Home » Data » Weighting data » When weights are not supported
When weights are not supported [message #3188] 
Mon, 03 November 2014 20:06 
Yohannes
Messages: 6 Registered: July 2014

Member 


I have DHS data for over 30 countries which I plan to use for a multicountry analysis using a STATA platform. I have already denormalised the weights (following DHS suggestion) but the model I want to fit, multi level probit/logit model, does not support weights. The question I have is what do you do when the platforms you use for analysis do not support weight, but you know that ignoring weights is not an option because sample sizes vary enormously between countries, and in some cases countries that have half the size population than the larger countries have two or three times larger samples.





Re: When weights are not supported [message #3201 is a reply to message #3196] 
Thu, 06 November 2014 00:09 
ReducedFor(u)m
Messages: 292 Registered: March 2013

Senior Member 


Yohannes,
I don't really understand the context of your research well enough to guarantee that any of these suggestions will be helpful, but here are some options (and some comments on the fixed/random effects question).
1  A very simple solution would be to use a "linear probability model" instead of a logit/probit  meaning an OLS regression on a 0/1 outcome. In big samples where you are interested in the effect of some particular covariate, this should give you a result very similar to the probit (unless you have someth really rare outcome, in which case maybe a Poisson regression). These are easily weighted and can deal with survey effects in any way you choose.
2  Disaggregation: You could estimate each country separately using any method you want, and then weight the coefficient estimates by population size to get a single, overall estimate  or just present the distribution of point estimates. This has a bit of a different interpretation than doing it all at once, and you are implicitly allowing each country to have its own (totally unconstrained relative to other countries) effect of each covariate. It will cost you power (efficiency). There may be a Bayesian hierarchical way to estimate this too all at once, but I don't know it, and I don't think Stata would do it.
3  Country Fixed Effects. I believe the recommendation for country level FEs had to do with establishing a commonality among countries in "levels". That is  if you use random effects, your model will still identify the coefficient of interest using both withincountry variation and acrosscountry variation. So if the levels of your Y or X variables are majorly different across countries (compared to withincountry) you will be estimating you coefficient mostly on differences between countries that may or may not be reasonably comparable. Using country fixedeffects demeans everything so that only the difference from the country level mean will identify the coefficient. In certain cases, this would make the weighting problem less severe (suppose all your observations were from very high or very low level country's for your covariates and outcome  the acrosscountry variation would be terrible, driven by lots of observations in the tails, but the withincountry might still be OK).
4  Depending on what your covariate of interest is, you will likely want to estimate your standard errors in ways that are far more conservative than those recommended for using one survey by the DHS. This depends a great deal on the particular empirical question you are asking, in particular on where the variation in your righthandside is (for instance, is it a response to some question in the DHS or some other data you are merging in). The paper linked below gives a good, if somewhat technical, overview of clustered standard errors and the problems you might face. I can offer better suggestions here if I understood your context a little better.
http://cameron.econ.ucdavis.edu/research/Cameron_Miller_Clus ter_Robust_October152013.pdf



Re: When weights are not supported [message #3204 is a reply to message #3201] 
Thu, 06 November 2014 18:39 
Yohannes
Messages: 6 Registered: July 2014

Member 


Thank you for the attention to my question and for the suggestions. Thank you also for the literature and the offer of assistance. Basically, what I am trying to do is look at the covariates of child well being in low and middle income countries in a multicountry context using primarily DHS data, but also supplemented by relevant national level indicators obtained from international databases, namely the World Bank. One of these child well being measures which I am trying to model is primary school attendance which is assumed to be a dichotomous outcome but can also take a count data form if level is taken in to account, and can be fitted using inflated or hurdle variants of Poisson or negative binomial models. I am also assuming that the response variable is affected by four set of factors: (1) child level characteristics (such as sex, age birth order etc); (2) household level characteristics (such as religion, parental education, and wealth status (I will come back to this to show how it is handled); (3) area level characteristics derived from the DHS data itself (such as urban rural residence, and other characteristics derived from the mean values for the strata in which the child lives); and (4) national level covariates (such as GDP, health expenditure per capita, external aid, indices of governance etc..) obtained from the World Bank. Given these, I set out to test two set of models, and in the first wanted to put all the four level variables in the main model and then add two random terms (without covariates) at country and strata level. In the second model, I wanted to keep only the child level and household level factors in the main model, and include the strata level and national level variables in the respective variance functions. For the wealth index variable, given that the DHS generated index is both country and survey specific, I went on and recalculated the index using the data for all countries combined, and reclassified households based on this new index rather than the original measure developed by the DHS.
So coming back to point 1 of the suggestion:
The data I am using for the study has over 200000 observations (unweighted) and the variable of interest, child schooling, is also not a rare event as such, so I can revert to a "linear probability model" easily. But my challenge is the available multilevel commands (such as the one on STATA which I use extensively for my research) do not support weights for any type of response variable specification. I am yet to go through the attached publication perhaps it may have a way to resolve my problem (??)
Yes, I can also do my analysis on country by country basis but as you noted that will change the research question. Primarily, I will not be able to capture between country effects. Besides, I am not exactly sure how I will be able to capture country level indicators in such analysis.
On the fixed random effects: The countries in the analysis vary widely both in terms of the response variable and explanatory variables as well as in DHS sample sizes. And given that my interest is also to look at both within and between country differences I was thinking that a random effect model that has the ability to correct for sample weights may be the best way to go. And given that the multilevel commands do not allow this, and that the fixed effect approach only partially addresses what I would like to do I am somehow torn between approaches neither of which appear to be ideal.



Re: When weights are not supported [message #3210 is a reply to message #3204] 
Fri, 07 November 2014 16:22 
ReducedFor(u)m
Messages: 292 Registered: March 2013

Senior Member 


Well... we are starting to get pretty far from area of expertise now (which is more about causal inference on a single RHS variable and not multilevel modeling).
That said  I wonder if the new class of sem (structural equation modeling) commands in Stata might help. They support the "svy" prefix with weights and strata, and I think you can model what you want using those commands, but like I said, getting pretty far from my expertise here.
http://www.stata.com/manuals13/sem.pdf [maybe start with intro 10  Fitting models with survey data (sem only)]
Let me know if these work  this problem has come up in enough contexts now that I would like to have an answer for people.
Oh  and out of curiosity, are you matching your country level covariates to the survey timing (so GDP in survey year) or to the birth or age timing (so relevant to when you were born/how old you are). For schooling, I'd say there is hazard of dropout every year, and if a kid dropped out two years ago, then current condition may not mean much as a predictor. I'm just sort of curious as to how people are thinking about these things. Thanks! Good luck.




Re: When weights are not supported [message #3244 is a reply to message #3199] 
Tue, 11 November 2014 12:26 
BridgetteDHS
Messages: 2809 Registered: February 2013

Senior Member 


Another response from Tom Pullum:
I agree with what Professor Cameron said. The fixed and random effects should partially remove the influence of the weights, as well as adjust for unmeasured sources of variation.
I suggest that you first apply, to the same data, a simpler statistical modelsinglelevel rather than multilevel that allows you to use weights. Apply that model with weights and then without weights to see how robust the estimates arethat is, to see whether there is a dramatic difference between the weighted and unweighted estimates when the fixed/random effects are included. (The fixed/random effects would be included in both the weighted and unweighted versions.) If there IS a dramatic difference, then maybe you should wait until the multilevel model has been revised to include weights.
There is another way to check robustness. I call this the construction of "fake" weights. First adjust v005 in the way you would like, for example so that the weighted number of cases in each survey is the same or is proportional to the population of the country, etc. Then think of v005 as an fweight rather than a pweight. You could remove a factor of 10,000 so that the arbitrary inflation factor is 100 rather than 1,000,000.
Say that the adjusted v005, still with the factor of 1,000,000, is called v005r. Then try these lines:
First run the model without any weights.
Then:
replace v005r=round(v005r/10000)
expand v005r
and then rerun the model on these data (without any weights).
Neither model will actually use weights, but the second data set has been artificially weighted through the expand command.
There is a substantial issue herethe expanded data file will be about 100 times bigger than the original file and probably too big. To make this strategy feasible you could do some sub sampling. OR you could work from a sample of the original data. The main objective would be to get a sense of how much distortion there will be in the estimates if you use fixed/random effects for countries and strata and do not weight.



Re: When weights are not supported [message #3245 is a reply to message #3244] 
Tue, 11 November 2014 20:19 
ReducedFor(u)m
Messages: 292 Registered: March 2013

Senior Member 


I almost pitched the same weighting workaround idea  just make your dataset sample size proportional to population by expanding the number of observations (and withinsurvey, you expand relative to the probability weights). I would just add that, if you use the "cluster" command and cluster at a level above the individual, then you should get proper inference because the model will "know" that there is no added variation from the extra observations.*
*Note: a great way to convince yourself of this is to generate some fake data, add an id number, run a regression, get the standard errors, and then replicate each observation 100 times (expand) and "cluster" on the id variable. You'll get back the original standard errors (while OLS on the expanded sample will produce SEs that are far too small). You could also do this using an original DHS dataset.







Goto Forum:
Current Time: Fri Jun 9 07:13:18 Coordinated Universal Time 2023
