Abstract
Using 2 years of home scanned data on household food purchases in France, we show how to infer the profile of average individual caloric intakes according to gender, age, and body mass index of household members. We also infer the individual consumption of macronutrients as carbohydrates, lipids or proteins. We then provide a descriptive analysis of eating in France over a long period of consumption that we compare to nutritional recommendations given by the French National Health and Nutrition Program. The results suggest that French people eat too much fats and proteins and not enough carbohydrates with respect to recommendations. They also show that obese or overweight individuals consume more calories at all ages and their consumption of fat is 20 % higher than normal individuals, meaning that public policies should aim at reducing fat consumption. We also find that the obesity of teenage boys cannot be explained by different food consumption as their dietary intake profiles are similar to other teenagers. Promoting physical activity for boys rather than public policies reducing food consumption could be more efficient.
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Notes
Source: OECD Health Data 2008.
The Body Mass Index (BMI) is the most commonly measure to assess whether an individual is obese or not. It corresponds to the weight divided by height squared and an individual is considered as obese if his BMI is larger than 30.
For examples: the Food Standard Agency in United Kingdom, the French National Health and Nutrition Program, the Centers for Disease Control and Prevention in the United States.
Other national surveys exist: the National Health and Nutrition Examination Survey in the US for example. This survey collects the information over a 24-h dietary recall (CDC 2012).
We removed 2,711 households that stopped participating in the survey at the end of 2001 and dropped 3,126 households because of missing information on age, gender, height, or weight for some individuals in the household. We finally used information of 4,166 households on the 2-year period that represent 11,237 individuals. This reduced sample has approximately the same characteristics than the initial one in terms of observables and thus attrition or missing values seem not systematically related to observable characteristics.
The different sources that allow us to build the dataset are: the Regal Micro Table, Cohen and Sérog (2004), nutritional web sites (www.i-dietetique.com, www.tabledescalories.com \(\ldots \)) and food industry companies web sites (Picard, Carrefour, Telemarket, Unifrais, Bridelice, Andros, Florette, Bonduelle, McCain, Nestlé, Avico).
We observe food purchases for products with bar codes and meat and fish without bar codes for 60 % of the sample, for products with bar codes and fruits and vegetables without bar codes for 38 % of the sample and only for products with bar codes for 2 % of the sample.
The obesity rates are not significantly different at 1 % level.
Note that a constant term \(\beta _{0}\) can be added to the previous specification and interpreted as a waste. Empirically, we will prefer the previous specification except for the disaggregation of lipids where it matters for fats used for cooking. The constant is then associated with the presence of a woman in a household.
Note that in our data the average size of these classes of individuals with the same age, gender, and obesity status is 10. Moreover, only 3.4 % of the individuals belong to a class with no other individuals.
Minimizing the sum of squared differences between the estimated consumption and the observed consumption for household with one individual, we find that the optimal penalization parameter is \(\lambda =500.\)
In appendix, Fig. 4 presents individual calories consumption with 95 % confidence intervals.
Using more information as provided by the data on household and individual characteristics (such as household income, region of residence, employment category for each household member, type of residence, town size) could be interesting but is left for future research. Here, we assume that conditional on gender, age, and BMI, these other characteristics either do not matter much or are not correlated with the current characteristics used.
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Acknowledgments
This paper is part of the “Politiques Nutritionnelles, Régulation des Filières Alimentaires et Consommation” (POLNUTRITION) project funded by the French National Program of Research, Grant Agreement No. ANR-05-PNRA-012. We thank Namanjeet Ahluwalia, Andrew Chesher, Nicole Darmon, Catherine Esnouf, Rachel Griffith, Vincent Réquillart, François-Charles Wolff for useful comments. We also thank the editor and two anonymous referees for helpful comments. All remaining errors are ours.
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Appendix
Appendix
1.1 Imputation methodology
To overcome the problem of missing data in one of the categories without bar code, we implement a procedure of imputation at the household level.
As said above, let \(y_{it}^{k}\) be the household consumption for category \(k=1,2,3\) and let us define \(S_{it}^{k}\in \{0,1\}\) equal to 1 only if \(y_{it}^{k}\) is observed. With a large set of demographic variables \(W_{it}\), we define \(\omega _{it}^{k}=y_{it}^{k}-E\left( y_{it}^{k}|W_{it}\right) \). The conditional independence assumption (1) implies the mean independence of \(y_{it}^{k}\) given \(W_{it}\) with the observation of \(y_{it}^{k}:\)
However, taking into account household heterogeneity by conditioning on as many variables as possible will lead to a more difficult non-parametric identification of the conditional means \(E\left( y_{it}^{k}|W_{it},S_{it}^{k}=1\right) \) due to the lack of sufficient observations given the large dimension of \(W_{it}\).
But, one can also use the fact that (1) implies (Rosenbaum and Rubin 1983)
and thus
where \(P\left( S_{it}^{k}=1|W_{it}\right) \) is the propensity score of observing category \(k\). One advantage of such an implication is that we can then condition on a unidimensional variable, the propensity score, and thus solve the dimensionality problem of conditioning on a large set of variables.
Moreover, we can apply this to any conditional mean for intervals of the propensity score, conditional on some \(W_{it}^{\prime }\), because we have
where \(F_{P(W)|W^{\prime },S_{it}^{k}=0}\) denotes the conditional cumulative distribution function of the propensity score given \(W^{\prime }\) and \(S_{it}^{k}=0\).
We thus first estimate the propensity score \(P\left( S_{it}^{k}=1|W_{it}\right) \) and then impute the unobserved category \(k\) households consumption with propensity score \(p\) with the average observed household consumption of category \(k\) food products with the same propensity score.
The regressions allowing us to estimate the propensity score matching for observation of the “fruits and vegetables” or “meat and fish” categories are not presented for brevity, but were done using a probit model.
1.2 Other Tables and Graphs
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Bonnet, C., Dubois, P. & Orozco, V. Household food consumption, individual caloric intake and obesity in France. Empir Econ 46, 1143–1166 (2014). https://doi.org/10.1007/s00181-013-0698-1
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DOI: https://doi.org/10.1007/s00181-013-0698-1