Agriculture Reference
In-Depth Information
non-sampled
N
n
units. Similarly, the vector of constant
ʳ
can be partitioned into
s
t
.
Now the estimated target can be expressed as
s
t
ʳ ¼ ʳ
; ʳ
t
Y
¼ ʳ
t
s
t
Y
s
ʳ
s
Y
s
þ ʳ
ð
12
:
3
Þ
t
Y
s
Y
s
þ ʳ
t
which is a realization of the random variable
ʳ
¼ ʳ
s
Y
s
. Because we
ʳ
t
y
s
after we have selected the sample, the estimation problem reduces to
predicting the unknown quantity
ʳ
know
this question).
Therefore, a linear estimator of
t
Y can be defined
ʸ ¼ ʳ
ʸ ¼
g
s
Y
s
;
ð
12
:
4
Þ
t
is a vector of coefficients. In this way, the error of
where g
s
¼
ð
g
1
g
2
...
g
n
Þ
the estimator
ʸ ¼
g
s
Y
s
is
Y
s
ʳ
ʸ ʸ ¼
g
s
Y
s
ʳ
t
Y
g
s
ʳ
t
s
t
a
t
Y
s
ʳ
t
¼
s
Y
s
¼
s
Y
s
;
ð
12
:
5
Þ
t
Y
where a
¼
ð
g
s
ʳ
s
Þ
. As demonstrated by Valliant et al. (
2000
), estimating
ʳ
using g
t
Y
s
is equivalent to estimating
s
Y
s
using a
t
Y
s
.
Generally, we assume that the covariates of Model (
12.2
) are known for each
unit in the population. In some particular cases, this assumption can be relaxed to
knowing only the population totals of the components of X (Valliant
2009
).
The matrices X and V can be re-expressed
t
ʳ
;
X
s
X
s
V
ss
V
ss
V
ss
V
ss
X
¼
V
¼
;
ð
12
:
6
Þ
where X
s
is
n
q
, X
s
is (
N
n
)
q
, V
ss
is
n
n
, V
ss
is (
N
n
)
(
N
n
), V
ss
is
n
V
ss
. Finally, we assume that V
ss
is positive definite.
(
N
n
), and V
ss
¼
ʸ ¼
g
s
Y
s
is unbiased (or, equivalently, prediction unbiased or
The estimator
¼
,
if
E
ξ
ʸ ʸ
model unbiased) for
0, see Eq. (
1.31
).
The error variance (or the prediction variance) of
ʸ ¼
ʸ
under a model
ξ
g
s
Y
s
under a model
ξ
is
then
2
E
ξ
ʸ ʸ
:
ð
12
:
7
Þ
The BLUP estimator under Model (
12.2
) is obtained by minimizing the error
variance in Eq. (
12.7
), that is (Royall
1976
),
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