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PERSPECTIVE
doi:10.1111/j.1558-5646.2007.00100.x
A CENTENNIAL CELEBRATION FORQUANTITATIVE GENETICSDerek A. Roff
Department of Biology, University of California, Riverside, California 92521
E-mail: [email protected]
Received December 6, 2006
Accepted January 28, 2007
Quantitative genetics is at or is fast approaching its centennial. In this perspective I consider five current issues pertinent to
the application of quantitative genetics to evolutionary theory. First, I discuss the utility of a quantitative genetic perspective in
describing genetic variation at two very different levels of resolution, (1) in natural, free-ranging populations and (2) to describe
variation at the level of DNA transcription. Whereas quantitative genetics can serve as a very useful descriptor of genetic variation,
its greater usefulness is in predicting evolutionary change, particularly when used in the first instance (wild populations). Second,
I review the contributions of Quantitative trait loci (QLT) analysis in determining the number of loci and distribution of their
genetic effects, the possible importance of identifying specific genes, and the ability of the multivariate breeder’s equation to
predict the results of bivariate selection experiments. QLT analyses appear to indicate that genetic effects are skewed, that at least
20 loci are generally involved, with an unknown number of alleles, and that a few loci have major effects. However, epistatic
effects are common, which means that such loci might not have population-wide major effects: this question waits upon (QTL)
analyses conducted on more than a few inbred lines. Third, I examine the importance of research into the action of specific genes
on traits. Although great progress has been made in identifying specific genes contributing to trait variation, the high level of
gene interactions underlying quantitative traits makes it unlikely that in the near future we will have mechanistic models for such
traits, or that these would have greater predictive power than quantitative genetic models. In the fourth section I present evidence
that the results of bivariate selection experiments when selection is antagonistic to the genetic covariance are frequently not well
predicted by the multivariate breeder’s equation. Bivariate experiments that combine both selection and functional analyses are
urgently needed. Finally, I discuss the importance of gaining more insight, both theoretical and empirical, on the evolution of the
G and P matrices.
KEY WORDS: Breeder’s equation, G matrix, microarrays, quantitative genetics, QTL analysis.
If we take the speculations of Yule presented at the Third Inter-
national Conference of Genetics (Yule 1906) on the relationship
between the biometrical and Mendelian approaches to heredity as
the foundations upon which the field of quantitative genetics is
based, then we have just passed the 100th birthday of quantita-
tive genetics. On the other hand, the 1918 publication of Fisher
might be taken as the real beginnings of quantitative genetics as
we know it (for a detailed account of Yule’s musings in relation
to Fisher’s contribution see Tabery 2004), in which case the cen-
tenary of quantitative genetics birth is but a few years away. No
matter which date we take, the fact remains that quantitative genet-
ics has been around for a long time, during which it has developed
with a very large statistical foundation that is still in the process of
being tested. Early work focused on the contribution of quantita-
tive genetics to animal and plant breeding but the work of Russell
Lande in the 1970s promoted the use of quantitative genetics by
those interested in evolutionary biology. A significant difference
between the interests of the breeder versus the evolutionary bi-
ologist is that whereas the breeder frequently is concerned with
the improvement of a single trait (or two traits combined into a
single index), the evolutionary biologist is generally faced with
addressing the evolution of multiple traits simultaneously. This
1017C© 2007 The Author(s). Journal compilation C© 2007 The Society for the Study of Evolution.Evolution 61-5: 1017–1032
PERSPECTIVE
change in focus has raised issues of methodology and approach
that are still being worked out: the purpose of this perspective is to
suggest that a singular contribution that quantitative genetics can
make to our understanding of organic evolution is in the area of
multivariate trait evolution and that the new fields of research in
genomics such as QTL and microarray analyses are contributing
to, and benefiting from, a quantitative genetic perspective.
The most general form in which quantitative genetics is used
in evolutionary biology is given by the equation �z = GP−1S,
where �z is the change in trait means, G is the genetic variance–
covariance matrix, P−1 is the inverse of the phenotypic variance–
covariance matrix, and S is the vector of selection differentials.
An alternate and equivalent formulation of this equation is �zi =∑n
j=1,n � j hi h jrAi j , where �zi is the response of the ith of n traits,
hj is the square root of the heritability of the jth trait, rAij is the
genetic correlation between traits i and j, and � j is the selection
gradient on the jth trait. I shall refer to these equations as the
multivariate breeder’s equation. In this perspective I shall highlight
five issues that bear upon the present and future contributions of
quantitative genetics to our understanding of evolutionary change:
(1) The utility of a quantitative genetic approach to measuring
genetic variation: In this section I outline the utility of a
quantitative genetic perspective in describing and analyzing
genetic variation at two very different levels of resolution,
namely genetic variation in natural populations and genetic
variation at the level of DNA transcription.
(2) Do the results of QTL analyses support the assumptions
of quantitative genetics? As a general descriptor in the two
circumstances discussed in section 1, the quantitative ge-
netic parameters may be useful in themselves, but what
we really desire is that the approach can actually be used
to predict evolutionary change. In this case we need to
consider whether the basic assumptions of quantitative ge-
netics are likely to be sufficiently accurate or robust for
at least short-term prediction and then whether selection
on multiple traits has produced results consistent with the
multivariate breeder’s equation. To address the question of
the number of loci and the distribution of their effects, I
use information recently obtained from QTL analyses, at
present possibly the premier method for investigating such
questions.
(3) What is the importance to quantitative genetics of identify-
ing specific genes? Recently there has been an enormous ef-
fort put into elucidating the molecular basis of variation with
attention being given to identifying genes of major effect.
Given that quantitative genetics focuses upon the totality
of genomic expression of a trait as expressed in a statisti-
cal description, does such research have any messages for
quantitative genetics?
(4) Testing predictions of the multivariate breeder’s equation. In
the fourth section I consider whether artificial selection on
multiple traits or evolutionary changes in wild populations
can be reasonably predicted by the multivariate breeder’s
equation.
(5) The evolution of the phenotypic and genetic variance co-
variance matrices. Application of the multivariate breeder’s
equation assumes that the variance–covariance matrices re-
main constant. In this section I examine this proposition
and suggest that the present hypothesis-testing approaches
should be replaced by an interval-estimation perspective.
The Utility of a Quantitative GeneticApproach to Measuring GeneticVariationA measure of genetic variation in a population and its potential
response to selection can be made by estimating G and P. The
latter is readily accomplished but the estimation of G presents
significant logistical problems. Three approaches can be used: (1)
Bring the organism into the lab and estimate the G matrix by
controlled breeding experiments, (2) use a sampling design in a
wild population that matches a standard pedigree design, such as
offspring on parent, (3) sample a population over a number of
generations and use the animal model.
The assumption of the first approach is that the estimate ob-
tained from a laboratory is equal or close to that which would be
obtained in the field. Because it was assumed that the environmen-
tal variance would be higher in the field than the lab, conventional
wisdom suggested that heritabilities and genetic correlations in
the field would be lower than in the lab. A meta-analysis of lab
and field studies showed that this was not the case for heritabil-
ities, though phenotypic variances tend to be reduced in the lab
(Weigensberg and Roff 1996). An assessment of the genetic cor-
relation or the genetic variances and covariances remains to be
undertaken. The results of the analysis on heritability show that
it is premature in the extreme to dismiss estimates from labora-
tory studies. Some studies in wild populations, most particularly
those on birds, have been able to estimate genetic parameters
from offspring on parent regression (e.g., Grant and Grant 1995;
Reale and Festa-Bianchet 2000; Roff et al. 2004). In general, how-
ever, a study of relationships among individuals in a wild popu-
lation will produce a convoluted set of relationships that cannot
be analyzed using such simple methods as half-sib or offspring–
parent regression. A solution to this dilemma is the animal model,
which does not require any specific pedigree (Knott et al. 1995;
Kruuk 2004). In addition to the important task of resolving the
question of how much genetic variation is found in wild popu-
lations (e.g., Reale et al. 2003; Kruuk 2004; Charmantier et al.
2006a), use of the animal model to estimate genetic parameters
1018 EVOLUTION MAY 2007
PERSPECTIVE
in wild populations has enabled detailed investigations into the
importance of maternal effects (Kruuk 2004; Wilson et al.
2005a,b; Charmantier et al. 2006b), genotype by environmen-
tal interactions (Kruuk 2003; Garant et al. 2004; Brommer et al.
2005; Nussey et al. 2005; Wilson et al. 2006), variation between
ages and sexes in genetic parameters (Pettay et al. 2005; Wilson
et al. 2005b; Charmantier et al. 2006c), and tests of sexual selec-
tion theory (Hadfield et al. 2006; Qvarnstrom et al. 2006). These
studies have demonstrated that genetic variation is usual in wild
populations and that long-term variation in trait values can only
be properly understood within a quantitative genetic framework.
Quantitative genetic approaches are also making significant
contributions at an entirely different level, namely variation at the
level of transcription of DNA. DNA microarrays have enabled
the visualization of the rates of transcription of hundreds to thou-
sands of genes (for overviews of the techniques see Brown and
Botstein 1999; Gibson 2002; Tarca et al. 2006). Early experiments
showed that rates of transcription varied among genotypes and that
transcription rates could themselves be viewed as heritable traits
(Schadt et al. 2003; Gibson and Weir 2005; Roelofs et al. 2006).
At a more general level, the analysis of microarray data can be
approached using the same statistical approaches as quantitative
genetics, namely mixed model analysis of variance, where both
genotypic and environmental sources of variation can be resolved
(Kerr et al. 2000, 2001; Wolfinger et al. 2001; Churchill 2002;
Chen et al. 2004; Nettleton 2006). At the present time use of mi-
croarrays is restricted by the costs of producing arrays for the
organism under study: even with model organisms the cost is suf-
ficiently high to preclude the analysis of hundreds of microarrays,
as would be necessary in a typical quantitative pedigree design.
Initial studies have used inbred lines (Jin et al. 2001; Rifkin et al.
2003; Schadt et al. 2003; crosses between isogenic lines (Drnevich
et al. 2004), different morphs of the same species (Derome et al.
2006), selected lines (Roberge et al. 2006), individuals from differ-
ent populations (Oleksiak et al. 2002; Vuylsteke 2005), or different
species (Rifkin et al. 2003). All cited studies showed genotypic
differences though only in a few cases were sample sizes suffi-
cient to attempt an estimate of variance components or a general
comparison with phenotypic variation.
Jin et al. (2001) examined rates of transcription in two inbred
strains of Drosophila melanogaster at ages one and six weeks and
separated variance components due to sex and genotype: sex con-
tributed most but the “genotypic contributions to transcriptional
variance may be of similar magnitude to those relating to some
quantitative phenotypes” (Jin et al. 2001, p. 389). In their analy-
sis of transcriptional variation in Arabidopsis thaliana, Vuylsteke
et al. (2005) found more than 30% of the genes had significant ad-
ditive effects and 5–20% of genes, depending on the cross, showed
nonadditive interaction. Most of the differences in transcriptional
variance in the fish Fundulus heteroclitus and F. grandis were
found within populations (coefficients of variation 5–15%) though
significant differences among populations and species were found
(Oleksiak et al. 2002).
Apart from the problem of sample size, the experiments us-
ing microarrays can suffer from a surfeit of data in the sense
that hundreds of genes may show differences. One could regard
the array as a variance–covariance matrix and calculate all possi-
ble variance and covariances, but this would generate enormous
problems of determining statistical significance. An alternative
approach is to collapse the array into a manageable number of un-
correlated variables using principal components analysis. Doing
this, Bochdanovits and de Jong (2004) were able to show sig-
nificant correlations between PC1 of gene expression and the two
traits, body weight and larval survival in D. melanogaster. Further-
more, PC analysis showed that variation in transcription rate was,
in addition to covarying with adult weight, a function of popula-
tion of origin and rearing temperature (Bochdanovits et al. 2003).
Whitefish (Coregonus clupeaformis) is found within a single
population in two morphs, a normal and a dwarf morph, that form
reproductively isolated ecomorphs (Derome et al. 2006). Com-
parison of transcriptional profiles of the two morphs collected
from two separate lakes, both morphs found in each lake, showed
both population- and morph-specific differences (Derome et al.
2006). Variation among gene expression has also been found in
the two phenotypic morphs, normal and “sneaker” (also known as
a “jack”) morph, of Atlantic salmon, Salmo salar (Aubin-Horth
et al. 2005a,b), and in territorial and nonterritorial males of the
cichlid, Astatotilapia burtoni (Hofmann et al. 1999; Hofmann
2003). Except for the whitefish study, where different populations
were raised in a common garden, separating environmental from
genetic components of variation was not possible in these exper-
iments, though the heritability of “jacking” in Chinook salmon
(Onchorynchus tshawytscha) is 0.67 (Mousseau et al. 1998), sug-
gesting that further testing for genetic differences in transcrip-
tional rates in the two morphs of Atlantic salmon would be prof-
itable. Genetic variation in transcription rates in Atlantic salmon
has been demonstrated by comparing strains selected for rapid
growth with wild strains. Five to seven generations of selection
produced heritable changes in gene transcription rates (Roberge
et al. 2006), but, because data on selection intensities are not avail-
able, heritabilities cannot be estimated.
Do the Results of QTL AnalysesSupport the Assumptions ofQuantitative Genetics?Prior to QTL analysis the estimation of the number of loci was
problematic and very uncertain. The advent of the use of molecu-
lar markers to divide the chromosome into many segments has
enabled QTL analysis, first conceived in 1923 (Sax 1923), to
EVOLUTION MAY 2007 1019
PERSPECTIVE
make great strides in enunciating the number of chromosomal
segments involved in quantitative genetic variation. Quantitative
trait loci analyses most frequently employ crosses between in-
bred lines, though methods exist for the analysis of outbred pop-
ulations (Lynch and Walsh 1998; for briefer, less mathematical
descriptions see Mackay 2001a or Mauricio 2001). Although the
statistical power of QTL analyses using inbred lines is generally
greater than those using outbred pedigrees (Erickson et al. 2004),
their weakness lies in their inability to detect more than two alle-
les at any locus. Thus even if a QTL analysis picks up relatively
few regions with significant effects we cannot immediately con-
clude that the assumption of a large number of genes of small
effect is violated, because there may still be numerous alleles at
each detected QTL or allelic variation at QTLs that happen to be
homozygous for the two inbred lines chosen. However, if QTL
analyses consistently found few regions of major effect we might
certainly begin to entertain the hypothesis that the assumption of
many genes of small effect may be incorrect, presuming that the
QTL segments are sufficiently small that they contain only a single
or possibly a few actual loci that affect the trait under study.
Early QTL analyses did indeed produce results that pointed
to relatively few regions of major effect. One would expect that
as sample size increased the number of QTLs detected would in-
crease, the percentage of phenotypic variance explained per QTL
would decrease, and the total variance explained would go up.
Rather surprisingly, though the first two predictions were upheld,
the third was not (see fig. 1.10 in Roff 1997). Using simulation,
Beavis (1994, 1998) showed that with small sample sizes QTL ef-
fects are grossly inflated and hence the effective number of QTLs
contributing to a trait is underestimated. This phenomenon has
become known as the Beavis effect and its theoretical basis inves-
tigated in detail by Xu (2003), though the general nature of the
problem was forecasted in the early 1990s both by the work of
Beavis and others (Kearsey and Farquhar 1998). To obtain reason-
ably accurate estimates of effects sample size must exceed 500,
whereas sample sizes much before the year 2000 were more typi-
cally in the range of 200 individuals (Roff 1997). It is still not clear
how many loci generally contribute to a trait or the distribution
of effects. In a review of QTL analyses in plants, Remington and
Purugganan (2003, p. S13) concluded “that individual genes with
relatively large effects on trait variation are probably important
in evolution,” but did not provide a meta-analysis to support this
statement. A meta-analysis of the distribution of QTL effects in
pigs and dairy did indicate that effects were skewed with a few
QTL of large effect, the total number of QTL for the dairy data
being estimated to lie between 50 and 100, depending on pop-
ulation size (Hayes and Goddard 2001). Mackay (2004, p. 254)
in reviewing QTL analyses in Drosophila drew the conclusion
that “the distribution of homozygous QTL effects is exponential,
with a large number of QTLs with small effects, and a smaller
number with large effects; the latter contribute most of the vari-
ation between parental lines.” To date I know of no study that
has carried out a meta-analysis of QTL effects from which gen-
eral statements about the number of QTLs and the distribution of
their effects can be made with statistical precision: such a study is
greatly needed.
Given that we know that there is not an infinite number of
loci, how many is enough to satisfy the assumption of normality
if each did indeed have a similar effect? The well-known answer
is that very few are required: four or five loci with two alleles per
locus will provide a distribution that is statistically very close to
normal. The problem lies in the fact that in such a situation selec-
tion can very rapidly erode genetic variation. A typical number
of QTL detected appears to be about 20 (Cheverud et al. 1996;
Vaughn et al. 1999; Mackay 2001a; Rocha et al. 2004; Nuzhdin
et al. 2005), though Walsh (2001, citing personal communication
with Mackay) gives an estimate of 130 genes for sternopleural
bristle number in D. melanogaster based on mutational effects.
Given the limitations of QTL detection, the number of loci might
well be typically in the dozens if not hundreds. What we do not
know, and need to know, is how many alleles typically segregate
at each locus (defining what is a locus at the molecular level it-
self presents difficulties, but here I refer only to QTL variation,
which admittedly is at best only a crude measure of a locus). The
number of QTL is probably sufficient to satisfy the assumption of
normality provided that the distribution of effects is itself close
to normal. The present QTL results, as expounded in the above-
cited reviews, suggest that the QTL effects are highly skewed.
On the other hand, this is not necessarily important, because the
multivariate breeder’s equation focuses upon the change in mean
trait values and hence even if the distribution of genetic effects
is not normal, by the central limit theorem, the distribution of
mean effects will be normal. Lack of normality is certainly ob-
served in many phenotypic distributions but these can be brought
into line by a suitable transformation. Theoretical and numerical
analyses have shown that the Gaussian approximation is satisfac-
tory even under strong selection, which produces large deviations
from normality (Turelli and Barton 1994). Thus, for single traits
the question of normality is probably not critical, at least for the
case of short-term (approximately 10 generations) selection. It is
not clear how important the assumption of multivariate normality
will be, and this question needs to be addressed via analytical, or
more likely, numerical analysis. If phenotypic effects mirror the
underlying additive genetic effects, then the question of multivari-
ate normality may be not be particularly significant because one
can find a suitable transformation. However, more troublesome is
the possibility that the distribution of additive genetic effects is not
the same as the composite phenotypic effects and hence a trans-
formation applied to the phenotypic scale does little or nothing to
improve the distribution on the additive genetic scale.
1020 EVOLUTION MAY 2007
PERSPECTIVE
But can we trust the distribution of effects as presently sug-
gested by the QTL analyses? Here we must consider the issue
of epistatic effects. First, it is very evident from analyses of line
crosses between inbred lines, different populations or different
species that both dominance and epistatic effects are exceedingly
common in both morphological and life-history traits, dominance
effects being demonstrated in more than 95% of cases and epistatic
effects demonstrated in more than 65% of cases (Roff and Emerson
2006). Quantitative trait loci analyses have made similar findings
(e.g., Cheverud and Routman 1995; Shook and Johnson 1999;
Mackay 2001b, 2004; Leips and Mackay 2002; Alonso-Blanco
et al. 2003; Carlborg et al. 2003; Caicedo et al. 2004; Carlborg
and Haley 2004; Weinig and Schmitt 2004; Malmber et al. 2005;
Mackay and Lyman 2005; Carlborg et al. 2006; Yi et al. 2006) de-
spite the fact that the power to detect epistatic interactions is low
(Flint and Mott 2001; Mackay 2001b; Carlborg and Haley 2004;
Erickson et al. 2004). If epistatic effects are so pervasive, the pres-
ence of alleles of large effect may be contingent on the particular
genetic background used in the QTL analysis, in which case the
effect of this “major” QTL may disappear when measured over
the entire complement of genomes present in a wild, outbreeding
population. In this scenario, epistatic effects could contribute sig-
nificantly to additive genetic variance but not epistatic variance.
This is the argument that Fisher himself used to dismiss the im-
portance of epistatic variance in large populations (Whitlock et al.
1995; Brodie 2000). In small populations, epistatic effects may
come to the fore and contribute to nonadditive genetic variance, a
consequence of which would be that the selection coefficient on a
locus in local populations may differ as a consequence of epistatic
effects, which is the argument Wright used in championing his
model of evolution (Hill 1989; Wade and Goodnight 1998). As
with QTL analysis, the detection of epistatic effects within pop-
ulations using traditional quantitative genetics approaches is ex-
tremely difficult, but this is itself no reason to ignore their possible
effects. In the light of the consistent evidence for epistatic effects,
we are in need of research both in the empirical investigation of
epistatic effects within populations, which will rely upon further
QTL analyses, and theoretical work on whether the effects as
presently observed could influence evolutionary trajectories.
At present, the conclusions on the importance of epistatic
variance, as opposed to epistatic effects, in modulating evolution-
ary responses is mixed. Keightley (1996) showed theoretically
that epistatic effects generated in metabolic pathways could cause
asymmetric responses to selection but empirical demonstration
is as yet absent. Other theoretical models have also shown that
epistatic effects could be important (Fuerst et al. 1997; Soriano
2000), but much remains to be done in working out the circum-
stances under which epistatic variance should be incorporated into
quantitative genetic models and analyses. Carlborg et al. (2006)
present an interesting case in which a single major QTL for growth
in chickens is actually composed of four interacting loci, the effect
of which is to produce a higher response to selection than would
be predicted by a single locus. Theoretical models incorporating
epistatic effects have also been studied in regards to mutation-
selection balance, the general finding being that, as with the ad-
ditive model, the final balance is sensitive to parameter values
(Hermisson et al. 2003; Hansen et al. 2006), about which we
know very little. Epistasis underlies canalization and may un-
der particular conditions be a source of cryptic variation (Hansen
2006). Several studies have shown that, as a result of the popu-
lation passing through a bottleneck, epistatic effects can be con-
verted into significant additive genetic variance (Goodnight 1988,
2000; Cheverud and Routman. 1996; Cheverud et al. 1999; Wade
2002) though its importance has been questioned by other studies
(Lopez-Fanjul et al. 2002, 2006b121; Hill et al. 2006; Turelli and
Barton 2006).
Finding considerable epistasis at the molecular level does not
mean that epistatic variance will be significant at the phenotypic
level at which most traits forming the focus of quantitative genetic
analysis are found. As discussed in the next section, epistatic in-
teractions are expected in such complex traits as morphology,
fecundity, or longevity but this may be irrelevant to quantitative
genetics if such effects are manifested as additive variance.
What is the Importance toQuantitative Genetics of IdentifyingSpecific Genes?Quantitative genetics is primarily a statistical description of the
action of genes and does not, in principle, concern itself with
the details of the genetic mechanism except in as much as such
mechanisms result in additive and nonadditive genetic variance.
On the other hand, such a broad brush approach to evolutionary
responses to selection or random sampling through drift may not
capture evolutionary responses in some instances. It is thus im-
portant to continually assess how the increasing information on
genetic mechanisms impacts quantitative genetic predictions. Re-
cent advances in genomics has led to the identification of specific
genes involved in traits of obvious evolutionary significance such
as morphology, life span, and resistance to pesticides (Table 1).
How do such findings impinge upon quantitative genetics?
Wing polyphenism is found in a large number of ant species
and is completely determinate in that particular castes, but not
all castes (queens in some species may be dimorphic for wings),
always exhibit the same phenotype. Although the same network
of gene interactions appear to be involved in the expression of
morphology, the point at which the network is interrupted dif-
fers among species (Abouheif and Wray 2002). This informa-
tion is important for an understanding of the genetic and physi-
ological regulation of caste development but does not affect the
EVOLUTION MAY 2007 1021
PERSPECTIVE
Tab
le1.
Exam
ple
so
fq
uan
tita
tive
trai
tsin
wh
ich
sin
gle
gen
esh
ave
maj
or
effe
cts
and
the
mo
lecu
lar
bas
iso
fre
gu
lati
on
has
bee
nst
ud
ied
.
Tra
itSp
ecie
sPa
thaf
fect
edN
otes
Sour
ce
Win
gpo
lyph
enis
mA
nts
Mul
tiple
Inte
rrup
tion
ofde
velo
pmen
taln
etw
ork
occu
rsat
diff
eren
tpl
aces
indi
ffer
ents
peci
esA
bouh
eif
and
Wra
y(2
002)
Gro
wth
ofin
sect
hind
legs
Num
erus
spec
ies
Ubx
and
abd-
Aex
pres
sion
Reg
ulat
orof
grow
thbu
tpre
cise
mol
ecul
arm
echa
nism
note
luci
date
dM
ahfo
ozet
al.(
2004
)
Bea
ksi
zeC
hick
ens,
duck
s,D
arw
in’s
finc
hes
Bm
p4D
iffe
rent
iale
xpre
ssio
nin
beak
mor
phog
enes
isA
bzha
nov
etal
.(20
04);
Wu
etal
.(20
04)
Hea
vym
etal
tole
ranc
eO
rche
sell
aci
ncta
Mt
Tra
nscr
iptio
nra
tere
gula
tes
Cd
excr
etio
nR
oelo
fset
al.(
2006
)
Bol
ting
A.t
hali
ana
FR
Ige
neen
code
sa
prot
ein
that
repr
esse
str
ansi
tion
tofl
ower
ing
Epi
stat
icin
tera
ctio
nw
ithF
LC
gene
spr
oduc
escl
inal
vari
atio
nSh
eldo
net
al.(
2000
);C
aice
doet
al(2
004)
Lif
esp
anD
.mel
anog
aste
rM
ultip
leM
ultip
lege
nes
indi
vidu
ally
have
maj
oref
fect
s(8
–85%
incr
ease
)Ta
ble
1in
Hug
hes
and
Rey
nold
s(2
005)
Lif
esp
anC
.ele
gans
Cel
l-si
gnal
ing
path
way
Up
to3×
incr
ease
p.43
2in
Hug
hes
and
Rey
nold
s(2
005)
.See
also
Ler
oi(2
001)
Res
ista
nce
A.t
hali
ana
Plas
ma
mem
bran
epr
otei
nth
atco
nfer
sab
ility
tore
cogn
ize
path
ogen
Not
driv
ento
fixa
tion
beca
use
ofa
trad
e-of
fw
ithse
edpr
oduc
tion
Tia
net
al.(
2003
)
Res
ista
nce
A.t
hali
ana
Aux
inre
spon
se3
mut
atio
nsaf
fect
ing
sam
epa
thw
ayR
oux
and
Reb
oud
(200
5)R
esis
tanc
eD
.mel
anog
aste
rJH
rece
ptor
Mut
antM
etal
lele
ssi
gnif
ican
tlyaf
fect
resi
stan
cean
dha
vest
atis
tical
lysi
gnif
ican
tple
iotr
opic
effe
cts
onlif
e-hi
stor
ytr
aits
Flat
tand
Kaw
ecki
(200
4)
Res
ista
nce
D.m
elan
ogas
ter
Ove
rtra
nscr
iptio
nD
iffe
rent
path
sca
nbe
affe
cted
(e.g
.,cy
toch
rom
eP4
50s,
glut
athi
one-
S-tr
ansf
eras
es,e
ster
ases
)L
eG
off
etal
.(20
03);
Fest
ucci
-Bus
elli
etal
.(2
005)
Res
ista
nce
Cul
expi
pien
sE
ster
ase
over
prod
uctio
nTw
olo
ciin
volv
ed,w
ithtw
ono
nexc
lusi
vem
echa
nism
sof
oper
atio
nB
ertic
atet
al.(
2002
)
Res
ista
nce
Myz
uspe
rsic
ae,
Mus
cado
mes
tica
Ove
rpro
duct
ion
ofca
rbox
ylas
esor
sodi
um-c
hann
elm
odul
atio
nPl
eiot
ropi
cef
fect
son
beha
vior
Fost
eret
al.(
2003
)
Res
ista
nce
Sacc
haro
myc
esce
revi
siae
Tra
nscr
iptio
nalr
egul
ator
sTw
ose
para
tem
utat
ions
,whi
chsi
ngly
incr
ease
resi
stan
cebu
ttog
ethe
rha
vene
gativ
eef
fect
son
fitn
ess
And
erso
net
al.(
2006
)
Res
ista
nce
Can
dida
albi
cans
Ove
rexp
ress
ion
ofdr
ug-r
esis
tanc
ede
term
inan
t3
diff
eren
tpat
tern
sev
olve
d,on
ein
volv
ing
asi
ngle
maj
orge
ne,t
heot
her
two,
whi
chw
ere
mor
eco
mm
on,
invo
lvin
gm
ultip
lege
nes
Cow
enet
al.(
2002
)
1022 EVOLUTION MAY 2007
PERSPECTIVE
general genetic model of caste determination nor does it imply
that wing development, or lack of, is a consequence of a single
gene or a single mutation. Caste determination in hymenoptera is
generally determined by environmental conditions during rear-
ing, including maternal inputs to the egg (Suzzoni et al. 1980;
Wheeler 1986, 1991), although there are cases of genetic differ-
ences among castes (Fraser 2000; Julian et al. 2002; Cahan and
Keller 2003). Genomic comparisons among castes have shown
that there is differential expression of numerous genes (Evans
and Wheeler 1999; Pereboom et al. 2005; Sumner et al. 2006),
though which ones are specifically required for determination is
not known. A general model for this mechanism of determina-
tion is the threshold model in which it is envisaged that at some
point in development the subsequent developmental trajectory is
determined by the value of some trait, called the liability, and a
threshold: values of the liability above the threshold shift develop-
ment into one trajectory whereas values below the threshold shift
development into the alternate path (Falconer 1965; Wright 1977;
Roff 1996a). The liability could indeed be equated to a single
gene that up- or downregulates some product, such as a hormone,
that controls future development. On the other hand, the liability
may be a function of a large number of factors, in which case
the liability may show a continuous distribution. In the former
case, evolution can be modeled using simple Mendelian popula-
tion genetics, whereas in the latter a quantitative genetic approach
is appropriate. With respect to wing dimorphism, it is intrigu-
ing to find that in holometabolous development, as found in the
hymenoptera, the vast majority of cases can be modeled using a
single locus model with winglessness being dominant, but in those
insects with hemimetabolous development a polygenic model best
fits the data (Roff and Fairbairn 1991).
Insects show enormous variation in the relative size of their
hind legs, which can be related to variation in the pattern of expres-
sion of the Ubx and abd-A genes (the method of detection could not
distinguish between these two and so their relative contributions
are not known; Mahfooz et al. 2004). Similarly, the activity of
the Bmp4 gene correlates with adult beak size in Darwin’s ground
finches (Abzhanov et al. 2004). Does this mean that leg length or
beak size is determined by the action of only one or two genes? It
is readily observed that there is continuous phenotypic variation
within populations and estimates of heritability of morphological
traits are relatively large (approximately 0.4, Mousseau and Roff
1987), which is inconsistent with single gene action. Morphol-
ogy is a result of a sequence of developmental processes, which
both affect and are affected by the expression of particular genes
such as Ubx, abd-A, and Bmp4. Even if we knew all the genes
involved in the developmental process, it is unlikely that we could
predict the results of selection on a single trait better than that
done by quantitative genetics (for reasons discussed below, the
jury is still out on whether the prediction of multivariate evolution
will typically require more than a traditional quantitative genetic
model).
An excellent illustration of the relationship between single
gene action and quantitative genetics is given by the study of
Roelofs et al. (2006) on additive genetic variation in metallothio-
nen expression in the collembolan Orchesella cincta. Tolerance
to heavy metals in this species is mediated by cadmium (Cd) ex-
cretion, which has been shown to have a heritability between 0.33
and 0.48 (Posthuma et al. 1993). It is known that the gene mt plays
a significant role in Cd excretion. Using quantitative polymerase
chain reaction (PCR), Roelofs et al. (2006) determined variation
in transcription rate of this gene and from parent–offspring regres-
sion estimated the heritability of transcription rate to be between
0.36 and 0.46, which agrees very well with the previously esti-
mated heritability for Cd excretion. Cadmium excretion is largely
under the control of a single gene (mt) but the expression of this
gene is itself modified by the action of other genes, thereby pro-
ducing continuous genotypic and phenotypic distributions.
Another example in which a single gene plays a key role
but its effect may be modeled by a quantitative genetic approach
is the gene FLC, which controls the onset of flowering in A.
thaliana (Sheldon et al. 2000). Flowering is controlled by the
induced transcription rate of FLC, variation in which is a func-
tion of both allelic variation at the FLC locus and the action of
other genes (Sheldon et al. 2000; Caicedo et al. 2004; see Rem-
ington and Purugganan 2003 for a review of other genes affect-
ing flowering time in plants). Epistatic interaction between the
genes FRI and FLC is responsible for clinal variation in flow-
ering time (Caicedo et al. 2004). It would be extremely inter-
esting to know if this epistatic interaction resulted in significant
epistatic variance.
Numerous mutations affecting life span in D. melanogaster
and C. elegans have been isolated (Table 1). Life span in
D. melanogaster has been the subject of intense study, both using
quantitative and genomic approaches. Life span responds readily
to selection with attendant correlated responses in physiology and
life-history traits, the mechanisms for which are still unresolved
(Valenzuela et al. 2004; Rose et al. 2005; Vermeulen and Bijlsma
2006). Single gene manipulations have shown that life span can be
substantially increased (up to 85%) and that no single gene deter-
mines this trait or even a unique mechanism by which longevity is
altered (see table 1 in Hughes and Reynolds 2005). Genomic anal-
yses have identified up to 25 QTL affecting longevity (Nuzhdin
et al. 2005). Eleven QTL were identified on chromosome 3 con-
taining from 12 to 170 positional candidate genes (Wilson et al.
2006). Quantitative trait loci analyses have also shown significant
dominance, epistatic and genotype by environment interactions
(Leips and Mackay 2002; Forbes et al. 2004). It is evident that
longevity is a highly complex trait likely involving a large ar-
ray of different physiological components. Although single gene
EVOLUTION MAY 2007 1023
PERSPECTIVE
mutations can have significant effects on longevity, the antagonis-
tic effects on other fitness components may exclude their invasion
into most natural populations: in the absence of such effects we
would expect these genes to be generally favored and spread to
fixation at which point they no longer contribute to variation (of
course high extrinsic mortality will greatly reduce the selective
advantage of longevity genes). The presence of dominance and
epistatic effects is not unexpected: life-history traits typically show
directional dominance (Roff 1997) and the complexity of phys-
iological components of longevity would argue for interactions
among loci. Whereas dominance effects may be revealed by con-
tributions to genetic variance, epistatic effects, even of large effect,
may contribute little to genetic variance, as illustrated, for example
by the lack of epistatic variance in Drosophila bristle number but
significant epistatic interaction revealed by QTL analysis (Mackay
and Lyman 2005). It remains to be shown if the epistatic effects
in longevity could play a significant role in evolutionary change
and thus need to be incorporated into a quantitative genetic model
of the evolution of life span.
Major gene effects conferring increased resistance to pes-
ticides, herbicides, and drugs have frequently been observed in
natural populations of animals and plants (Table 1; Jasieniuk et al.
1996; ffrench-Constant et al. 2004). In many cases the molec-
ular mechanism underlying this resistance is an upregulation of
transcription (Table 1; Taylor and Feyereisen 1996). Major gene
action is common in the evolution of insecticide resistance in nat-
ural populations but artificial selection appears to act on polygenic
variation (McKenzie and Batterham 1994). The precise reasons for
this are still debated (McKenzie and Batterham 1998; McKenzie
2000) but certainly a contributing factor is that the relevant muta-
tions are likely to be absent in laboratory populations but available
in the much larger natural populations. An understanding of the
potential genetic mechanisms available for resistance is, in this
case, important for predicting the circumstances under which par-
ticular evolutionary trajectories will be taken.
In summary, detailing the genetic mechanisms is an impor-
tant enterprise but, with relatively few exceptions, knowledge of
those mechanisms does not contribute to the prediction of the
evolutionary trajectory of traits that fall within the purview of
quantitative genetics. At present, although it is possible to simu-
late simple gene networks and follow their evolutionary change
(Frank 1999; Omholt et al. 2000; Hasty 2001; de la Fuente et al.
2002; Nijhout 2002; Bergman and Siegal 2003), we are nowhere
close to simulating the complexity of genetic interactions involved
in the determination of such traits as fecundity, longevity, or
body size.
An important area of research that is highlighted by the search
for specific genetic mechanisms is that of determining the number
of alternate paths to a single phenotype. Selection in the “classi-
cal” quantitative genetic model assumes equality of all loci, with
the result that the change in allelic frequencies during selection
may differ due to chance. Under this scenario two lines selected
in the same direction could display the same phenotype but differ
at particular loci. Because of nonadditive genetic interactions, a
cross between two such selected lines would not then necessarily
produce the same phenotype. For example, crosses between lines
of mice selected for growth rate revealed extensive nonadditive
interactions (Mohamed et al. 2001). Differences in genetic mecha-
nism have also been demonstrated in mice selected for thermoreg-
ulatory nest-building behavior (Bult and Lynch 1996). Perhaps,
even more intriguing is the possibility of different morpholog-
ical, physiological, or behavioral pathways leading to the same
selection response. Examples in this category include selection
on competitive ability in Drosophila (Joshi and Thompson 1995),
growth rate patterns in mice (Rhees and Atchley 2000), wheel
running in mice (Garland et al. 2002), and adaptive evolution to
growth media in Escherichia coli (Fong et al. 2005). Different
pathways to the same phenotype have also been found in natural
populations of D. subobscura. Near identical clines in wing size
is found in D. subobscura populations in Europe, South America,
and North America, but the components of the wing show striking
differences (Gilchrist et al. 2004). Crosses among populations of
D. melanogaster also suggest that different clines in wing size
have different genetic bases (Gilchrist and Partridge 1999). Such
results do suggest that research incorporating quantitative genetic
and mechanistic approaches are fundamental to the prediction of
evolutionary change and that we need to develop models that com-
bine these two components.
Testing Predictions of theMultivariate Breeder’s EquationWhereas QTL analysis can provide direct evidence for or against
the assumptions underlying the quantitative genetic framework,
indirect tests are provided by the ability of quantitative genetic
models to predict the rate and direction of evolutionary change.
Perhaps more importantly, the results of such experimental com-
parisons inform us on the robustness of the models to the un-
derlying assumptions. In this respect the record on predictions
for single trait responses to artificial selection is very good, ex-
cellent predictions being made for the first 10–15 generations of
selection, followed generally by the predicted decline in response
as variation is eroded (Hill and Caballero 1992; fig. 2.5 in Roff
2002). Artificial selection experiments also tend to support the
results from QTL analyses that genes of large effect frequently
occur (Hill and Caballero 1992). The analysis of trait variation
in wild populations, particularly responses following changes in
biotic or abiotic conditions, depends generally upon being able to
predict multivariate responses, and here even the results of artifi-
cial selection experiments are somewhat discouraging.
1024 EVOLUTION MAY 2007
PERSPECTIVE
Tab
le2.
Asu
rvey
of
biv
aria
tear
tifi
cial
sele
ctio
nex
per
imen
ts.
Spec
ies
Tra
it1
Tra
it2
Com
pare
dto
Res
ult
Ref
eren
cepr
edic
ted?
Sele
ctio
nin
allf
our
dire
ctio
nsB
icyc
lus
anya
naA
nter
ior
eyes
pot
Post
erio
rey
espo
tN
oB
oth
trai
tsre
spon
ded
Bel
dade
etal
.(20
02)
Bic
yclu
san
yana
Fore
win
gar
eaB
ody
wei
ght
No
Bot
htr
aits
resp
onde
dFr
anki
noet
al.(
2005
)M
ouse
12to
21-d
ayw
eigh
tgai
n51
day
wei
ght
Yes
Goo
din
two
dire
ctio
ns(H
–H;H
–L),
poor
inth
eot
her
two
(L–L
;L–H
)B
erge
ran
dH
arve
y(1
975)
D.m
elan
ogas
ter
Cox
als
Ster
nopl
eura
lbri
stle
sY
esG
ood
fiti
nea
rly
gene
ratio
n(1
0)po
orfi
tin
late
rge
nera
tion
(22)
Sher
idan
and
Bar
ker
(197
4)
Trib
oliu
mca
sten
eum
13-d
ayla
rval
wei
ght
Pupa
lwei
ght
Yes
Poor
,par
ticul
arly
for
anta
goni
stic
sele
ctio
nB
ella
ndB
urri
s(1
973)
Trib
oliu
mca
sten
eum
14-d
ayla
rval
wei
ght
30-d
ayla
rval
wei
ght
Yes
Poor
,par
ticul
arly
for
anta
goni
stic
sele
ctio
nO
kada
and
Har
din
(196
7)
Trib
oliu
mca
sten
eum
Pupa
lwei
ght
Egg
layi
ngY
esG
ood,
cons
iste
ntw
ithes
timat
esC
ampo
and
dela
Fuen
te(1
991)
One
dire
ctio
nof
sele
ctio
nre
info
rcin
gan
da
seco
ndan
tago
nist
icO
ntho
phag
usac
umin
atus
Hor
nle
ngth
Bod
ysi
zeN
oR
espo
nse
sam
ein
both
dire
ctio
nsE
mle
n(1
996)
Rei
nfor
cing
sele
ctio
nM
ouse
Post
wea
ning
wei
ghtg
ain
Litt
ersi
zeat
birt
hN
oB
oth
trai
tsre
spon
ded
Doo
little
etal
.(19
72)
D.m
elan
ogas
ter
Abd
omin
albr
istle
sSt
erno
pleu
ralb
rist
les
No
Bot
htr
aits
resp
onde
dSe
nan
dR
ober
tson
(196
4)Tr
ibol
ium
cast
eneu
mPu
palw
eigh
tFa
mily
size
Yes
Poor
,but
good
for
sing
letr
aits
Ber
ger
(197
7)Pl
ant
Hei
ght
Num
ber
ofle
aves
Yes
Goo
dM
atzi
nger
etal
.(19
77)
Ant
agon
istic
sele
ctio
nM
ouse
Tail
leng
thB
ody
wei
ght
No
Bot
htr
aits
resp
onde
dC
ockr
em(1
959)
Mou
seFo
odin
take
,or
gona
dalf
atpa
d,or
fatp
adB
ody
wei
ght
No
Bot
htr
aits
resp
onde
dSh
arp
etal
.(19
84)
Bra
ssic
ara
paFi
lam
entl
engt
hC
orol
lale
ngth
No
Bot
htr
aits
resp
onde
dC
onne
r(2
003)
Boa
rD
aily
wei
ghtg
ain
betw
een
30–8
0kg
Bac
kfa
tind
exat
80kg
No
Bot
htr
aits
resp
onde
dO
llivi
er(1
980)
Mou
seTa
ille
ngth
Bod
yw
eigh
tY
esPo
orR
utle
dge
etal
(197
3)M
ouse
Wei
ghta
t5w
eeks
Wei
ghta
t10
wee
ksY
esPo
orM
cCar
thy
and
Doo
little
(197
7)M
ouse
6-w
eek
body
wei
ght
Litt
ersi
zeat
birt
hY
esPo
orE
isen
(197
8)M
ouse
12-w
eek
fatw
eigh
tC
onst
ant1
2-w
eek
body
wei
ght
Yes
Fair
inon
edi
rect
ion,
poor
inth
eot
her
Eis
en(1
992)
Mou
se8-
wee
kbo
dyw
eigh
t3–
5w
eek
wei
ghtg
ain
Yes
Poor
von
But
ler
etal
.(19
86)
Mou
seW
eigh
tgai
n,bi
rth
to10
days
Wei
ghtg
ain,
28da
ysto
56da
ysY
esG
ood
inon
ere
gim
e,po
orin
anot
her
Atc
hley
etal
.(19
97)
Trib
oliu
mca
sten
eum
Bod
ysi
zePu
palw
eigh
tY
esPo
orC
ampo
and
Ray
a(1
986)
Trib
oliu
mca
sten
eum
Lar
valw
eigh
t,or
deve
lopm
entt
ime,
orpu
palw
eigh
t
Inde
xof
othe
rtw
oY
esG
ener
ally
poor
Sche
inbe
rget
al.(
1967
)
Trib
oliu
mca
sten
eum
Pupa
lwei
ghta
t21
days
Adu
ltbo
dyw
eigh
tat2
1da
ysY
esG
ood
inon
edi
rect
ion,
poor
inot
her
Cam
poan
dV
elas
co(1
989)
Chi
cken
Egg
wei
ght
Bod
yw
eigh
tY
esPo
orFe
stin
gan
dN
ords
kog
(196
7);
Nor
dsko
g(1
977)
Tur
key
Day
ste
sted
Egg
wei
ghta
ndra
teof
lay
Yes
Acc
urat
efo
rth
eon
ege
nera
tion
test
edG
arw
ood
etal
.(19
78)
Tur
key
8-w
eek
body
wei
ght
24-w
eek
body
wei
ght
Yes
Mod
erat
eA
bpla
nalp
etal
.(19
63)
Mai
zeY
ield
Ear
heig
htY
esPo
orM
olle
tal.
(197
5)So
ybea
nPr
otei
nco
ncen
trat
ion
Oil
cont
ent
Yes
Goo
din
one
dire
ctio
n,po
orin
othe
rO
pens
haw
and
Had
ley
(198
4)
EVOLUTION MAY 2007 1025
PERSPECTIVE
The general finding of artificial bivariate selection experi-
ments is that antagonistic selection, meaning selection opposite
to the sign of the genetic correlation, frequently does not accord
with prediction (Table 2). Various reasons have been advanced for
the poor response: incorrect initial estimates, maternal effects, ge-
netic drift, asymmetry in gene frequencies, type of index selection
applied, and functional constraints. However, in no case has the
cause of the irregularity in response been adequately analyzed.
If quantitative genetic theory cannot account for response to ar-
tificial bivariate selection then it will be severely limited in how
useful it can be in understanding short-term evolutionary change
in wild populations.
The breeder’s equation has been applied to explain selection
response in three natural populations: changes in a diapause com-
ponent, KP, in the lepidopteran, Hyphantria cunea (Morris 1971);
the evolution of body components in Darwin’s medium ground
finch, Geospiza fortis (Grant and Grant 1995); the evolution of ju-
venile hormone esterase (JHE) activity in the Bermuda population
of the sand cricket, Gryllus firmus (Roff and Fairbairn 1999). For
H. cunea, Morris (1971) successfully used the single trait breeder’s
equation to predict the change in Kp in three populations over 12
years (for a summary and discussion see Roff 1997, p. 157–159).
Roff and Fairbairn (1999) successfully predicted the correlated
response of JHE activity to changes in proportion macropterous
(long-winged and capable of flight) female G. firmus using genet-
ical parameters derived from laboratory rearings. Finally, Grant
and Grant (1995) obtained good agreement between observed and
predicted response to natural selection in G. fortis using genetical
parameters estimated from offspring–parent pedigrees in the same
population. Multivariate selection was overwhelmingly reinforc-
ing on G. fortis, meaning that selection was in the direction of
the genetic correlations, which is the case most likely in theory to
produce predictable responses (this also appears to be supported
by the empirical findings in Table 2, though the number of cases
I have been able to locate is surprisingly few).
To address the utility of the multivariate breeder’s equation
we need bivariate selection experiments in which both functional
and genetic factors that could restrict the evolutionary trajectory
can be explored. Such experiments will most likely be achievable
using an invertebrate or plant system, though a fast growing ver-
tebrate such as guppies might also be useful. Possible candidates
for which we have considerable information on functional and
genetic parameters are D. melanogaster (e.g., Roff and Mousseau
1987; Flatt et al. 2005; Chippindale et al. 2003; Rose et al. 2005),
Arabidopsis (e.g., Pigliucci 1998; Ungerer and Rieseberg 2003;
Ungerer et al. 2003; Koornneef et al. 2004), Manduca sexta (e.g.,
D’Amico et al. 2001; Davidowitz et al. 2005; Nijout et al. 2006,
2007), Bicyclus anynana (e.g., Beldade et al. 2002; Brakefield
et al. 2003; Zijlstra et al. 2003; Frankino et al. 2005), Onthoph-
agus sp. (Emlen 1996, 2000, 2001; House and Simmons 2005;
Emlen et al. 2006; Moczek 2006), and G. firmus (e.g., Roff and
Fairbairn 1999, 2001, 2006; Roff et al., 2002; Zera and Harshman
2001).
The Evolution of the Phenotypicand Genetic Variance–CovarianceMatricesA fundamental assumption of the foregoing discussion is that the
variance–covariance matrices do not themselves evolve. This is
clearly not the case but we presently lack a detailed theory on how
the matrix will change over time (Arnold et al. 2001; McGuigan
2006; Phillips and McGuigan 2006). Schluter (1996), assuming
that the G matrix remains constant, pointed out that evolution
would tend to follow the trajectory in which additive genetic vari-
ances are maximal: thus, for example, with two traits the evolu-
tionary path would at least initially tend to be in the same direction
as the major axis of the bivariate distribution. On the other hand,
we would also expect that variances and covariances would be
selected such that the resulting major axis of the bivariate distri-
bution would be in the direction of selection, that is, the G ma-
trix aligns itself to selection (Lande 1980; Cheverud 1984; Arnold
1992; Arnold et al. 2001). Some understanding of the evolution of
the G matrix under different types of selection has been achieved
by simulation (Jones et al. 2003, 2004) but empirical descriptions
of the manner of variation in the G matrix are still rather few
and general patterns have yet to emerge with which theoretical
analysis can be compared.
To date most empirical studies of the G matrix have focused
upon the question of whether G matrices vary among populations
or species (Roff 2000; Steppan et al. 2002). It comes as no surprise
that given sufficiently large sample sizes statistically significant
variation among G matrices is very common, if not ubiquitous. It is
time to depart from this hypothesis-testing approach and consider
the question of interval-estimation, that is, asking not whether
two matrices differ but what is the amount and pattern of differ-
ences (a point also pressed by Phillips and McGuigan 2006). A
potential stumbling block is the logistical difficulty of determin-
ing G matrices. One solution may be to use the P matrix as a
surrogate, which for morphological traits can be justified by the
close correspondence between the phenotypic and genetic corre-
lations (Cheverud 1988; Roff 1996b). However, a comparison of
how the P and G matrices interpreted variation among species
of crickets suggested that using P as a surrogate for G can be
misleading even for morphological traits (Begin and Roff 2004).
Because it is an important component of the breeder’s equation,
a study of variation in the P matrix is also of importance in its
own right, regardless of its possible use in place of G (Roff and
Mousseau 2005).
1026 EVOLUTION MAY 2007
PERSPECTIVE
ConclusionsQuantitative genetics has shown itself to be an extremely fruitful
approach to the analysis of quantitative variation. The intellectual
achievement of bringing together Mendelian genetics and statis-
tics was a landmark in evolutionary biology. The breeder’s equa-
tion, in either its singular or multivariate formulation, is elegant
in its simplicity yet has proven to be of high explanatory abil-
ity, though the predictive ability of the multivariate version needs
much more testing.
As a descriptor of genetic variation in a population the quanti-
tative genetic perspective has been extremely important. Analyses
of wild populations have shown that genetic variation is rampant
and generally ample for rapid evolutionary responses. At the level
of the genome the quantitative genetics perspective has played a
major role in bringing order to the vast amount of data extracted
from microarrays. The potential of this combination has yet to
be realized, but surely will be as the cost of microarray analy-
sis drops to a point at which it can be applied to standard ped-
igree designs.
The underlying assumptions of the breeder’s equation, in ei-
ther its singular or multivariate forms, have always been known
to be mathematical approximations of what is actually happening
at the level of the gene. The important question is simply how
good are these approximations? The results of single trait selec-
tion suggest that they are reasonable for short-term selection but
predictable deviations occur over the long term. Quantitative trait
loci analyses have shed more light on the number of loci and
the distribution of genetic effects but much remains to be learned
about the number of alleles and the distribution of genetic ef-
fects in a large outbreeding population. In particular, do QTLs of
major effect show such effects across the large array of genetic
backgrounds expected in an outbreeding population?
The considerable research done at the level of molecular ge-
netics has revealed extensive networks of interacting genes. Fre-
quently, genes of large effect are found and these may indeed be
common, though research tends to be directed towards detecting
such genes. While it is important to elucidate the genetic mecha-
nisms underlying traits, those of interest to quantitative geneticists
will generally be composed of such a large array on interacting
components that at this stage there is no possibility of creating
a useful mechanistic model for such traits. Quantitative genetics
cuts through this Gordian knot to provide a convenient and pow-
erful summary tool of these interactions. Further developments in
the mathematics of gene networks may provide a means of con-
necting mechanism and statistical description, but it remains to be
seen whether such would provide greater explanatory power than
presently provided by the quantitative genetic approach.
An area in which quantitative genetics has been surprisingly
unsuccessful is that of the quantitative prediction of multivariate
evolution when selection is antagonistic to the genetic covariances.
In large part this failing is due to a paucity of bivariate selection
experiments with follow-up analyses of the mechanistic causes for
the deviations from expectation. The recent acknowledgment of
the utility of selection experiments (Gibbs 1999; Brakefield et al.
2003; Conner 2003; Garland 2003; Fuller et al. 2005; Swallow and
Garland 2005) and of experimental evolution approaches (Bennett
and Lenski 1999; Stearns et al. 2000; Mery and Kawecki 2002;
Rose et al. 2005; Roff and Fairbairn 2007) will likely remedy
this situation.
Just as genetic variances are expected to evolve under the
force of selection so too are the G and P matrices expected to
evolve. Theoretical and numerical analyses of such evolution is
beginning, as is the description of variation of the matrices in wild
populations in relation to possible factors of selection, but we are
still at the early stages and this area is ripe for further study.
Quantitative genetics has proven itself of great utility over
the last 100 years. The advent of massive computing power and
the ability to delve into the molecular foundation of genetic vari-
ation promises to contribute to an increasing refinement of the
multivariate breeder’s equation: there is no reason to expect that
the contribution of quantitative genetics to our understanding of
the basis and evolution of trait variation will diminish in the
near future.
ACKNOWLEDGMENTSThis work is supported by National Science Foundation (NSF) grant DEB-0445140. I am very grateful for the constructive criticisms of the tworeviewers.
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