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c i is a source cohort fixed effect.
Furthermore, two source-specific factors are considered: the average education level and the proportion of employed in the source cohort.
Finally, I build the diaspora ratios as the proportion of the size of the diaspora cohort to the size of the source cohort.
If the proportion of employed in a source cohort increases by 5.6 percentage points, the annual change in the diaspora ratio decreases by about 1 in the free movement scenario.
While no evidence is found that the average education level in the source has an impact on the dependent variable, the proportion of employed in the source cohort seems to negatively affect the annual change in the diaspora ratio.
For example, the education variable for the 15-24 year old EU-2 source cohort denotes the average education level of the 15-24 year old Bulgarians and Romanians together.
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Using weights provided by Eurostat, I then calculate the size of these nine diaspora cohorts and the size of the respective nine source cohorts.
We found 53 929 people aged 65 to 94 who were Group Health members as of 1 September in one of the study years, including 46 824 (87%) who met eligibility criteria on the basis of electronic data sources and thus made up the source cohorts.
The analysis included individuals with chronic or spontaneously cleared HCV infections from a multiple-source cohort (n = 389) and a single-source cohort (n = 71).
We next investigated the net host genetic contribution to spontaneous HCV clearance in the single-source cohort.
A previous study of an Irish HCV single-source cohort showed evidence of immune selection in known T cell targets.
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