status and sample indicator supports the statistical appropriateness of the pooling of samples. In Column 4, the estimate was little changed by inclusion of lifetime abstention status and a linear measure of age of onset of regular drinking, parental drinking problems, state beer taxes and per capital alcohol consumption when the respondent was 18, educational attainment, current marital status, current employment status, and presence of children under 13 in the respondent’s current household (OR 1.30, 95% c.i. 1.16 to 1.44, p< .0001) Effect estimates were similar for each age group (20–29, 30–34, 35–39, 40–44, and 45+) (Figure 2, and supplementary Table 4). The results were identical when age of onset was modeled as unordered age categories, (1.30, 95% c.i. 1.16 to 1.44, p< .0001), nearly identical for alcohol abuse (1.27, 95% ci 1.04 to 1.54, p = .017) and for alcohol dependence (1.27, 95% c.i. 1.11 to 1.45, p = .001) when these diagnoses were considered separately, and similar when we specified probit models rather than logits.
