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53

the file). We apply the DPM model to estimate the distribution of the house prices
(disregarding the rest of the information in the file).

A particular case of model (3.9) is given in Escobar and West (1995), and imple-
mented in the R-package “DPpackage” (Alejandro Jara, 2007):

I. yi I μii ~ N(μii) for i = 1,... ,n,
II.
(μι,λ1), ...,(μnn) ∣G~G
III. G I Q,fc0,μι,≠ι ~ DP(α,G0(∙ I ⅛o,μι,≠ι)),
G0ii I k011') = N(μi m1, k0λi) Ga(λ ∣ r∕ι,≠ι)
IV. a ~ Ga(aa,bct'),mι ~ N(m2,s2β
ψι ~ Ga(η22)
and k0 ~ Gα(α⅛0∕2, ⅛0∕2),
where
N(m,τ) denotes the normal distribution with mean m and precision τ, and
Ga(a,β') the gamma distribution with mean aβ ηι,aa,ba, s2,η2,ψ2, dk,bk > 0 and
m2 ∈ JL

(3.25)


Notice that the variables yi,(μi,λi) and (m1,⅛,ψι) of the model in (3.25) play
the role of the variables
xt,θi and 7, respectively, in the general DPM (3.9). Let
Уп = {⅛∙∙∙ >y∏} represent the prices of n — 506 houses. Besides, we denote with
μ* =
(μ*1,...,μ*κ) and λ* = (ʌɪ,..., AJf) the vectors of size K containing the unique
values of the
μi and the λi respectively. We use the notation of the previous section
for the variables related with the configurations. When stating a complete conditional
posterior distribution in this section, we make explicit only the relevant quantities
(for example, since the complete conditional posterior distribution of
k0 depends only
on
m1,μ* and A*, we just write k0 m1,μ*, λ*).

We now describe steps (a)-(e) of the MCMC sampling scheme given in the previous
section for this specific example. There is no common parameter
σ so that step (c)
is not necessary. Let t(y ∣
m, s, v) denote a student t distribution with location m,
scale
s and degrees of freedom υ.

(a) Given the currently imputed values of (μ*, λ*), K and φ, generate a new config-
uration by simulating φi,...,
φn from the complete conditional posterior distri-



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