Let (x) be the field of mass-density fluctuations and g (x) the corresponding field of galaxy-density fluctuations, at a given time and for a given type of object. The fields are both smoothed with a fixed window which defines the term ``local''. The local biasing relation is considered to be a random process, specified by the biasing conditional distribution P(g | ). Let the one-point probability distribution functions (PDF) P() and P(g) be of zero means and standard deviations 2 < 2 > and g2 < g2 >.
Define the mean biasing function b() by the conditional mean,
This function is plotted in Figure 1.
It is a natural generalization of the deterministic linear biasing relation,
g = b1 .
The function b() allows
for any possible non-linear biasing.
We find it useful to characterize the function b()
by its moments and
defined by
It will become clear that is the
natural extension of b1
and that /
is the relevant measure of
non-linearity, independent of stochasticity.
The local statistical character of the biasing can be expressed
by the conditional moments of higher order about the mean at a given
Define the random biasing field by
g - < g | >, with < | > = 0.
The local variance of at a
given defines the biasing
scatter
function b() and by averaging over
one obtains the local biasing scatter parameter:
The scaling by 2 is
for convenience.
The function < 2
| >1/2 is marked by
error bars in
Figure 1.
Here and below we make use of a straightforward lemma,
valid for any functions p(g) and q
():
From the three basic parameters defined above one can derive other
biasing parameters.
A common one is the ratio of variances,
The second equality is a result of Eq. (4).
It immediately shows that bvar is sensitive both to
non-linearity and
to stochasticity, with bvar .
This makes bvar biased compared to
,
Using Eq. (4), the mean parameter
is related to the covariance,
Thus, is the slope of the linear regression of g on
,
which makes it a natural generalization of b1.
Unlike the variance g2 in Eq. (5), the covariance in Eq. (7)
has no contribution from b.
A complementary parameter to bvar is the linear
correlation coefficient,
The ``inverse" regression, of
on g, yields another biasing parameter:
Thus, binv is biased relative to
, even more than
bvar.
The parameter binv is close to what is measured in practice
by two-dimensional linear regression
[52],
because the errors in are
larger than in g.
Note that and
b nicely separate the
non-linearity and stochasticity, while bvar, r
and binv mix them.
In the case of linear, stochastic biasing,
the above parameters reduce to
Thus, b1
bvar
binv.
In the case of non-linear deterministic biasing:
In the fully degenerate case of linear and deterministic biasing,
all the b parameters are the same, and only then r = 1.
In actual applications,
the above local biasing parameters are involved when the parameter
``''
is measured from observational data.
For linear and deterministic biasing this parameter is defined unambiguously
as 1
f
() /
b1, but any deviation from this
model causes us to measure different
's by the
different methods. For example,
it is var
f () / bvar which is
determined from g
and f ().
The former is typically determined from a redshift survey,
and the latter either from an analysis of peculiar velocity data,
from the abundance of rich clusters,
or by COBE normalization of a specific power-spectrum shape.
In the case of stochastic biasing bvar
is always an overestimate of ,
Eq. (5), and when the biasing is linear
bvar is an overestimate of
b1. Therefore var is underestimated
accordingly.
Another useful way of estimate
is via the linear regression of the fields in our cosmological
neighborhood, e.g., - .
v(x) on g (x)
[17,
33,
52].
In the mildly-non-linear regime, -
. v(x) is actually replaced by
another function of the first spatial
derivatives of the velocity field, which better approximates the
scaled mass-density field f ()(x)
[47].
The regression is effectively
on g, because the errors in
. v (or f
) are
typically more than twice as large as the errors in g.
Hence, the measured parameter is close to
inv
f
() / binv.
In the case of linear and stochastic biasing, Eq. (10), binv
is an overestimate of b1 so
the corresponding
is underestimated accordingly.