Unmarried Cohabitation and Union Stability: The Cohabitation-diffusion-hypothesis Revisited

Unmarried Cohabitation and Union Stability: The Cohabitation-diffusion-hypothesis Revisited | Research Square window.SnipcartSettings = { analytics: { enabled: false } }; (function() { var accessVector = localStorage.getItem('access_vector') || ''; window.dataLayer = window.dataLayer || []; if (accessVector) { window.dataLayer.push({ user: { profile: { profileInfo: { snid: accessVector } } } }); } })(); (function(w,d,s,l,i){w[l]=w[l]||[];w[l].push({'gtm.start':new Date().getTime(),event:'gtm.js'});var f=d.getElementsByTagName(s)[0],j=d.createElement(s),dl=l!='dataLayer'?'&l='+l:'';j.async=true;j.src='https://www.googletagmanager.com/gtm.js?id='+i+dl;f.parentNode.insertBefore(j,f);})(window,document,'script','dataLayer','GTM-K279D39R'); Browse Preprints In Review Journals COVID-19 Preprints AJE Video Bytes Research Tools Research Promotion AJE Professional Editing AJE Rubriq About Preprint Platform In Review Editorial Policies Our Team Advisory Board Help Center Sign In Submit a Preprint Cite Share Download PDF Short Report Unmarried Cohabitation and Union Stability: The Cohabitation-diffusion-hypothesis Revisited Maike van Damme, Fernando Ruiz-Vallejo This is a preprint; it has not been peer reviewed by a journal. https://doi.org/ 10.21203/rs.3.rs-8213630/v1 This work is licensed under a CC BY 4.0 License Status: Posted Version 1 posted You are reading this latest preprint version Abstract We revisit the U-shape diffusion hypothesis of Liefbroer and Dourleijn (2006) by replicating the impact of cohabitation diffusion on union dissolution in different union cohorts in ‘European’ contexts, the USA, and Canada. The impact of cohabitation diffusion on union dissolution is expected to take the form of a U-shaped relationship because of selection effects into cohabitation of ‘separation tolerant’ couples in low cohabitation contexts, or selection into marriage of ‘conventional’ couples in high cohabitation contexts. Where Liefbroer and Dourleijn studied data from three birth cohorts from 1953–1967, we use data from women in the Harmonized Histories (HH) of 21 countries and 14 (5-year) birth cohorts (1930/34–1995/99). We perform multilevel discrete time event history analyses on the pooled countries data and we check to what extent the variation in the ‘cohabitation effect’ can be explained by the percentage and percentage squared of the cohabitation rate in country-birth cohorts. Our findings indicate a U-shaped relationship between the cohabitation rate and the relative risk of union dissolution of cohabiting couples, with prior cohabiting, currently married couples having a risk of separation lower than married couples. Implications of our findings are that future research should not neglect the role of selection. Figures Figure 1 Figure 2 1. Introduction The Second Demographic Transition (SDT) predicted -among other trends- an increase in cohabitation rates due to corresponding changes towards more tolerant and individualized attitudes and a decrease in stigma with respect to cohabitation. Moreover, the SDT did not only predict higher cohabitation rates in more and more countries globally, but also higher dissolution rates (Lesthaeghe, 2014 ; Lesthaeghe & Van de Kaa, 1986 ). In addition, many studies point at the higher risk of union dissolution of cohabitors compared to married people (Hiekel & Wagner, 2020 ; Liefbroer & Dourleijn, 2006; Lyngstad & Jalovaara, 2010 ; Smock, 2000 ). Yet, these differences in union stability between cohabitating and married individuals vary significantly between contexts and seem to depend upon the diffusion of cohabitation in the context couples live in (Kiernan, 2002 ; Liefbroer & Dourleijn, 2006). This impact of cohabitation diffusion on union dissolution would take the form of a U-shaped relationship with former cohabitors having a higher separation rate than formerly married couples only in contexts in which cohabitation is a rare phenomenon (due to selection into cohabitation of ‘separation tolerant’ and less committed couples) or occurs amongst the majority of couples (due to selection into marriage of ‘conventional’ couples). In this paper, we revisit this U-shape diffusion hypothesis by replicating the impact of cohabitation diffusion on union dissolution of cohabitors in the context of different regions and birth cohorts in ‘European’ contexts, the USA, and Canada, using the most recently available data on retrospective family histories (The Harmonized Histories (HH) from the Generations and Gender Programme (GGP)). 2. Theoretical background The most commonly used theory formulating expectations about the differences in union dissolution rates between cohabiting couples and married couples is the ‘trial marriage’ theory. This theoretical approach assumes that as cohabiting unions progress, more and more information is gathered about the partner and good quality relationships will then convert into marriages, whereas the poor-quality ones will break up. Such ‘weeding’ of cohabiting unions may as such result in a particular selection of couples into cohabiting couples (those that have a short duration as they have relatively high break up rates), premarital cohabitors (with a long duration once they are converted into marriages) or direct married couples (those with a shorter duration as there was no ‘trial period’) (Boyle & Kulu, 2006 ; Cherlin, 1992 ; Liefbroer & Dourleijn, 2006). However, empirical findings on this ‘trial marriage’ theory are mixed. Where Boyle and Kulu ( 2006 ) found a confirmation of the ‘weeding’ hypothesis after controlling for various observed and unobserved characteristics, Liefbroer and Dourleijn (2006) found that, next to those who were cohabiting throughout, premarital cohabitors also have higher break up rates than the directly married couples. This selection of couples into more break up prone or less break up prone is suggested to have to do with the extent of diffusion of cohabitation in a certain context. Liefbroer and Dourleijn (2006) have shown that there is a U-shaped relationship between the cohabitation rate in a context and the impact of cohabitation on union dissolution. They suggest that cohabiting couples in a context with low cohabitation diffusion are more likely to be the ones with unconventional values and attitudes, have weaker commitment to marriage, and may be the ones with socioeconomic and personality characteristics linked to an increased separation risk (Liefbroer and Dourleijn 2006). Couples that directly marry in a context with much cohabitation diffusion, on the other hand, might be very particular in their turn. These might be selective couples that may be the ‘laggards’ in the cohabitation diffusion process and such a minority may consist, for instance, of religious fundamentalists (e.g. reformed Protestants) who view marriage as sacrosanct and as such are very conventional with low tolerance of divorce (Liefbroer and Dourleijn 2006). Thus, both in a context where cohabitation hardly takes place, and in a context where there is ample cohabitation, there will be selectivity of couples. In the first instance, the small minority will consist of divorce tolerant, less committed, cohabiting couples, and in the latter instance, the small minority are conventional couples that directly marry. More specifically, the differences in separation risk should be smallest when about 50% of the population in union experienced cohabitation (Liefbroer and Dourleijn 2006). In this paper, we replicate and update the study of Liefbroer and Dourleijn (2006) for 21 countries and 14 birth cohorts, using more recent data. Our hypothesis is thus formulated as follows: We expect to find that in the contexts where cohabitation rates are either low or high, union dissolution rates among cohabitors are the highest (U-shape relationship) ( Hypothesis 1 ) 3. Data and method We use data from the Harmonized Histories (HH) from the Generations and Gender Programme (GGP) (USA, Austria, Belgium, Bulgaria, Belarus, Canada, Czech Republic, Estonia, France, Georgia, Germany, Italy, Lithuania, the Netherlands, Norway, Poland, Romania, the Russian Federation, Spain, Sweden and the United Kingdom) (Koops et al., 2022 ; Perelli-Harris et al., 2010 ; Schumann et al., 2024 ). We did not analyse the Hungarian data as the variable on migrant background is not asked there. Our analytical sample entails women aged between 15 and 87 years, who were at some moment in a union (period (1950–2019)). We will compare thirteen 5-year birth cohorts, varying from 1 "1930/34" until 13 "1994/99". The Dependent Variable is dissolution of either marriage or cohabitation (divorced or separated) of (initially) first union only, widow(er)s are excluded at the time of partner’s death). The main Independent Variable is the percentage of cohabitation in the different regions and birth cohorts. Regarding the control variables, we include data on age at union formation (and its square), whether the woman has at least one child, being a native, education, and whether the woman’s parents have been divorced. These are covariates that have been shown to be important predictors of union dissolution (Cherlin, 1992 ; Liefbroer & Dourleijn, 2006; Lyngstad & Jalovaara, 2010 ). Our methodological approach entails first a descriptive picture of cohabitation and union dissolution rates in the different country-cohort contexts. This gives us an idea of the variation in the ‘cohabitation effect’. Secondly, we pool all countries together and perform a multilevel discrete time event history analysis on these pooled data, with country ( u 0j ) and birth cohort ( v 0j ) as random intercepts and the type of union as random slopes by both country ( u 2j ) and birth cohort ( v 2j ) (covariance between random intercept and random slopes is set at exchangeability) (Snijders & Bosker, 2012 ). We include the cohabitation rate and cohabitation rate squared to assess a curvilinear effect of cohabitation diffusion interacted with the type of union (just like Liefbroer and Dourleijn 2006). Note that our model is more complex than that of Liefbroer and Dourleijn, who had included all significant interactions of countries and birth cohorts with type of union and did not perform a multilevel model, but a country fixed effects model. We believe, however, that the resulting curvilinear effect in that case is what remains of the country and birth cohort differences that are not included in the model. See the following formula for the estimation of our pooled multi-level discrete time event history model: 4. Results 4.1. Descriptive analyses Our descriptive findings in Table 1 indeed indicate a large variation in the ‘cohabitation effect’ between the different country contexts. Georgia has the lowest influence of cohabitation on separation, whereas in Sweden the largest influence is found. Also note the high union dissolution risk in general in the USA. We can thus continue with the explanation of the variation in this ‘cohabitation effect’. Table 1 Percentage of couples having broken up after five years of union, by type of union. Percentages per country. country cohabiting former cohabiting directly married 401. Austria GGS wave1 0.29 0.04 0.09 1001. Bulgaria GGS wave1 0.07 0.01 0.02 1121. Belarus GGS wave 1 0.14 0.03 0.03 1241. Canada GSS 2006/11 0.24 0.05 0.04 2031. Czech Republic GGSI/GGSII 0.24 0.04 0.04 2081. Denmark 0.21 0.01 0.00 2331. Estonia GGS wave/GGSII 0.23 0.07 0.06 2501. France GGS wave1 0.18 0.02 0.03 2681. Georgia GGS wave1 0.05 0.01 0.03 2761. Germany GGS wave 1/PAIRFAM 0.30 0.03 0.01 3801. Italy GGS wave 1/ Fss 2016 0.22 0.00 0.01 4401. Lithuania GGS wave1 0.30 0.03 0.04 5281. Netherlands FFS/OG 0.26 0.00 0.05 5781. Norway GGS wave 1/GGSII 0.22 0.03 0.04 6162. Poland GGS wave1 0.16 0.02 0.02 6421. Romania GGS wave1 0.16 0.02 0.02 6431. Russia GGS wave1 0.26 0.09 0.07 7241. Spain SFS2006/18 0.20 0.02 0.00 7521. Sweden GGS wave 1 0.43 0.02 0.01 8261. UK BHPS 0.27 0.03 0.03 8401. USA NSFG1995/2007 0.50 0.11 0.13 In Fig. 1 , we present the cohabitation diffusion over the different countries (averaged over the 5-year birth cohorts). We see that there is ample variation in the cohabitation rate between around 90% in Austria and Denmark (but note that these data only consist of young birth cohorts (> 1960)) to around 25% in Romania. 4.2. Explanatory analyses In our following analyses we pool all country-birth cohort contexts and include the cohabitation rate and its square, while including random intercepts for country and birth cohort, as well as random slopes for type of union for both country and birth cohort (i.e. a cross-classified model). As expected, we find a U-shaped relationship between the cohabitation rate and the relative risk of union dissolution of cohabiting couples (see Fig. 2 for the calculated relative risks by cohabitation diffusion). The corresponding Table S1 is presented in the Supplementary Material. The random slopes of type of union means that the variation around the logit of the difference between cohabiting and directly married couples is 0.40 on the country level and 0.13 on the birth cohort level. This implies that the logit coefficient varies between 0.38 and 1.64 on the country level with an average of 1.016 and between 0.65 and 1.38 on the birth cohort level, with the same average logit of 1.016. The interpretation of Fig. 2 means that in contexts where cohabitation is rare, the impact of cohabiting on the separation risk is high, whereas also in contexts where direct marriage is rare, the difference in break up risk between cohabiting and direct marriage couples is larger. The minimum of the U-shaped relationship is at around 40%, implying that the difference in union dissolution risk between cohabiting and married couples is the smallest at this rate of cohabitation. These results are thus in line with what Liefbroer and Dourleijn (2006) found, who included all significant interactions of birth cohorts and countries with type of union in a country fixed effects model, although they found a minimum of the U-shaped relationship at 50%. This difference in minimum compared to Liefbroer and Dourleijn (2006) can be due to at least two reasons: 1) we used more recent data and more birth cohorts, covering a longer time span; 2) our approach is slightly more adequate compared to the country fixed effects model of Liefbroer and Dourleijn as we take with our multilevel model clustering of individuals in countries and birth cohorts into account. Furthermore, salient is that the difference between those couples that were prior cohabiting and then married versus those that directly married is negative. Prior cohabitors have a lower separation risk than the directly married. This is in line with the ‘weeding’ hypothesis that has been so frequently mentioned in the literature but has been difficult to prove (but see e.g. Boyle & Kulu, 2006 ; Hewitt & De Vaus, 2009 ; Manning & Cohen, 2012 ). Here we see that, once we take selection into cohabitation into account via the cohabitation diffusion hypothesis, we can identify the ‘weeding’ hypothesis with couples that are trialling a marriage via cohabitation having lower separation risks once they marry, whereas those that directly marry do not have this trial period and are thus experiencing higher union dissolution risks. 5. Conclusion In this article, we replicated the research by Liefbroer and Dourleijn (2006) and re-assessed the U-shaped relationship between the cohabitation rate on the one hand and the impact of cohabitation on union dissolution on the other hand. Via a multilevel discrete time, event history analysis with random intercepts and random slopes, we detected a U-shaped relationship between the cohabitation rate and the cohabitation effect. The minimum of the U-shape was at around 40% of cohabitation rate, contrary to the minimum around 50% found by Liefbroer and Dourleijn (2006). Implications of our findings are that in future research the role of selection should not be neglected. What is more is that we found that married couples who were previously cohabiting have lower separation risks than couples that directly married. This is in line with the theoretical ‘weeding’ mechanism, that has been so frequently laid out in the literature. Hence, both the selection hypothesis and the ‘weeding’ hypothesis seem to play a role. Future studies should thus at least be aware of sufficiently control for various characteristics that take away (part of) the selection problem when comparing the dissolution risk of cohabiting couples with married ones. Declarations Author Contribution Author 1 formulated the research idea, hypotheses, and objectives. She performed the analyses, and wrote the manuscript. Author 2 read various versions of the manuscript. Acknowledgement Maike van Damme and Fernando Ruiz-Vallejo thank the Faculty of Social and Human Sciences, Universidad Externado de Colombia, for supporting the research through project No. 1601160330600102. Data Availability The data of the Harmonized Histories can be accessed after registration viahttps://www.ggp-i.org/data/harmonized-histories/#toc1 References Boyle, P. J., & Kulu, H. (2006). Does cohabitation prior to marriage raise the risk of marital dissolution and does this effect vary geographically? (MPIDR Working Papers, Issue. Cherlin, A. (1992). Marriage, divorce, remarriage . Harvard University Press. Hewitt, B., & De Vaus, D. (2009). Change in the association between premarital cohabitation and separation, Australia 1945–2000. Journal of Marriage and Family , 71 (2), 353–361. https://doi.org/https://doi.org/10.1111/j.1741-3737.2009.00604.x Hiekel, N., & Wagner, M. (2020). Individualized relationship practices and union dissolution: Differences between marriage and cohabitation . European Sociological Review. Kiernan, K. E. (2002). Cohabitation in Western Europe: Trends, issues, and implications. In A. Booth (Ed.), Just Living Together: Implications of Cohabitation on Families, Children, and Social Policy . http://www.ewidgetsonline.net/dxreader/Reader.aspx?token=N9ytIXNcuxyXIbRcI5BPaA%3d%3d&rand=1369725560&buyNowLink=&page=&chapter =. Koops, J. C., Kubisch, K., Beaupré, P., Cabella, W., Fernández Soto, M., Fostik, A., Mogi, R., Nathan, M., Pardo, I., Pedetti, G., & Simon, S. (2022). Harmonized Histories I. Generations and Gender Programme. Lesthaeghe, R. (2014). The second demographic transition: A concise overview of its development. Proceedings of the National Academy of Sciences, 111 (51), 18112–18115. https://doi.org/10.1073/pnas.1420441111 Lesthaeghe, R., & Van de Kaa, D. J. (1986). Twee demografische transities? (Two demographic transitions?). In Van de D. J. Kaa, & R. Lesthaeghe (Eds.), Bevolking: Groei en krimp (Population: Growth and decline) (pp. 9–24). Van Loghum Slaterus. Liefbroer, A. C., & Dourleijn, E. (2006). Unmarried cohabitation and union stability:Testing the role of diffusion using data from 16 European countries. Demography, 43 (2), 203–221. http://proquest.umi.com/pqdweb?index=2&sid=1&srchmode=1&vinst=PROD&fmt=6&startpage=-1&clientid=38742&vname=PQD&RQT=309&did=1084442781&scaling=FULL&ts=1198143177&vtype=PQD&rqt=309&TS=1198143183&clientId=38742 Lyngstad, T. H., & Jalovaara, M. (2010). A review of the antecedents of union dissolution. Demographic Research, 23 (10), 257–292. http://www.demographic-research.org/volumes/vol23/10/23-10.pdf Manning, W. D., & Cohen, J. A. (2012). Premarital cohabitation and marital dissolution: An examination of recent marriages. Journal of Marriage and Family , 74 (2), 377–387. https://doi.org/https://doi.org/10.1111/j.1741-3737.2012.00960.x Perelli-Harris, B., Kreyenfeld, M., & Kubisch, K. (2010). Technical manual for the Harmonized Histories database. (Rostock, MPIDR Working paper 2010-011, Issue. Schumann, A., Allegra, S. F., & Meli, E. (2024). Harmonized Histories II . Generations and Gender Programme. Smock, P. (2000). Cohabitation in the United States: An appraisal of research themes, findings, and implications. Annual Review of Sociology , 26 , 1. http://www.jstor.org/stable/223434 Snijders, T., & Bosker, R. (2012). Multilevel analysis: An introduction to basic and advanced multilevel modeling . Los Angeles. SAGE. Additional Declarations No competing interests reported. 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17:01:27","extension":"html","order_by":10,"title":"","display":"","copyAsset":false,"role":"acdc-reference","size":50783,"visible":true,"origin":"","legend":"","description":"","filename":"earlyproof.html","url":"https://assets-eu.researchsquare.com/files/rs-8213630/v1/630e280d7f661cb07dec7240.html"},{"id":98819069,"identity":"4afa75d7-17a7-477d-a023-fef70d3a5dee","added_by":"auto","created_at":"2025-12-22 17:01:27","extension":"png","order_by":1,"title":"Figure 1","display":"","copyAsset":false,"role":"figure","size":32924,"visible":true,"origin":"","legend":"\u003cp\u003e\u003cem\u003ePercentage (%) cohabiting first union in 21 countries, percentages averaged over five-year birth cohorts per country\u003c/em\u003e\u003c/p\u003e","description":"","filename":"1.png","url":"https://assets-eu.researchsquare.com/files/rs-8213630/v1/e570bb499da2c9d849eee670.png"},{"id":98819070,"identity":"2c050582-b21c-4c37-8ae9-e420a263412b","added_by":"auto","created_at":"2025-12-22 17:01:27","extension":"png","order_by":2,"title":"Figure 2","display":"","copyAsset":false,"role":"figure","size":46537,"visible":true,"origin":"","legend":"\u003cp\u003e\u003cem\u003eRelative risk of union dissolution of cohabitors and former cohabitors compared with women who marry without prior cohabitation, by the incidence of unmarried cohabitation in the context. 21 countries, 252 birth cohorts\u003c/em\u003e\u003c/p\u003e","description":"","filename":"2.png","url":"https://assets-eu.researchsquare.com/files/rs-8213630/v1/b87ce74f0281df6ddba35593.png"},{"id":99322144,"identity":"cc2d8a87-4dc5-48a8-ae7d-b2d1a609e97f","added_by":"auto","created_at":"2025-12-31 16:43:01","extension":"pdf","order_by":0,"title":"","display":"","copyAsset":false,"role":"manuscript-pdf","size":631179,"visible":true,"origin":"","legend":"","description":"","filename":"manuscript.pdf","url":"https://assets-eu.researchsquare.com/files/rs-8213630/v1/591be04e-7065-43ce-89b0-e5b467ea4d9b.pdf"},{"id":99307371,"identity":"eed4716f-519a-4cb9-a391-8d9af0b02c94","added_by":"auto","created_at":"2025-12-31 16:06:05","extension":"docx","order_by":0,"title":"","display":"","copyAsset":false,"role":"supplement","size":15386,"visible":true,"origin":"","legend":"","description":"","filename":"CohabitationdiffusionhyprevisitedSMEJP.docx","url":"https://assets-eu.researchsquare.com/files/rs-8213630/v1/96315119974430348c3c867a.docx"}],"financialInterests":"No competing interests reported.","formattedTitle":"\u003cp\u003eUnmarried Cohabitation and Union Stability: The Cohabitation-diffusion-hypothesis Revisited\u003c/p\u003e","fulltext":[{"header":"1. Introduction","content":"\u003cp\u003eThe Second Demographic Transition (SDT) predicted -among other trends- an increase in cohabitation rates due to corresponding changes towards more tolerant and individualized attitudes and a decrease in stigma with respect to cohabitation. Moreover, the SDT did not only predict higher cohabitation rates in more and more countries globally, but also higher dissolution rates (Lesthaeghe, \u003cspan citationid=\"CR7\" class=\"CitationRef\"\u003e2014\u003c/span\u003e; Lesthaeghe \u0026amp; Van de Kaa, \u003cspan citationid=\"CR8\" class=\"CitationRef\"\u003e1986\u003c/span\u003e). In addition, many studies point at the higher risk of union dissolution of cohabitors compared to married people (Hiekel \u0026amp; Wagner, \u003cspan citationid=\"CR4\" class=\"CitationRef\"\u003e2020\u003c/span\u003e; Liefbroer \u0026amp; Dourleijn, 2006; Lyngstad \u0026amp; Jalovaara, \u003cspan citationid=\"CR10\" class=\"CitationRef\"\u003e2010\u003c/span\u003e; Smock, \u003cspan citationid=\"CR14\" class=\"CitationRef\"\u003e2000\u003c/span\u003e). Yet, these differences in union stability between cohabitating and married individuals vary significantly between contexts and seem to depend upon the diffusion of cohabitation in the context couples live in (Kiernan, \u003cspan citationid=\"CR5\" class=\"CitationRef\"\u003e2002\u003c/span\u003e; Liefbroer \u0026amp; Dourleijn, 2006). This impact of cohabitation diffusion on union dissolution would take the form of a U-shaped relationship with former cohabitors having a higher separation rate than formerly married couples only in contexts in which cohabitation is a rare phenomenon (due to selection into cohabitation of \u0026lsquo;separation tolerant\u0026rsquo; and less committed couples) or occurs amongst the majority of couples (due to selection into marriage of \u0026lsquo;conventional\u0026rsquo; couples).\u003c/p\u003e \u003cp\u003eIn this paper, \u003cb\u003ewe revisit this U-shape diffusion hypothesis\u003c/b\u003e by replicating the impact of cohabitation diffusion on union dissolution of cohabitors in the context of different regions and birth cohorts in \u0026lsquo;European\u0026rsquo; contexts, the USA, and Canada, using the most recently available data on retrospective family histories (The \u003cem\u003eHarmonized Histories\u003c/em\u003e (HH) from the \u003cem\u003eGenerations and Gender Programme\u003c/em\u003e (GGP)).\u003c/p\u003e"},{"header":"2. Theoretical background","content":"\u003cp\u003eThe most commonly used theory formulating expectations about the differences in union dissolution rates between cohabiting couples and married couples is the \u0026lsquo;trial marriage\u0026rsquo; theory. This theoretical approach assumes that as cohabiting unions progress, more and more information is gathered about the partner and good quality relationships will then convert into marriages, whereas the poor-quality ones will break up. Such \u0026lsquo;weeding\u0026rsquo; of cohabiting unions may as such result in a particular selection of couples into cohabiting couples (those that have a short duration as they have relatively high break up rates), premarital cohabitors (with a long duration once they are converted into marriages) or direct married couples (those with a shorter duration as there was no \u0026lsquo;trial period\u0026rsquo;) (Boyle \u0026amp; Kulu, \u003cspan citationid=\"CR1\" class=\"CitationRef\"\u003e2006\u003c/span\u003e; Cherlin, \u003cspan citationid=\"CR2\" class=\"CitationRef\"\u003e1992\u003c/span\u003e; Liefbroer \u0026amp; Dourleijn, 2006). However, empirical findings on this \u0026lsquo;trial marriage\u0026rsquo; theory are mixed. Where Boyle and Kulu (\u003cspan citationid=\"CR1\" class=\"CitationRef\"\u003e2006\u003c/span\u003e) found a confirmation of the \u0026lsquo;weeding\u0026rsquo; hypothesis after controlling for various observed and unobserved characteristics, Liefbroer and Dourleijn (2006) found that, next to those who were cohabiting throughout, premarital cohabitors also have higher break up rates than the directly married couples. This selection of couples into more break up prone or less break up prone is suggested to have to do with the extent of diffusion of cohabitation in a certain context. Liefbroer and Dourleijn (2006) have shown that there is a U-shaped relationship between the cohabitation rate in a context and the impact of cohabitation on union dissolution. They suggest that cohabiting couples in a context with low cohabitation diffusion are more likely to be the ones with unconventional values and attitudes, have weaker commitment to marriage, and may be the ones with socioeconomic and personality characteristics linked to an increased separation risk (Liefbroer and Dourleijn 2006). Couples that directly marry in a context with much cohabitation diffusion, on the other hand, might be very particular in their turn. These might be selective couples that may be the \u0026lsquo;laggards\u0026rsquo; in the cohabitation diffusion process and such a minority may consist, for instance, of religious fundamentalists (e.g. reformed Protestants) who view marriage as sacrosanct and as such are very conventional with low tolerance of divorce (Liefbroer and Dourleijn 2006). Thus, both in a context where cohabitation hardly takes place, and in a context where there is ample cohabitation, there will be selectivity of couples. In the first instance, the small minority will consist of divorce tolerant, less committed, cohabiting couples, and in the latter instance, the small minority are conventional couples that directly marry. More specifically, the differences in separation risk should be smallest when about 50% of the population in union experienced cohabitation (Liefbroer and Dourleijn 2006).\u003c/p\u003e \u003cp\u003eIn this paper, we replicate and update the study of Liefbroer and Dourleijn (2006) for 21 countries and 14 birth cohorts, using more recent data. Our hypothesis is thus formulated as follows:\u003c/p\u003e \u003cp\u003e \u003cb\u003eWe expect to find that in the contexts where cohabitation rates are either low or high, union dissolution rates among cohabitors are the highest (U-shape relationship)\u003c/b\u003e (\u003cem\u003eHypothesis 1\u003c/em\u003e)\u003c/p\u003e"},{"header":"3. Data and method","content":"\u003cp\u003eWe use data from the \u003cem\u003eHarmonized Histories\u003c/em\u003e (HH) from the \u003cstrong\u003eGenerations and Gender Programme (GGP)\u003c/strong\u003e (USA, Austria, Belgium, Bulgaria, Belarus, Canada, Czech Republic, Estonia, France, Georgia, Germany, Italy, Lithuania, the Netherlands, Norway, Poland, Romania, the Russian Federation, Spain, Sweden and the United Kingdom) (Koops et al., \u003cspan class=\"CitationRef\"\u003e2022\u003c/span\u003e; Perelli-Harris et al., \u003cspan class=\"CitationRef\"\u003e2010\u003c/span\u003e; Schumann et al., \u003cspan class=\"CitationRef\"\u003e2024\u003c/span\u003e). We did not analyse the Hungarian data as the variable on migrant background is not asked there. Our analytical sample entails women aged between 15 and 87 years, who were at some moment in a union (period (1950\u0026ndash;2019)). We will compare thirteen 5-year birth cohorts, varying from 1 \u0026quot;1930/34\u0026quot; until 13 \u0026quot;1994/99\u0026quot;.\u003c/p\u003e\n\u003cp\u003eThe Dependent Variable is dissolution of either marriage or cohabitation (divorced or separated) of (initially) first union only, widow(er)s are excluded at the time of partner\u0026rsquo;s death).\u003c/p\u003e\n\u003cp\u003eThe main Independent Variable is the percentage of cohabitation in the different regions and birth cohorts.\u003c/p\u003e\n\u003cp\u003eRegarding the control variables, we include data on age at union formation (and its square), whether the woman has at least one child, being a native, education, and whether the woman\u0026rsquo;s parents have been divorced. These are covariates that have been shown to be important predictors of union dissolution (Cherlin, \u003cspan class=\"CitationRef\"\u003e1992\u003c/span\u003e; Liefbroer \u0026amp; Dourleijn, 2006; Lyngstad \u0026amp; Jalovaara, \u003cspan class=\"CitationRef\"\u003e2010\u003c/span\u003e).\u003c/p\u003e\n\u003cp\u003eOur methodological approach entails first a descriptive picture of cohabitation and union dissolution rates in the different country-cohort contexts. This gives us an idea of the variation in the \u0026lsquo;cohabitation effect\u0026rsquo;. Secondly, we pool all countries together and perform a multilevel discrete time event history analysis on these pooled data, with country (\u003cem\u003eu\u003c/em\u003e\u003csub\u003e\u003cem\u003e0j\u003c/em\u003e\u003c/sub\u003e) and birth cohort (\u003cem\u003ev\u003c/em\u003e\u003csub\u003e\u003cem\u003e0j\u003c/em\u003e\u003c/sub\u003e) as random intercepts and the type of union as random slopes by both country (\u003cem\u003eu\u003c/em\u003e\u003csub\u003e\u003cem\u003e2j\u003c/em\u003e\u003c/sub\u003e) and birth cohort (\u003cem\u003ev\u003c/em\u003e\u003csub\u003e\u003cem\u003e2j\u003c/em\u003e\u003c/sub\u003e) (covariance between random intercept and random slopes is set at exchangeability) (Snijders \u0026amp; Bosker, \u003cspan class=\"CitationRef\"\u003e2012\u003c/span\u003e). We include the cohabitation rate and cohabitation rate squared to assess a curvilinear effect of cohabitation diffusion interacted with the type of union (just like Liefbroer and Dourleijn 2006). Note that our model is more complex than that of Liefbroer and Dourleijn, who had included all significant interactions of countries and birth cohorts with type of union and did not perform a multilevel model, but a country fixed effects model. We believe, however, that the resulting curvilinear effect in that case is what remains of the country and birth cohort differences that are not included in the model. See the following formula for the estimation of our pooled multi-level discrete time event history model:\u003c/p\u003e\n\u003cp\u003e\u003cimg 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\"\u003e\u003c/p\u003e"},{"header":"4. Results","content":"\u003cdiv id=\"Sec5\" class=\"Section2\"\u003e \u003ch2\u003e4.1. Descriptive analyses\u003c/h2\u003e \u003cp\u003eOur descriptive findings in Table\u0026nbsp;\u003cspan refid=\"Tab1\" class=\"InternalRef\"\u003e1\u003c/span\u003e indeed indicate a large variation in the \u0026lsquo;cohabitation effect\u0026rsquo; between the different country contexts. Georgia has the lowest influence of cohabitation on separation, whereas in Sweden the largest influence is found. Also note the high union dissolution risk in general in the USA. We can thus continue with the explanation of the variation in this \u0026lsquo;cohabitation effect\u0026rsquo;.\u003c/p\u003e \u003cp\u003e \u003cdiv class=\"gridtable\"\u003e\u003ctable float=\"Yes\" id=\"Tab1\" border=\"1\"\u003e \u003ccaption language=\"En\"\u003e \u003cdiv class=\"CaptionNumber\"\u003eTable 1\u003c/div\u003e \u003cdiv class=\"CaptionContent\"\u003e \u003cp\u003ePercentage of couples having broken up after five years of union, by type of union. Percentages per country.\u003c/p\u003e \u003c/div\u003e \u003c/caption\u003e \u003ccolgroup cols=\"4\"\u003e \u003cdiv align=\"left\" class=\"colspec\" colname=\"c1\" colnum=\"1\"\u003e\u003c/div\u003e \u003cdiv align=\"char\" char=\".\" class=\"colspec\" colname=\"c2\" colnum=\"2\"\u003e\u003c/div\u003e \u003cdiv align=\"char\" char=\".\" class=\"colspec\" colname=\"c3\" colnum=\"3\"\u003e\u003c/div\u003e \u003cdiv align=\"char\" char=\".\" class=\"colspec\" colname=\"c4\" colnum=\"4\"\u003e\u003c/div\u003e \u003cthead\u003e \u003ctr\u003e \u003cth align=\"left\" colname=\"c1\"\u003e \u003cp\u003ecountry\u003c/p\u003e \u003c/th\u003e \u003cth align=\"left\" colname=\"c2\"\u003e \u003cp\u003ecohabiting\u003c/p\u003e \u003c/th\u003e \u003cth align=\"left\" colname=\"c3\"\u003e \u003cp\u003eformer cohabiting\u003c/p\u003e \u003c/th\u003e \u003cth align=\"left\" colname=\"c4\"\u003e \u003cp\u003edirectly married\u003c/p\u003e \u003c/th\u003e \u003c/tr\u003e \u003c/thead\u003e \u003ctbody\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e401. Austria GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.29\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.09\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e1001. Bulgaria GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.07\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e1121. Belarus GGS wave 1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.14\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e1241. Canada GSS 2006/11\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.24\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.05\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2031. Czech Republic GGSI/GGSII\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.24\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2081. Denmark\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.21\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.00\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2331. Estonia GGS wave/GGSII\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.23\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.07\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.06\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2501. France GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.18\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2681. Georgia GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.05\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e2761. Germany GGS wave 1/PAIRFAM\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.30\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e3801. Italy GGS wave 1/ Fss 2016\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.22\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.00\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e4401. Lithuania GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.30\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e5281. Netherlands FFS/OG\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.26\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.00\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.05\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e5781. Norway GGS wave 1/GGSII\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.22\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.04\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e6162. Poland GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.16\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e6421. Romania GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.16\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e6431. Russia GGS wave1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.26\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.09\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.07\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e7241. Spain SFS2006/18\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.20\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.00\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e7521. Sweden GGS wave 1\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.43\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.02\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.01\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e8261. UK BHPS\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.27\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.03\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003ctr\u003e \u003ctd align=\"left\" colname=\"c1\"\u003e \u003cp\u003e8401. USA NSFG1995/2007\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c2\"\u003e \u003cp\u003e0.50\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c3\"\u003e \u003cp\u003e0.11\u003c/p\u003e \u003c/td\u003e \u003ctd align=\"char\" char=\".\" colname=\"c4\"\u003e \u003cp\u003e0.13\u003c/p\u003e \u003c/td\u003e \u003c/tr\u003e \u003c/tbody\u003e \u003c/colgroup\u003e \u003c/table\u003e\u003c/div\u003e \u003c/p\u003e \u003cp\u003eIn Fig.\u0026nbsp;\u003cspan refid=\"Fig1\" class=\"InternalRef\"\u003e1\u003c/span\u003e, we present the cohabitation diffusion over the different countries (averaged over the 5-year birth cohorts). We see that there is ample variation in the cohabitation rate between around 90% in Austria and Denmark (but note that these data only consist of young birth cohorts (\u0026gt;\u0026thinsp;1960)) to around 25% in Romania.\u003c/p\u003e \u003cp\u003e \u003c/p\u003e \u003c/div\u003e \u003cdiv id=\"Sec6\" class=\"Section2\"\u003e \u003ch2\u003e4.2. Explanatory analyses\u003c/h2\u003e \u003cp\u003eIn our following analyses we pool all country-birth cohort contexts and include the cohabitation rate and its square, while including random intercepts for country and birth cohort, as well as random slopes for type of union for both country and birth cohort (i.e. a cross-classified model). As expected, we find a U-shaped relationship between the cohabitation rate and the relative risk of union dissolution of cohabiting couples (see Fig.\u0026nbsp;\u003cspan refid=\"Fig2\" class=\"InternalRef\"\u003e2\u003c/span\u003e for the calculated relative risks by cohabitation diffusion). The corresponding Table \u003cspan refid=\"MOESM1\" class=\"InternalRef\"\u003eS1\u003c/span\u003e is presented in the Supplementary Material. The random slopes of type of union means that the variation around the logit of the difference between cohabiting and directly married couples is 0.40 on the country level and 0.13 on the birth cohort level. This implies that the logit coefficient varies between 0.38 and 1.64 on the country level with an average of 1.016 and between 0.65 and 1.38 on the birth cohort level, with the same average logit of 1.016.\u003c/p\u003e \u003cp\u003eThe interpretation of Fig.\u0026nbsp;\u003cspan refid=\"Fig2\" class=\"InternalRef\"\u003e2\u003c/span\u003e means that in contexts where cohabitation is rare, the impact of cohabiting on the separation risk is high, whereas also in contexts where direct marriage is rare, the difference in break up risk between cohabiting and direct marriage couples is larger. The minimum of the U-shaped relationship is at around 40%, implying that the difference in union dissolution risk between cohabiting and married couples is the smallest at this rate of cohabitation. These results are thus in line with what Liefbroer and Dourleijn (2006) found, who included all significant interactions of birth cohorts and countries with type of union in a country fixed effects model, although they found a minimum of the U-shaped relationship at 50%. This difference in minimum compared to Liefbroer and Dourleijn (2006) can be due to at least two reasons: 1) we used more recent data and more birth cohorts, covering a longer time span; 2) our approach is slightly more adequate compared to the country fixed effects model of Liefbroer and Dourleijn as we take with our multilevel model clustering of individuals in countries and birth cohorts into account.\u003c/p\u003e \u003cp\u003eFurthermore, salient is that the difference between those couples that were prior cohabiting and then married versus those that directly married is negative. Prior cohabitors have a lower separation risk than the directly married. This is in line with the \u0026lsquo;weeding\u0026rsquo; hypothesis that has been so frequently mentioned in the literature but has been difficult to prove (but see e.g. Boyle \u0026amp; Kulu, \u003cspan citationid=\"CR1\" class=\"CitationRef\"\u003e2006\u003c/span\u003e; Hewitt \u0026amp; De Vaus, \u003cspan citationid=\"CR3\" class=\"CitationRef\"\u003e2009\u003c/span\u003e; Manning \u0026amp; Cohen, \u003cspan citationid=\"CR11\" class=\"CitationRef\"\u003e2012\u003c/span\u003e). Here we see that, once we take selection into cohabitation into account via the cohabitation diffusion hypothesis, we can identify the \u0026lsquo;weeding\u0026rsquo; hypothesis with couples that are trialling a marriage via cohabitation having lower separation risks once they marry, whereas those that directly marry do not have this trial period and are thus experiencing higher union dissolution risks.\u003c/p\u003e \u003cp\u003e \u003c/p\u003e \u003c/div\u003e"},{"header":"5. Conclusion","content":"\u003cp\u003eIn this article, we replicated the research by Liefbroer and Dourleijn (2006) and re-assessed the U-shaped relationship between the cohabitation rate on the one hand and the impact of cohabitation on union dissolution on the other hand. Via a multilevel discrete time, event history analysis with random intercepts and random slopes, we detected a U-shaped relationship between the cohabitation rate and the cohabitation effect. The minimum of the U-shape was at around 40% of cohabitation rate, contrary to the minimum around 50% found by Liefbroer and Dourleijn (2006).\u003c/p\u003e \u003cp\u003eImplications of our findings are that in future research the role of selection should not be neglected. What is more is that we found that married couples who were previously cohabiting have lower separation risks than couples that directly married. This is in line with the theoretical \u0026lsquo;weeding\u0026rsquo; mechanism, that has been so frequently laid out in the literature. Hence, both the selection hypothesis and the \u0026lsquo;weeding\u0026rsquo; hypothesis seem to play a role. Future studies should thus at least be aware of sufficiently control for various characteristics that take away (part of) the selection problem when comparing the dissolution risk of cohabiting couples with married ones.\u003c/p\u003e"},{"header":"Declarations","content":"\u003ch2\u003eAuthor Contribution\u003c/h2\u003e\u003cp\u003eAuthor 1 formulated the research idea, hypotheses, and objectives. She performed the analyses, and wrote the manuscript. Author 2 read various versions of the manuscript.\u003c/p\u003e\u003ch2\u003eAcknowledgement\u003c/h2\u003e\u003cp\u003eMaike van Damme and Fernando Ruiz-Vallejo thank the Faculty of Social and Human Sciences, Universidad Externado de Colombia, for supporting the research through project No. 1601160330600102.\u003c/p\u003e\u003ch2\u003eData Availability\u003c/h2\u003e\u003cp\u003eThe data of the Harmonized Histories can be accessed after registration viahttps://www.ggp-i.org/data/harmonized-histories/#toc1\u003c/p\u003e"},{"header":"References","content":"\u003col\u003e\u003cli\u003e\u003cspan\u003eBoyle, P. J., \u0026amp; Kulu, H. (2006). \u003cem\u003eDoes cohabitation prior to marriage raise the risk of marital dissolution and does this effect vary geographically?\u003c/em\u003e (MPIDR Working Papers, Issue.\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eCherlin, A. (1992). \u003cem\u003eMarriage, divorce, remarriage\u003c/em\u003e. Harvard University Press.\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eHewitt, B., \u0026amp; De Vaus, D. (2009). Change in the association between premarital cohabitation and separation, Australia 1945\u0026ndash;2000. \u003cem\u003eJournal of Marriage and Family\u003c/em\u003e, \u003cem\u003e71\u003c/em\u003e(2), 353\u0026ndash;361. \u003cspan class=\"ExternalRef\"\u003e\u003cspan class=\"RefSource\"\u003ehttps://doi.org/https://doi.org/10.1111/j.1741-3737.2009.00604.x\u003c/span\u003e\u003cspan address=\"10.1111/j.1741-3737.2009.00604.x\" targettype=\"DOI\" class=\"RefTarget\"\u003e\u003c/span\u003e\u003c/span\u003e\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eHiekel, N., \u0026amp; Wagner, M. (2020). \u003cem\u003eIndividualized relationship practices and union dissolution: Differences between marriage and cohabitation\u003c/em\u003e. European Sociological Review.\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eKiernan, K. E. (2002). 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C., \u0026amp; Dourleijn, E. (2006). Unmarried cohabitation and union stability:Testing the role of diffusion using data from 16 European countries. \u003cem\u003eDemography, 43\u003c/em\u003e(2), 203\u0026ndash;221. http://proquest.umi.com/pqdweb?index=2\u0026amp;sid=1\u0026amp;srchmode=1\u0026amp;vinst=PROD\u0026amp;fmt=6\u0026amp;startpage=-1\u0026amp;clientid=38742\u0026amp;vname=PQD\u0026amp;RQT=309\u0026amp;did=1084442781\u0026amp;scaling=FULL\u0026amp;ts=1198143177\u0026amp;vtype=PQD\u0026amp;rqt=309\u0026amp;TS=1198143183\u0026amp;clientId=38742\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eLyngstad, T. H., \u0026amp; Jalovaara, M. (2010). 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Premarital cohabitation and marital dissolution: An examination of recent marriages. \u003cem\u003eJournal of Marriage and Family\u003c/em\u003e, \u003cem\u003e74\u003c/em\u003e(2), 377\u0026ndash;387. \u003cspan class=\"ExternalRef\"\u003e\u003cspan class=\"RefSource\"\u003ehttps://doi.org/https://doi.org/10.1111/j.1741-3737.2012.00960.x\u003c/span\u003e\u003cspan address=\"10.1111/j.1741-3737.2012.00960.x\" targettype=\"DOI\" class=\"RefTarget\"\u003e\u003c/span\u003e\u003c/span\u003e\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003ePerelli-Harris, B., Kreyenfeld, M., \u0026amp; Kubisch, K. (2010). \u003cem\u003eTechnical manual for the Harmonized Histories database.\u003c/em\u003e (Rostock, MPIDR Working paper 2010-011, Issue.\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eSchumann, A., Allegra, S. F., \u0026amp; Meli, E. (2024). \u003cem\u003eHarmonized Histories II\u003c/em\u003e. Generations and Gender Programme.\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eSmock, P. (2000). Cohabitation in the United States: An appraisal of research themes, findings, and implications. \u003cem\u003eAnnual Review of Sociology\u003c/em\u003e, \u003cem\u003e26\u003c/em\u003e, 1. \u003cspan class=\"ExternalRef\"\u003e\u003cspan class=\"RefSource\"\u003ehttp://www.jstor.org/stable/223434\u003c/span\u003e\u003cspan address=\"http://www.jstor.org/stable/223434\" targettype=\"URL\" class=\"RefTarget\"\u003e\u003c/span\u003e\u003c/span\u003e\u003c/span\u003e\u003c/li\u003e \u003cli\u003e\u003cspan\u003eSnijders, T., \u0026amp; Bosker, R. (2012). \u003cem\u003eMultilevel analysis: An introduction to basic and advanced multilevel modeling\u003c/em\u003e. Los Angeles. SAGE.\u003c/span\u003e\u003c/li\u003e\u003c/ol\u003e"}],"fulltextSource":"","fullText":"","funders":[],"hasAdminPriorityOnWorkflow":false,"hasManuscriptDocX":true,"hasOptedInToPreprint":true,"hasPassedJournalQc":"","hasAnyPriority":false,"hideJournal":true,"highlight":"","institution":"","isAcceptedByJournal":false,"isAuthorSuppliedPdf":false,"isDeskRejected":"","isHiddenFromSearch":false,"isInQc":false,"isInWorkflow":false,"isPdf":false,"isPdfUpToDate":true,"isWithdrawnOrRetracted":false,"journal":{"display":true,"email":"[email protected]","identity":"researchsquare","isNatureJournal":false,"hasQc":true,"allowDirectSubmit":true,"externalIdentity":"","sideBox":"","snPcode":"","submissionUrl":"/submission","title":"Research Square","twitterHandle":"researchsquare","acdcEnabled":true,"dfaEnabled":false,"editorialSystem":"","reportingPortfolio":"","inReviewEnabled":false,"inReviewRevisionsEnabled":true},"keywords":"","lastPublishedDoi":"10.21203/rs.3.rs-8213630/v1","lastPublishedDoiUrl":"https://doi.org/10.21203/rs.3.rs-8213630/v1","license":{"name":"CC BY 4.0","url":"https://creativecommons.org/licenses/by/4.0/"},"manuscriptAbstract":"\u003cp\u003eWe revisit the U-shape diffusion hypothesis of Liefbroer and Dourleijn (2006) by replicating the impact of cohabitation diffusion on union dissolution in different union cohorts in \u0026lsquo;European\u0026rsquo; contexts, the USA, and Canada. The impact of cohabitation diffusion on union dissolution is expected to take the form of a U-shaped relationship because of selection effects into cohabitation of \u0026lsquo;separation tolerant\u0026rsquo; couples in low cohabitation contexts, or selection into marriage of \u0026lsquo;conventional\u0026rsquo; couples in high cohabitation contexts. Where Liefbroer and Dourleijn studied data from three birth cohorts from 1953\u0026ndash;1967, we use data from women in the Harmonized Histories (HH) of 21 countries and 14 (5-year) birth cohorts (1930/34\u0026ndash;1995/99). We perform multilevel discrete time event history analyses on the pooled countries data and we check to what extent the variation in the \u0026lsquo;cohabitation effect\u0026rsquo; can be explained by the percentage and percentage squared of the cohabitation rate in country-birth cohorts. Our findings indicate a U-shaped relationship between the cohabitation rate and the relative risk of union dissolution of cohabiting couples, with prior cohabiting, currently married couples having a risk of separation lower than married couples. Implications of our findings are that future research should not neglect the role of selection.\u003c/p\u003e","manuscriptTitle":"Unmarried Cohabitation and Union Stability: The Cohabitation-diffusion-hypothesis Revisited","msid":"","msnumber":"","nonDraftVersions":[{"code":1,"date":"2025-12-22 17:01:23","doi":"10.21203/rs.3.rs-8213630/v1","editorialEvents":[{"type":"communityComments","content":0}],"status":"published","journal":{"display":true,"email":"[email protected]","identity":"researchsquare","isNatureJournal":false,"hasQc":true,"allowDirectSubmit":true,"externalIdentity":"","sideBox":"","snPcode":"","submissionUrl":"/submission","title":"Research Square","twitterHandle":"researchsquare","acdcEnabled":true,"dfaEnabled":false,"editorialSystem":"","reportingPortfolio":"","inReviewEnabled":false,"inReviewRevisionsEnabled":true}}],"origin":"","ownerIdentity":"4a3cd996-542d-4899-ab20-efc85947f677","owner":[],"postedDate":"December 22nd, 2025","published":true,"recentEditorialEvents":[],"rejectedJournal":[],"revision":"","amendment":"","status":"posted","subjectAreas":[],"tags":[],"updatedAt":"2026-03-19T13:24:41+00:00","versionOfRecord":[],"versionCreatedAt":"2025-12-22 17:01:23","video":"","vorDoi":"","vorDoiUrl":"","workflowStages":[]},"version":"v1","identity":"rs-8213630","journalConfig":"researchsquare"},"__N_SSP":true},"page":"/article/[identity]/[[...version]]","query":{"redirect":"/article/rs-8213630","identity":"rs-8213630","version":["v1"]},"buildId":"8U1c8b4HqxoKbykW_rLl7","isFallback":false,"isExperimentalCompile":false,"dynamicIds":[84888],"gssp":true,"scriptLoader":[]}