- 42. Harbaugh W. T., Levinson A., and Wilson D. M. (2002). Re-examining the empirical evidence for an environmental Kuznets curve. The Review of Economics and Statistics, 84, 541–551.
- 43. Galeotti M., Lanza A., and Pauli F. (2006). Reassessing the environmental Kuznets curve for CO2 emissions: A robustness exercise. Ecological Economics, 57, 0152–163.
- 44. Behrens P., Kiefte-de Jong J. C., Bosker T., Rodrigues J. F., de Koning A., and Tukker A. (2017) Evaluating the environmental impacts of dietary recommendations. Proceedings of the National Academy of Sciences, 114(51), 13412–13417.
- 45. Springmann M., Godfray H. C. J., Rayner M., and Scarborough P. (2016) Analysis and valuation of the health and climate change cobenefits of dietary change. Proceedings of the National Academy of Sciences, 113(15), 4146–4151.
- 46. Vermeulen S. J., Campbell B. M., and Ingram J. S. (2012) Climate change and food systems. Annual Review of Environment and Resources, 37, 195–222.
- 47. Skinner J.D., Carruth B.R., Bounds W., and Ziegler J. (2002) Children’s food preferences: A longitudinal analysis, The American Dietetic Association, 102(11), 1638–1647.
- 48. Becker W., and Enghardt Barbieri H. (2004) Svenska barns matvanor 2003 –resultat från enkätftågor. The National Food Agency, Sweden.
- 49. Heat P., Houston-Price C., and Kennedy O.B. (2011) Increasing food familiarity without the tears. A role for visual exposure? Appetite, 832–838. pmid:21683747
- 50. Brännlund R., and Ghalwash T. (2008) The income–pollution relationship and the role of income distribution: An analysis of Swedish household data. Resource and Energy Economics, 30(3), 369–387.
- 51. SAEG. (2016) Tourism in Sweden 2015. The Swedish Agency for Economic and regional Growth. Stockholm: Ordförrådet AB.
- 52. Keefe L. M. (2018) # FakeMeat: How big a deal will animal meat analogs ultimately be?. Animal Frontiers, 8(3), 30–37.