(This is one part of an ongoing discussion of the 2018 OSR Survey results. See the table of contents at the bottom of this post for links to the other parts.)
Earlier, I reported the OSR ratings of various games (as in, level of agreement with the statement: I think the game ________ is OSR) and also which games respondents reported playing. As I noted in that post, these variables allowed me to score individual responses on degree of OSR play behavior. Respondents themselves, in aggregate, determined what OSR play behavior entails. In addition to being related to several other variables that you might expect (such as self-declared participation in the OSR, degree of identification with the OSR, and having bought an OSR product), degree of OSR play behavior also positively predicts blogging about tabletop roleplaying games generally and belief that the OSR welcomes diverse voices.
I came up with the idea of scoring respondents on OSR play behavior after designing the survey, so the set of games rated on OSR-ness differs slightly from the set of games respondents could indicate they were currently playing. However, there is a substantial overlap between the two sets. This set of overlapping games contributes to the OSR play behavior score. To create an OSR play score for each respondent, I calculated an average of play scores (playing = 1, not playing = missing value) weighted by game OSR rating, which ranges from 1 to 7. For example, a respondent that indicated playing Vampire: The Masquerade (OSR rating = 1.90) and B/X D&D (OSR rating = 6.14) would have an overall OSR play score of (1.90 + 6.14) / 2 = 4.02. One of the options for currently played games was Home-brew (OSR), which I decided should have an OSR game rating of 7. After all, what game could be more subjectively OSR than one the respondent categorized themselves as Home-brew (OSR)? I determined this scoring scheme prior to looking at any results.
1634 respondents reported currently playing some games for which I had OSR ratings, allowing me to score those responses on OSR play behavior. The mean rating of OSR play among these respondents was 4.41 (SD = 1.44, min = 1.75, max = 7). The distribution of this score was roughly uniform, though there were spikes around 2.87 (n = 198), which corresponds to respondents that reported only currently playing D&D 5E, around 4.93 (n = 64), which corresponds to respondents that reported playing D&D 5E + Home-brew (OSR), and around 7 (n = 96), which corresponds to respondents that reported only currently playing a Home-brew (OSR) game.
This composite play score is obviously imperfect, as respondents indicated play dichotomously rather than by degree, the set of games available to select was incomplete, and the measurement of game OSR-ness was itself imprecise (though derived empirically from the beliefs of respondents). However, the relevant question is whether the rating captures some meaningful variation in degree of OSR play behavior rather than whether it perfectly describes each respondent’s play behavior.
Within sample, the OSR play behavior score has some predictive validity. For example, OSR participants have higher OSR play behavior scores (t(1630) = -18.13, p < .001, MOSR = 4.68, Mnon-OSR = 3.26, using a two-sample t test with unequal variances). Looking at the same relationship another way, I regressed the OSR play behavior score on effects-coded self-declared OSR participation (omnibus F(1, 1628) = 283.61, R2 = .15, b = 1.42, SE = .08, t = 16.84, p < .001, 95% CI [1.25, 1.58]). In English, people who said they participate in the OSR (yes/no) do actually report higher OSR play behavior (the R2 = .15 value means that self-declared participation explains about 15% of the variance in OSR play behavior). Additionally, people with higher OSR play scores were more likely to report having bought an OSR product, according to a logistic regression (b = .51, SE = .07, z = 7.21, p < .001, 95% CI [.37, .65]). This is somewhat exploratory, but strongly suggests the score is capturing some meaningful variation in reported behavior.
Now for some of the more intriguing relationships, such as with blogging (Do you have a blog where you post about tabletop roleplaying games? Yes/No). OSR play behavior positively predicts blogging about any tabletop roleplaying games (b = .32, SE = .06, z = 5.55, p < .001, 95% CI [.21, .43], using a logistic regression). General play behavior, however, measured as the number of different games played, has no relationship to blogging (b = .09, SE = .06, z = 1.55, p = .121). The logistic regression equivalent of R2 is pretty low for this relationship, around 2%, so the importance of the relationship may be small, but the point is comparative: something about OSR play inclines people toward sharing long-form thoughts about tabletop roleplaying compared to just playing a wide variety of games.
Finally, respondents with higher OSR play behavior scores reported the OSR to be more welcoming of diverse voices (omnibus F(1, 1628) = 129.69, R2 = .07, b = .46, SE = .04, t = 11.39, p < .001, 95% CI [.38, .54]). The text of this particular item was: The OSR welcomes diverse voices (1 = Strongly disagree, 7 = Strongly agree; M = 4.79, SD = 1.70, n = 1823). There are a few potential interpretations of this result. Optimistically, people walking the talk (that is, respondents that actually play consensually-defined OSR games) have a more positive view of the degree to which the OSR is welcoming. Pessimistically, there may be some selection bias, as people who feel the OSR is unwelcoming may have been less likely to participate in the survey at all. Anecdotally, I did observe this reaction from a handful of individuals. As a crude robustness check, I arbitrarily changed 50 of the “welcoming” responses (around 2% of the sample) to be 1 (Strongly disagree), simulating absent negative responses, and ran the same analysis again. The result held, suggesting that this sort of selection bias would have minimal effect on aggregate beliefs.