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way as Waterhouse et al. [227, 226] by performing a Laplace approximation of
the posterior.
The Laplace approximation aims at finding a Gaussian approximation to the
posterior density, by centring the Gaussian on the mode of the density and
deriving its covariance by a second-order Taylor expansion of the posterior [19].
The mode of the posterior is found by solving
∂
ln
q
V
(
V
)
∂
V
=0
,
(7.46)
which, by using the posterior (7.45) and the definition of
g
k
(7.10), results in
(
r
nk
−
g
k
(
x
n
))
φ
(
x
)
−
E
β
(
β
k
)
v
k
=0
,
k
=1
,...,K.
(7.47)
n
Note that, besides the addition of the
E
β
(
β
k
)
v
k
term due to the shrinkage prior
on
v
k
, the minimum we seek is equivalent to the one of the prior-less generalised
softmax function, given by (6.11). Therefore, we can find this minimum by ap-
plying the IRLS algorithm (6.5) with error function
E
(
V
)=
−
ln
q
V
(
V
), where
the required gradient vector and the
D
V
×
D
V
blocks
H
kj
of the Hessian matrix
(6.9) are given by
⎛
⎞
∇
v
1
E
(
V
)
.
⎝
⎠
∇
v
j
E
(
V
)=
n
∇
V
E
(
V
)=
,
(
g
j
(
x
n
)
−
r
nj
)
φ
(
x
n
)+
E
β
(
β
j
)
v
j
,
∇
v
K
E
(
V
)
(7.48)
and
H
kj
=
H
jk
=
n
g
j
(
x
n
))
φ
(
x
n
)
φ
(
x
n
)
T
+
I
kj
E
β
(
β
k
)
I
.
g
k
(
x
n
)(
I
kj
−
(7.49)
I
kj
is the
kj
th element of the identity matrix, and the second
I
in the above
expression is an identity matrix of size
D
V
D
V
. As the resulting Hessian is
positive definite [173], the posterior density is concave and has a unique maxi-
mum. More details on how to implement the IRLS algorithm are given in the
next chapter.
Let
V
∗
with components
v
k
denote the parameters that maximise (7.45).
V
∗
gives the mode of the posterior density, and thus the mean vector of its
Gaussian approximation. As the logarithm of a Gaussian distribution is a qua-
dratic function of the variables, this quadratic form can be recovered by a
second-order Taylor expansion of ln
q
V
(
V
) [19], which results in the precision
matrix
×
Λ
V
ln
q
V
(
V
∗
)=
E
(
V
∗
)=
H
=
−∇∇
∇∇
|
V
=
V
∗
,
(7.50)
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