A Note on the Berkson Model Note that in the Berkson model yi = β 0 + β 1 xi + β 1 ηi + εi if we let β 1 η i + εi = γ i then with σ 2γ = β 21 σ 2η + σ 2 we have nothing but the usual SLR model with error variance σ 2γ . In particular, the Berkson model with parameters β 0 , β 1 , σ2 , and σ 2η is not identifiable. (For a given set of SLR parameters β 0 , β 1 , and σ2γ , there are many σ 2η and σ 2 pairs that produce the same σ2γ and therefore same distribution of the observables. So, for example, if b0 , b1 , and SSE/n ¡ ¢ are the usual Stat 511 least squares MLEs of the SLR parameters, any σ2η , σ 2 pair with SSE/n = b21 σ2η + σ 2 will maximize the Berkson likelihood. It is therefore really not possible to estimate all of the Berkson parameters. In a Bayes context, if one goes ahead and tries to do Bayes estimation of all 4 Berkson parameters, what one gets will be very prior-dependent. For example, one sensible way to proceed is to place priors on β 0 , β 1 , and σ 2γ as if one had the SLR model (which one does) and then make some prior assumption about σ 2η σ2 k= For example, independent flat priors on β 0 , β 1 , and ln σ γ produce inferences like those from standard linear models theory for β 0 , β 1 , ynew , and xnew . Then an independent prior on k leads to (completely prior-dependent) inferences for σ 2η and σ 2 based on the identities σ2 = σ 2γ kβ 21 + 1 and σ 2η = kσ 2 One should not fool oneself ... in terms of separating σ 2η and σ 2 , all one is looking at in the posterior is what one has put in in terms of prior assumptions about k. Some of you had difficulty getting MCMC to behave sensibly in MiniProject #3. Sometimes, what that kind of thing is telling you, is that you’ve got a likelihood/posterior that has a "ridge" in it where the sampler wanders around with wildly different values of the parameter vector giving very similar posterior densities. That is, lack of identifiability can lead to poorly behaved MCMC. 1