Upload
andrew-j-plumptre
View
213
Download
0
Embed Size (px)
Citation preview
Monitoring mammal populations with line transect
techniques in African forests
ANDREW J. PLUMPTRE
The Wildlife Conservation Society, 185th Street and Southern Boulevard, Bronx, New York, NY 10460±1099,
USA
Summary
1. Line transect survey techniques have been used to estimate population density
for a variety of mammal species in tropical forests. In many cases indirect methods,
surveying signs of animals such as counts of dung or nests, have been used because
of the poor visibility in these forests. The estimates of the production and decom-
position rates of these signs each have their associated errors; however, for the
majority of published studies these errors have not been incorporated into the esti-
mate of the standard errors or con®dence limits of the density estimate. An equa-
tion is given showing how this should be done.
2. An equation is also given relating the resolution (R) of a density estimate to the
coe�cient of variation (CV) of the estimate. This shows that to detect a 10%
change in a population the CV must be 3�6% (with a power of 50%) or 2�4% (with
80% power). Using this equation and data from studies in Africa, it is shown that
di�erences of less than 10±30% change in the population are unlikely to be
detected between two surveys where visual sightings of animals are made. When
indirect methods of estimating the population are used, it is unlikely that less than
a 30±50% change in the population could be detected.
3. Some studies have surveyed primate groups using estimates of an average group
spread. Data from primate groups in Budongo Forest, Uganda, show that group
spread is highly variable and varies at di�erent times of day and between months.
This survey technique is not recommended.
4. If line transects are used for monitoring populations, conversion factors should
be minimized as each contributes to an increase in the CV and a reduction in the
ability to detect small changes in population density.
5. Monitoring trends in abundance over several survey periods can improve the
detection of change, although this is costly and requires several surveys before any
conclusions can be reached. Re-using transects in subsequent surveys can also
reduce the variation around the estimate and will improve the resolution. Focusing
survey e�orts in areas of high density is an alternative strategy, but one that could
lead to other errors as high-density areas may be the safest and hence the last to
show change. Using biased survey methods is also a promising technique that can
increase the precision of surveys. It is concluded that a combination of di�erent
survey methods will ensure that changes in abundance are identi®ed.
Key-words: elephants, population errors, primates, surveying mammals.
Journal of Applied Ecology (2000) 37, 356±368
Introduction
Ecological monitoring should be a vital component
of any conservation project so that the e�ects ofCorrespondence: A.J. Plumptre (fax 718 3644275; e-mail
Journal of
Applied Ecology
2000, 37,
356±368
# 2000 British
Ecological Society
management can be assessed (Kremen, Merenlender
& Murphy 1994). Management plans always empha-
size that monitoring should take place and, more
recently, some have attempted to de®ne limits of
acceptable change beyond which management action
should be taken (Alexander 1996). However, if we
are to de®ne these limits, we must be certain that
our survey techniques can detect them.
The use of distance sampling techniques to esti-
mate animal population densities has become
increasingly popular since the production of the
computer package TRANSECT (Laake, Burnham &
Anderson 1979) and subsequently DISTANCE
(Buckland et al. 1993; Laake et al. 1994). In African
forests this technique has mainly been used to esti-
mate the density of primate groups (Whitesides et al.
1988; White 1992, 1994; Plumptre & Reynolds
1994), as many species are highly visible. Surveyors
of most other mammals in these forests have
resorted to indirect estimation techniques rather
than direct observation because visibility is often
poor and some species cannot be approached in
safety. In these surveys animal densities were calcu-
lated from line transects, counting signs that animals
leave behind, usually nests (apes: Ghiglieri 1984;
Tutin & Fernandez 1984; Wrogeman 1992; White
1994; Hashimoto 1995; Ihobe 1995; Marchesi et al.
1995; Plumptre & Reynolds 1996, 1997; Hall et al.,
1998a) or dung (elephants Loxodonta africana: Wing
& Buss 1970; Short 1983; Merz 1986; Barnes & Jen-
sen 1987; Dawson 1990; Ruggiero 1990; Fay &
Agnagna 1991; Barnes 1993; Plumptre & Harris
1995; ungulates: Plumptre 1991; White 1992, 1994;
Plumptre & Harris 1995). Indirect counts require
conversion factors to be calculated to convert the
count of dung or nests to animal density. These fac-
tors include the rates of production and the decay
rates of dung/nests. Some studies have avoided the
need to correct for the rate of decomposition of
dung or nests by counting the number that appear
over a certain time period. The same transects are
visited repeatedly during this period at intervals
shorter than the quickest time to decay. These are
referred to here as marked nest counts or clearance
plot dung counts (Plumptre & Reynolds 1996;
Staines & Ratcli�e 1987).
Where the animals/signs of interest occur in
groups, then conversions have to be made to calcu-
late animal/sign density from group density. This
has been particularly common in primate surveys
(Whitesides et al. 1988; Plumptre & Reynolds 1994),
where individual density has been calculated using
mean group size. Whitesides et al. (1988), in addi-
tion, recommended that a measure of mean group
spread be calculated for primate studies, using a per-
pendicular distance measure to the nearest animal to
the transect to calculate the perpendicular distance
from the transect to the centre of the group. They
argued that this was necessary because monkeys
further from the transect tended to be missed.
Each of these conversion factors has an associated
error. Few studies report their standard errors or
95% con®dence limits, and where they do these
errors are of the count only and rarely include errors
from conversion factors. If line transects are to be
used for monitoring populations of mammals then
the true errors of the estimate should be calculated.
This paper investigates how variation in conversion
factors and measures of e�ort a�ect the error of the
density estimate. Table 1 summarizes the errors asso-
ciated with di�erent methods of analysis.
Methods
LINE TRANSECT TECHNIQUES
Line transects are commonly established using a
strati®ed random sampling procedure (Plumptre &
Reynolds 1994). In African forests transects have
usually been walked at approximately 1 km hÿ1,counting all groups of animals seen from the trans-
ect. The perpendicular distance from the transect
line to the centre of the group seen is measured and
the number of animals seen in the group recorded
(Plumptre & Reynolds 1994; White 1994). The per-
pendicular distances are used to calculate a prob-
Table 1. The additional errors associated with direct and indirect counts of mammals from transects. These associated
errors should be calculated in addition to the error of the basic count.� � error associated with survey estimate; ±�noerror;�/±� can be an error depending on method used
Method Production rate Decomposition rate Group size Group spread
Direct counts
Sightings of single animals ± ± ± ±
Sightings of groups ± ± � � / ±Indirect counts
Dung counts � � � ±
Nest counts � � � ±
Clearance plot dung counts � ± � ±
Marked nest counts � ± � ±
357A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
ability density function that models the decrease in
sightings of animals with distance from the centre
line of the transect. This function is used to calculate
a density of groups with standard error and 95%
con®dence limits (Buckland et al. 1993). Individual
density can be calculated from group density by
multiplying by mean group size (see below). Esti-
mating density using line transects has been thor-
oughly covered by Buckland et al. (1993) and the
reader is referred to this book for details.
A Z-test is used to test whether two population
(Buckland et al. 1993, p. 381):
Z � D2 ÿD1
�p se�D2�2 � se�D1�2�where Dn � density estimate of population n or the
same population at time n; and se(Dn) � standard
error of this estimate
The assumptions for this test are that se(D2)�se(D1) and that the sample units from the ®rst sur-
vey are drawn independently from the sample units
in the second survey. An additional assumption is
that sample sizes are su�ciently large that the distri-
bution is close to normal. Sample size in transect
analyses is a function of the number of objects seen
and the number of transects censused. Buckland
et al. (1993) recommend that at least 10 transects
are censused to meet this assumption, although stu-
dies of elephant dung in Gabon indicate that 20±25
transects are required to approach normality (P.
Walsh, personal communication). With fewer than
this number of transects, it is better to use a t-distri-
bution (see Appendix 1 for a possible test).
Line transect surveying makes several assump-
tions (for details see Buckland et al. 1993): (i)
objects on the centre line are detected with certainty;
(ii) objects are detected at their initial location; (iii)
measurements are exact. Some papers state that an
object should not be counted on more than one
transect line, but this is not in fact an assumption of
this technique provided movement is random with
respect to the lines (Buckland et al. 1993, p. 37).
CALCULATING RESOLUTION OF DENSITY
ESTIMATION FROM TWO INDEPENDENT
SURVEYS
The resolution of a density estimate is de®ned here
as the percentage change that will be detectable
between two independent surveys. Surveys in Afri-
can forests are costly and there are few places where
more than two surveys have been carried out to date
(see Discussion). The resolution will depend on the
standard errors of the two density estimates. If initi-
ally we make an assumption that the standard error
of a density estimate is equal to the standard error
of a second density estimate, which is changed by a
factor R, i.e. D2�D1�D1*R, where D1 � density
estimate and R � proportional change or resolution
(100R�% change), then we can derive a simple
equation from the Z-test equation above to calculate
the resolution (R). Substituting D2�D1�D1*R in
the equation above:
Z � D1 ÿD1 �D1�R
�p se�D2�2 � se�D1�2�Therefore:
Z � D1�R
�p 2�se�D1�2���21:96
(for P� 0�05, 2-tailed test; but see below).Therefore:
R � 2:77se�D1�D1
� 2:77�CV=100� eqn 1
where CV � coe�cient of variation calculated by
DISTANCE.
For example, if we want to detect a 10% change
in the population then R� 0�1 and CV� 3�61%.
However, the power of the Z-test to detect a di�er-
ence at P� 0�05 is low (see Appendix 2), only
around 50%. If we want the power of the test to be
around 80% (as most textbooks suggest) then we
need to calculate the Z-test for 2�8 standard errors.
In this case CV� 2�4% (Appendix 2).
If the standard error of the second density esti-
mate di�ers from the ®rst (a violation of one of the
assumptions of the test, see above) then the number
in equation 1 changes and the resolution that is
detectable changes, although not greatly (Fig. 1).
This test provides a measure of the percentage
change in a population. However, a 100% increase
(population doubling) is di�erent to a 100%
decrease (population extinction). One way to deal
with this is to use di�erences between densities on a
logarithmic scale and the fact that the CV of the
density is approximately equal to the standard
deviation of the loge transformed density (P. Roth-
ery, personal communication). This method has the
advantage that working with log densities helps to
approximate a normal distribution. However, for
the purposes of this paper, percentage increases/
decreases will be used as examples because it is
easier to visualize references to 20% changes in the
text rather than di�erences on a logarithmic scale.
With indirect counts there are errors and CVs
associated with each conversion factor used. A stan-
dard dung survey, for example, corrects the dung
density for the decomposition rate and the deposi-
tion rate of dung:
T � DP=Q
where T � density of animals; D � density of dung
on transects; P � mean rate of decay (1/mean days);
358Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
and Q � mean number of dung piles produced per
day.
Barnes (1993) gives an equation (derived using the
delta method) that provides an approximate esti-
mate of the CV for the product of several variables:
CV2�T� � CV2�D� � CV2�P� � CV2�Q� eqn 2
where CV(X) � coe�cient of variation of variable X
(standard error/mean *100%) [CV(Q) is approxi-
mately � CV(1/Q)].
This equation assumes that the values of the com-
ponent variables are not correlated (for example it is
possible that dung decay is faster if dung density is
high because dung beetles are more abundant, in
which case this assumption would be invalid).
The variance of the corrected estimate is:
Var�T� � �D�P=Q�2���CV�D��2 � �CV�P��2
� �CV�Q��2�
RESOLUTION OF DIRECT OBSERVATIONS
FROM TRANSECT DATA IN AFRICA
Primate sightings
Data from primate surveys in the Budongo Forest
in western Uganda (Plumptre & Reynolds 1994,
1996) were used to investigate the e�ects of total dis-
tance walked and number of groups sighted. Data
were used from surveys of blue monkeys Cercopithe-
cus mitis Matschie and black and white colobus
monkeys Colobus guereza Ruppell in several com-
partments in the forest. In each compartment ®ve
transects were established using a strati®ed random
sampling procedure (Plumptre & Reynolds 1994),
and were walked twice each month during 1993.
The total length of transects was at least 10 km in
each compartment. The data were analysed each
time the transects were walked three times, until
they had been walked 21 times. This allowed the
change in the CV to be monitored with survey e�ort
and number of groups seen.
Nest counts
Data from gorilla Gorilla gorilla graueri Matschie
surveys (Hall et al. 1998b) and chimpanzee Pan
troglodytes schweinfurthi Blumenbach surveys
(Plumptre & Reynolds 1996; Hall et al. 1998b) were
used to investigate the e�ect of sample size on CV
of nest counts.
EFFECTS OF CORRECTION FACTORS USING
DATA FROM AFRICA
Dung defaecation rates
Standard errors and CVs of data for defaecation
rates that could be found in the literature (for large
African mammals) were calculated.
Fig. 1. The percentage change detectable (resolution) with a Z-test as the coe�cient of variation changes and the standard
errors of the density estimates change. The lines plotted are where the standard errors of two density estimates are equal
(SE1� SE2; assumed in equation 1) and also where one is half (SE1� 2SE2) or double (2SE1�SE2) the size of the other.Lines are plotted where the power of the test is around 50%.
359A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
Nest construction rates
Estimates of nest construction rate and its CV were
calculated from dawn to dusk follows of habituated
individuals in a community of chimpanzees in the
Budongo Forest in western Uganda. Only data from
complete dawn to dusk follows were used (Plumptre
& Reynolds 1997).
Nest decay rates
Mean time to nest decay has traditionally been cal-
culated from nest decay rates in the literature,
although nest decay can also be calculated in a simi-
lar way to decay of dung by ®tting an equation to
the decay curve and obtaining bootstrap estimates
of the error (Barnes & Barnes 1992; Barnes et al.
1994; Plumptre & Reynolds 1996). Fitting a decay
rate equation such as an exponential decay (Barnes
& Barnes 1992) has advantages in that the slowest
decomposing nests/dung do not need to be moni-
tored until they have disappeared before an estimate
for the rate can be obtained. However, this method
measures the median rate of decay rather than the
mean rate and it is recommended that mean rate is
used (Barnes & Barnes 1992; White 1995). CVs of
published mean time to nest decay studies were cal-
culated where the data were available to do so.
Dung decay rates
Barnes et al. (1994) provided data on bootstrapped
estimates of the median decay rate of elephant Lox-
odonta africana Blumenbach dung and its associated
errors for dung monitored in Ghana and Cameroon.
The e�ects of sample size on bootstrapped CV were
analysed using these data.
The combined e�ects of these errors for these con-
version factors were investigated using equation 2.
EFFECTS OF MEASURES OF GROUP SIZE
AND SPREAD ON PRIMATE SURVEYS
Individual animal density is calculated by multiply-
ing the group density by the mean group size. It is
sometimes found that large groups are seen at
further distances from the transects than small
groups, in which case it is necessary to correct for
this bias. Buckland et al. (1993, pp. 130±134) give
four methods to do this: (i) calculate mean group
size from observations within a strip width where
there is no bias observed; (ii) use the perpendicular
distance for the group to replace the group by n
individuals with the same perpendicular distance
(where n � number of animals seen); (iii) stratify the
density estimation procedures by group size
(requires a large sample size to do this); (iv) regress
group size with distance or estimated detection
probability. DISTANCE can carry out the last
method and by default regresses log(group size) on
the estimated detection probability. The e�ects of
correcting for group size on CV was investigated
with the primate data, correlating CV of group den-
sity with CV of individual monkey density calcu-
lated by DISTANCE.
Many primatologists have surveyed groups of pri-
mates by measuring the perpendicular distance to
the nearest animal in a group and then computing
an average group spread to calculate the true per-
pendicular distance to the group centre (Whitesides
et al. 1988; White 1994). This method assumes that
group spread on average is circular, constant
throughout the day and has no error associated with
its measurement. As Struhsaker (1997) pointed out,
primates often move in a linear fashion and are very
unlikely to be distributed in a circle. To test the
assumption that group spread is fairly constant,
measurements were made during dawn to dusk fol-
lows of 17 groups of monkeys (six blue monkey, six
black and white colobus monkey and ®ve redtail
monkey Cercopithecus ascanius Matschie) made
between October 1994 and January 1996 in the
Budongo Forest. Groups were located at around
16.00 h on day 1 and followed until dusk, then from
dawn until dusk on day 2 and on the third day from
dawn until the time at which they were found on
day 1. Each group was followed using this protocol
once each month. Group spread was measured
using a range®nder (often several measurements
were required to measure across the whole group as
visibility was not much greater than 30m; these
would be made to tree stems and summed across the
group). Group spread was measured in this manner
every 30min throughout the day.
Results
DIRECT OBSERVATIONS FROM TRANSECTS
Distance walked
Not surprisingly, increasing the distance walked
reduced the CV of group density in primates in
Budongo Forest (Table 2) because it increased the
numbers of groups encountered. What is of interest
here is that the CV remained fairly high (10±20%)
even when the distance walked was large (200� km),and the forest supports a relatively high density of
primates (Plumptre & Reynolds 1994). Conse-
quently, in order to detect this degree of change in
primate populations in Africa, it is necessary to
walk at least 200 km and probably further because
most other sites will have a lower sighting fre-
quency.
Number of groups seen
The number of groups seen strongly reduced the CV
for primate groups in Budongo Forest (Fig. 2). This
360Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
was expected as standard error (and hence CV) is
always reduced by increased sample size. By ®tting a
curve of the equation CV� a/p(N) (where N �number of groups seen; a� a constant) to these
points (Radj2 =0�93, F� 685�8, P<0�001) it can be
calculated that to detect a 10% change
(CV� 3�61%) in the group density you would need
to see about 1671 primate groups, and to detect a
20% change (CV� 7�22%) about 418 groups. How-
ever, as stated previously, the power to detect this
change is only about 50%. For a power of 80% the
respective values are 3781 (CV� 2�4%) and 1029
groups (CV� 4�6%).
Number of nests seen
Variation around group density estimates (chimpan-
zees and gorillas combined) for the number of nest
sites seen from transects was high. Fitting a similar
curve (CV� a/p(N)) of nest sites seen on CV gives
a reasonable regression (Radj2 =0�67, F� 36�2,
P<0�001). Using the equation derived, 349 nests
would need to be found to detect a 20% di�erence
and 1395 nests to detect a 10% change (again with
only a power of 50% to detect this change). For a
power of 80% the values are 3157 (10% change)
and 859 nests (20% change).
INDIRECT SURVEYING
Production rates
The defaecation rates of various mammals have
been calculated and published in the literature.
However, few studies have published the errors
around these rates. The CV for those that have are
Table 2. The number of groups seen, distance walked and coe�cient of variation (CV) for two monkey species in di�erent
compartments in Budongo Forest
Species Compartment Number of groups Distance walked (km) Density (groups kmÿ2) CV (%)
Blue monkey B1 163 210 21�0 9�7Cercopithecus mitis K11±13 16 210 2�9 37�9
W21 76 210 9�4 17�9K4 74 212 9�4 13�5N3 133 227 13�8 10�8
Black and white colobus B1 58 210 6�5 16�7Colobus guereza K11±13 47 210 6�6 16�7
K4 68 212 8�8 15�0N3 95 227 9�9 13�7
Fig. 2. Changes in coe�cient of variation with numbers of primate groups seen for surveys of blue and colobus monkeys in
di�erent forest compartments.
361A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
not too high (Table 3) and very much depend on the
number of days over which production was mea-
sured. For elephants, production has been calculated
by following the trails of a group over several days
for each estimate (Wing & Buss 1970; Tchamba
1991), providing a large sample size. For other esti-
mates individual animals have been monitored over
much less time and hence the CV is larger.
There is no published literature on the production
rates of nests by gorillas and only one for chimpan-
zees (Plumptre & Reynolds 1997). The mean pro-
duction rate from the dawn±dusk follows of
chimpanzees in Budongo was 1�15 nests per day
with a CV of 4�1%. This was based on 201 dawn±
dusk follows.
Decay rates
For nest decay, the mean number of days to com-
plete decay has been calculated to correct the nest
density estimate to an animal density. Two pub-
lished studies have provided measures of variance/
error around these mean estimates. In the Tai For-
est, mean decay was 73�3 days, SE� 9�7,CV� 13�3% (Marchesi et al. 1995), and in Budongo
Forest, mean decay was 45�9 days, SE� 3�6,CV� 7�8% (Plumptre & Reynolds 1996).
Barnes et al. (1994) used bootstrapping of median
time to decay (1000 replications) as a procedure to
calculate the standard error of the mean number of
days for elephant dung to decay. Dung was moni-
tored in di�erent sites or at di�erent times of year in
Ghana and Cameroon to provide 12 estimates of
decay rate with standard errors. The CV was about
5% with 70 monitored dung piles and 10% with 40
monitored piles.
Combining CVs for two independent surveys
A CV of 10% allows measurement of a 27�7%change in the population in a second survey (with
50% power). Counts of primates (Fig. 3) and nests
rarely had lower CVs, even with large sample sizes.
If CVs of dung/nest deposition and decay are
around 5% as well, then the total CV of the group
density estimate is:
�CV total�2 � �CV density�2 � �CV deposition�2
� �CV decay�2 � p�150� � 12�2%
This CV will allow detection of a 34% change in
the population (with 50% power) or a 67% change
(with 80% power). This is using fairly optimistic
estimates of CV for dung decay and deposition; sev-
eral estimates given above are larger than 5%. If
decay and deposition are both 10%, then only a
48% change in the population can be detected (50%
Table 3. The coe�cient of variation in the deposition rate of dung for various species, and construction rate of chimpanzee
nests from published studies. N � number of sample intervals over which dung/nest production was measured to obtain a
mean
Species N
Deposition
rate
(no. dayÿ1)CV
(%) Reference
Dung
Elephant Loxodonta africana Blumenbach 6 17�0 3�4 Wing & Buss (1970)
Elephant Loxodonta africana 16 19�8 1�2 Tchamba (1991)
Elephant Loxodonta africana 2 16�2 2�8 Plumptre (1991); A.J. Plumptre,
unpublished data
Bu�alo Syncerus ca�er Sparrmann 15 5�1 5�2 Plumptre (1991); A.J. Plumptre,
unpublished data
Okapi Okapia johnstoni P.Sclater 5 5�2 14�1 J. Hart, unpublished data
Blue duiker Cephalophus monticola Thunberg 4 4�9 26�5 Koster & Hart (1988)
Bay duiker Cephalophus dorsalis Gray 4 4�4 29�5 Koster & Hart (1988)
Bushbuck Tragelaphus scriptus Pallas 5 19�0 49�6 Plumptre (1991); A.J. Plumptre,
unpublished data
Blackbuck Antilope cervicapra L. 12 10�4 7�7 Rollins, Bryant & Montandon (1984)
Fallow deer Dama dama L. 12 11�3 11�5 Rollins, Bryant & Montandon (1984)
Sika deer Cervus nippon Temminick 20 6�9 4�3 Rollins, Bryant & Montandon (1984)
Axis deer Axis axis Erxleben 12 12�6 11�9 Rollins, Bryant & Montandon (1984)
White-tailed deer 12 19�6 11�7 Rollins, Bryant & Montandon (1984)
Odocoileus virginianus Zimmermann
Moose Alces alces L. 22 10�9 2�3 Miquelle (1983)
Nests
Chimpanzee P. troglodytes Blumenbach 14 1�15 4�1 A.J. Plumptre, unpublished data
362Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
power). For 80% power, not even 100% change can
be detected.
GROUP SIZE AND SPREAD
The primate groups followed in Budongo often split
up into two or more subgroups that could be sepa-
rated by 200� m. During a survey these would be
counted as separate groups, and hence the density
estimate would be overestimated if these were multi-
plied by a mean group size calculated from follow-
ing di�erent groups and counting all individuals
present. Consequently, it is recommended that the
number of animals seen from the transect should be
used as the group size in DISTANCE.
Density estimates of group density and total mon-
key density were calculated from the Budongo sur-
vey data using the corrected mean group size
(observed from the transects) and the default
method in DISTANCE. Regressing the CV of pri-
mate group density on the CV of total monkey den-
sity gave the following equation:
CV �total� � 1�005�CV group�
� 3�333�R2adj � 0�99; F � 4802; P < 0�001�
Therefore calculating total density from group
density increases the CV by 3�3% for the Budongo
data.
The CV of group spread was very low after a very
large sample size for all species (blue monkeys:
n� 3163, mean � 65�6m, CV� 1�0%; redtail mon-
key: n� 2426, mean � 64�6m, CV� 1�1%; colobus
monkey: n� 2698, mean � 31�5m, CV� 1�7%).
This small variation should be included in the total
survey variation if average group spreads are used
to calculate perpendicular distance.
A repeated measures general linear model analysis
was carried out to investigate the time of day and
month of the year on group spread. For each species
the natural logarithm of group spread was taken to
normalize the data. Primate group spread varied sig-
ni®cantly throughout the day (blue monkey:
F� 8480�2, d.f.� 1,5, P<0�001, range 6±321m;
redtail monkey: F� 4260�9, d.f.� 1,4, P<0�001,range 7±267m; colobus monkey: F� 8281�6,d.f.� 1,5, P<0�001, range 1±212m), increasing
between 06.00 and 08.00 h (Fig. 3), the time when
most surveys are taking place. Group spread also
varied signi®cantly between months (blue monkey:
F� 7622�1, d.f.� 1,5, P<0�001; redtail monkey:
F� 5140�6, d.f.� 1,4, P<0�001; colobus monkey:
F� 5678�9, d.f.� 1,5, P<0�001).Due to this variation in group spread it is con-
cluded that correcting perpendicular distance data
to the nearest individual in a group with a measure
of the radius of mean group spread (Whitesides et al.
1988) is not a good method and should be avoided.
It is better to measure the perpendicular distance to
the centre of the group of animals seen and count
these, or to measure distance to every individual in
the group and analyse the data for individuals (S.
Buckland, personal communication).
Fig. 3. Mean group spread for three primate species at di�erent times of day in Budongo Forest, Uganda.
363A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
Discussion
MONITORING
In African forests line transect surveys have mainly
been used to obtain density estimates of large mam-
mals, and few studies have established monitoring
programmes. It is often implied that subsequent sur-
veys will show whether the population is changing,
but little thought is given to planning future surveys.
If future surveys are to detect change then the
results in this paper show that both surveys must be
intensive. Where monitoring has occurred in Africa
it has provided useful data for conservation. For
example, detection of population changes of ele-
phants following aerial monitoring of several popu-
lations in savannas led to the placing of this species
on Appendix 1 of CITES (Douglas-Hamilton 1987;
Douglas-Hamilton, Michelmore & Inamdar 1992).
With the recent concessions made to allow limited
trade of ivory, it is vital that elephant populations
continue to be monitored. In forests this can cur-
rently only be achieved using line transect dung
counts (Barnes et al. 1994).
IMPROVING THE RESOLUTION BY
REPEATED SURVEYING OR REPEATED USE
OF TRANSECTS
If line transect methods are to be used for monitor-
ing animal populations in Africa, the results from
this study show that at best a 10±30% change in the
population will be detectable between two surveys,
and if high power is required for the test then the
percentage change detectable will be higher still.
Estimations of density using indirect methods (dung
or nest counts) will at best be able to detect a 30±
50% change in the population. These results are,
however, obtained on the assumption that two inde-
pendent surveys are made and that the two density
estimates obtained are tested for di�erences. The
resolution can be improved in two ways if this
assumption is not made:
1. carrying out regular surveys and ®tting a
trendline to the data obtained (Buckland & Anga-
nuzzi 1988; Buckland et al. 1993, pp. 392±396).
2. using the same transects for the second survey.
In this case the variance of the di�erence in the den-
sity estimate of the two surveys is reduced by the
covariance of the two estimates:
V�D2 ÿ D1� � V�D2� � V�D1� ÿ 2 cov �D2;D1�In this case it would be better to estimate density
for each transect separately (using the detection
function obtained by pooling data across all trans-
ects), and then use Wilcoxon's signed ranks test (or
a paired t-test if the data are normal) on the paired
data to assess whether there has been a signi®cant
change in the population (P. Rothery, personal com-
munication). This will be a more robust test than
the Z-test.
Both these improvements assume that funding for
surveys is regular, something that is rare in Africa.
Transect lines can become overgrown and di�cult
to ®nd after only 6 months, so that if regular sur-
veyors are to revisit lines then it will be necessary to
employ labourers to keep the lines open. Even for a
single survey the costs can be prohibitive if large
areas are being surveyed. The Wildlife Conservation
Society's Grauer's gorilla Gorilla gorilla graueri
Matschie survey in Kahuzi Biega National Park in
the Democratic Republic of Congo cost around
$80 000, and a recent survey of the mountain goril-
las in Bwindi Impenetrable National Park in
Uganda, covering only 325 km2, cost around
$35 000.
IMPROVING THE RESOLUTION TO DETECT
CHANGES IN TWO INDEPENDENT SURVEYS
Accuracy, bias and precision
The accuracy of a population estimate is a function
of the bias of the estimate and the precision of the
estimate. In most surveys line transects are estab-
lished using strati®ed random sampling methods to
eliminate any potential bias. However, the e�ort
required to do this may be at the expense of a larger
sample size because it takes more time to establish
transects than to use paths that already exist in the
forest. It is possible to census from paths in the for-
est, but this will give a biased estimate of the popu-
lation density. However, this biased estimate is
likely to be more precise for the same e�ort
(human-days) as a transect census because more
ground will be covered and a larger sample size is
more likely to be obtained. In order to improve the
ability to detect changes in a population, the preci-
sion of the two estimates must be high. If the bias
can be corrected, obtaining biased estimates may in
fact allow greater resolution.
Walsh & White (1999) have developed a method
that they call `reconnaissance (recce) walks' that fol-
low a path of least resistance through the forest.
They have found that elephant dung encounter rate
(Walsh & White 1999) and gorilla nest encounter
rate (Hall et al. 1998b) on recce walks are highly
correlated with encounter rates on nearby line trans-
ects. Thus, a statistically rigorous estimate of density
can be made from recce data if some e�ort is made
to calibrate the functional relationship between
recce and transect encounter rates and thereby cor-
rect for the bias. Therefore a combination of recce
and transect sampling should provide a more precise
estimate of density than transect sampling alone,
because transect sampling requires roughly three
364Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
times the e�ort necessary for recce sampling (Walsh
& White 1999).
Decay rates
The resolution of indirect counts can also be
improved by reducing the number of conversion fac-
tors involved. Transects that are visited regularly
can measure the accumulation of nests and dung
and thereby avoid the need to correct for decay
(marked nest counts in Plumptre & Reynolds 1996,
1997; clearance counts of dung in Staines & Ratcli�e
1987). Given the inter-seasonal variation in decay
rates of nests (Plumptre & Reynolds 1996) and dung
(Plumptre 1991; Plumptre & Harris 1995; A.
Nchanji, unpublished elephant dung data), dung
and nest count resolution is poor where decay rates
are calculated. It is not valid to calculate separate
dung decay rates for wet and dry seasons because
long-lived dung (such as elephant and bu�alo) sur-
vives from one season into the next and decays at a
di�erent rate to dung deposited in that subsequent
season (A. Nchanji, unpublished data). Many stu-
dies utilize nest or dung decay data from other sites
but, given the variation that occurs, these data are
likely to be inappropriate. However, repeatedly visit-
ing transects is more labour intensive and costly
than one-o� counts, and counting only fresh dung/
nests will result in lower sample sizes. Consequently
there is a trade-o� between the loss of precision due
to lower sample sizes and the decrease in resolution
as a result of correcting for decay rates. This should
be investigated further.
Defaecation rates
If surveys use indirect signs to estimate population
size, better estimates of defaecation rates and nest
production rates are needed with smaller CVs.
Many of the values for CV in Table 3 are high
because the observation time was short. Elephant
defaecation rates had the lowest CV because it is
possible to follow a group for several days and
hence obtain a large sample size. Population esti-
mates from indirect counts should incorporate the
errors of the deposition and decay rates in the error
of the estimate and the errors should be published
in papers.
Sample sizes
Sample sizes in surveys should reach at least 100
groups if the objective of the study is to monitor the
population changes in future. A pilot study should
be carried out to determine the sighting rate prior to
commencing the main survey. For rare species,
obtaining 100 sightings is likely to require many
hundreds of kilometres of transects, and conse-
quently line transects may not be appropriate and
recce walks may be a better method. One option is
to concentrate transects in areas where densities are
known to be high or that are visited regularly by the
animals, and to monitor these areas. In the forests
of central Africa many animals visit waterholes/salt
licks or `bais' (Turkalo & Fay 1995), and monitor-
ing could be better concentrated at sites such as
these. This method would assume that habitat use
does not change over time, however, and care must
be taken to ensure that monitoring also occurs else-
where at the same time to con®rm this. It is possible
that populations will concentrate at these sites when
they are declining elsewhere if these sites are consid-
ered `safe' or `good habitat', and general population
declines will not be detected until it is too late to do
anything.
Monitoring of animal populations in African for-
ests must rely on information from various sources
in order to adapt management practices in time to
assist declining populations. Relying solely on trans-
ect counts is inadvisable because of the low resolu-
tion of changes that can be detected. For example, if
elephant populations are to be monitored in forests
it would be advisable to focus dung counts in
regions where the population is known to be high,
whilst at the same time having some transects or
camera traps in low density regions (where the data
of interest will be presence or absence, rather than
density or encounter rates). In addition, records of
carcasses should be collected and surveys of meat in
markets conducted so that additional data are avail-
able from other sources. Using a multi-method
approach such as this is likely to give a clearer pic-
ture of changes in mammal abundance.
RECOMMENDATIONS FOR MONITORING IN
TROPICAL FORESTS
1. Carry out a pilot study prior to a survey to deter-
mine the encounter rate along transects: are trans-
ects going to be a suitable method to use? At the
same time test the possible use of recce walks or
other biased survey methods that may give more
precise but biased estimates (if the bias can be cor-
rected).
2. Obtain data on decay rates of signs and, if the
variation is high, consider the use of repeated sur-
veys along transects.
3. Obtain at least 100 sightings of groups or sepa-
rate sightings of individuals.
4. If possible and if the budget allows it, survey reg-
ularly and ®t trendlines to the data. Re-use the same
transects wherever possible.
5. Record the number of animals seen whenever a
group is sighted and do not use measures of group
spread to correct the perpendicular distance.
6. Obtain good measures of the production rate of
signs so that the associated CV is small.
365A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
7. Think about a variety of methods that can be
used to monitor the population in question and do
not rely on one method.
Acknowledgements
I would like to thank many of the people who have
contributed through informal discussion to the ideas
in this paper. In particular John Hart (who also pro-
vided data for Table 2), Peter Walsh and Lee White
have made me think hardest about survey methods
and monitoring. Len Thomas, Peter Rothery and
Peter Walsh have all provided helpful advice on the
statistics given here, and provided solutions given in
the Appendices. I am also grateful to the two anon-
ymous referees whose advice greatly improved this
paper. Data collected in the Virungas, Rwanda, on
dung production was funded by Bristol University,
Fauna and Flora International and the Dian Fossey
Gorilla Fund. Data collected in Budongo Forest,
Uganda, was funded by ODA, National Geographi-
cal Society, Jane Goodall Institute and the Wildlife
Conservation Society. I am grateful to the Ugandan
and Rwandan ®eld assistants who helped collect
these data, particularly Mutungire Nabert, Muhu-
muza Geresomu, Kyamanywa Julius, Uwimana
Fidele, Tolith Alfred, Hatari Stephen, Biroch God-
frey, Tuka Zephyr, Tinka John, Kugonza Dissan,
Kakura James and Akanya Martin and other sta�
of the Budongo Forest Project and the Karisoke
Research Centre. I am also grateful to the Institute
of Biological Anthropology at Oxford University
and in particular Professor Vernon Reynolds for
support whilst working in Uganda.
References
Alexander, M. (1996) Management Planning for SSSIs.
Countryside Council for Wales, Gwynedd, UK.
Barnes, R.F.W. (1993) Indirect methods for counting ele-
phants in forest. Pachyderm, 16, 24±30.
Barnes, R.F.W. & Barnes, K.L. (1992) Estimating decay
rates of elephant dung piles in forest. African Journal
of Ecology, 30, 316±321.
Barnes, R.F.W. & Jensen, K.L. (1987) How to count ele-
phants in forests. IUCN African Elephant and Rhino
Specialist Group Technical Bulletin, 1, 1±6.
Barnes, R.F.W., Asamoah-Boateng, B., Majam, J.N.,
Ageyei-Ohemeng, J., Tchamba, M.N., Ekobo, A. &
Nchanji, A. (1994) Improving the Accuracy of Forest
Elephant Census Methods: Studies of Dung Decay
Rates in Ghana and Cameroon. European Commission
DG VIII: Ecology in Developing Countries Pro-
gramme (Vol. 5). African Elephant Conservation Pro-
gramme, Environment and Development Group,
Oxford, UK.
Buckland, S.T. & Anganuzzi, A.A. (1988) Estimated trends
in abundance of dolphins associated with tuna in the
eastern tropical Paci®c. Report of the International
Whaling Commission, 38, 411±437.
Buckland, S.T., Anderson, D.R., Burnham, K.P. & Laake,
J.L. (1993) Distance Sampling: Estimating Abundance
of Biological Populations. Chapman & Hall, London,
UK.
Dawson, S. (1990) A model to estimate density of Asian ele-
phants (Elephus maximus) in forest habitats. MSc The-
sis. Oxford University, Oxford, UK.
Douglas-Hamilton, I. (1987) African elephant population
trends and their causes. Oryx, 21, 11±14.
Douglas-Hamilton, I., Michelmore, I.F. & Inamdar, A.
(1992) African Elephant Database. UNEP, Nairobi,
Kenya.
Fay, J.M. & Agnagna, M. (1991) A population survey of
forest elephants (Loxodonta africana cyclotis) in north-
ern Congo. African Journal of Ecology, 29, 177±187.
Ghiglieri, M.P. (1984) The Chimpanzees of Kibale Forest: A
Field Study of Ecology and Social Structure. Columbia
University Press, New York, NY.
Hall, J.S., Saltonstall, K., Inogwabini, B.I. & Omari, I.
(1998a) Distribution, abundance and conservation sta-
tus of Grauers gorilla. Oryx, 32, 122±130.
Hall, J.S., White, L.J.T., Inogwabini, B.I., Ilambu, O.,
Morland, H.S., Williamson, E.A., Saltonstall, K.,
Walsh, P., Sikubabwo, C., Dumbo, B., Kaleme, P.K.,
Vedder, A. & Freeman, K. (1998b) A survey of
Grauers gorillas (Gorilla gorilla graueri) and chimpan-
zees (Pan troglodytes schweinfurthi) in the Kahuzi
Biega National Park lowland sector and adjacent for-
est in eastern Congo. International Journal of Primatol-
ogy, 19, 207±235.
Hashimoto, C. (1995) Population census of the chimpan-
zees in the Kalinzu forest, Uganda: comparison
between methods with nest counts. Primates, 36, 477±
488.
Ihobe, H. (1995) The diurnal primate fauna and popula-
tion densities of Tschego chimpanzees in southwestern
Congo. African Study Monographs, 16, 35±44.
Koster, S.H. & Hart, J.A. (1988) Methods of estimating
ungulate populations in tropical forests. African Jour-
nal of Ecology, 26, 117±126.
Kremen, C., Merenlender, A.M. & Murphy, D.D. (1994)
Ecological monitoring: a vital need for integrated con-
servation and development programs in the tropics.
Conservation Biology, 8, 1±10.
Laake, J.L., Burnham, K.P. & Anderson, D.R. (1979)
Users' Manual for Program TRANSECT. Utah State
University Press, Logan, UT.
Laake, J.L., Buckland, S.T., Anderson, D.R. & Burnham,
K.P. (1994) DISTANCE User's Guide V2.1. Colorado
Cooperative Fish and Wildlife Research Unit, Color-
ado State University, Fort Collins, CO.
Marchesi, P., Marchesi, N., Fruth, B. & Boesch, C. (1995)
Census and distribution of chimpanzees in Cote
d'Ivoire. Primates, 36, 591±607.
Merz, G. (1986) Counting elephants (Loxodonta africana
cyclotis) in tropical rain forests with particular refer-
ence to Tai National Park, Ivory Coast. African Jour-
nal of Ecology, 24, 61±68.
Miquelle, D. (1983) Summer defecation-urination rates and
volumes of moose. Journal of Wildlife Management,
47, 1230±1233.
Plumptre, A.J. (1991) Plant±herbivore dynamics in the Bir-
ungas. PhD Thesis. University of Bristol, Bristol, UK.
Plumptre, A.J. & Harris, S. (1995) Estimating the biomass
of large mammalian herbivores in a tropical montane
forest: a method of faecal counting that avoids assum-
ing a `steady state' assumption. Journal of Applied
Ecology, 32, 111±120.
Plumptre, A.J. & Reynolds, V. (1994) The impact of selec-
tive logging on the primate populations in the
Budongo Forest Reserve, Uganda. Journal of Applied
Ecology, 31, 631±641.
366Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
Plumptre, A.J. & Reynolds, V. (1996) Censusing chimpan-
zees in the Budongo forest, Uganda. International
Journal of Primatology, 17, 85±99.
Plumptre, A.J. & Reynolds, V. (1997) Nesting behavior of
chimpanzees: implications for censuses. International
Journal of Primatology, 18, 475±485.
Rollins, D., Bryant, F.C. & Montandon, R. (1984) Fecal
pH and defecation rates of eight ruminants fed known
diets. Journal of Wildlife Management, 48, 807±813.
Ruggiero, R.G. (1990) The ecology and conservation of the
African elephant (Loxodonta african). PhD Thesis.
University of Ann Arbor, Ann Arbor, MI.
Short, J.C. (1983) Density and seasonal movements of the
forest elephant (Loxodonta africana cyclotis Matschie)
in Bia National Park, Ghana. African Journal of Ecol-
ogy, 21, 175±184.
Staines, B.W. & Ratcli�e, P.R. (1987) Estimating the abun-
dance of red deer (Cervus elaphus L.) and roe deer
(Capreolus capreolus L.) and their current status in
Great Britain. Symposium of the Zoological Society of
London, 58, 131±152.
Struhsaker, T.T. (1997) Ecology of an African Rain Forest.
University Press of Florida, Gainesville, FL.
Tchamba, M.N. (1991) Defaecation by the African forest
elephant (Loxodonta africana cyclotis) in the Santchou
reserve, Cameroon. Nature et Faune, 7, 27±31.
Turkalo, A. & Fay, J.M. (1995) Studying forest elephants
by direct observation: preliminary results from Dzan-
gha clearing, Central African Republic. Pachyderm, 20,
45±54.
Tutin, C.E.G. & Fernandez, M. (1984) Nationwide census
of gorilla (Gorilla g. gorilla) and chimpanzee (Pan t.
troglodytes) populations in Gabon. American Journal
of Primatology, 6, 313±336.
Walsh, P.D. & White, L.J.T. (1999) What will it take to
monitor forest elephants? Conservation Biology, 13,
1194±1202.
White, L.J.T. (1992) Vegetation history and logging distur-
bance: e�ects on rainforest mammals in the Lope
Reserve, Gabon. PhD Thesis. University of Edinburgh,
Edinburgh, UK.
White, L.J.T. (1994) Biomass of rain forest mammals in
the Lope Reserve, Gabon. Journal of Animal Ecology,
63, 499±512.
White, L.J.T. (1995) Factors a�ecting the duration of ele-
phant dung piles in rain forest in the Lope Reserve,
Gabon. African Journal of Ecology, 33, 142±150.
Whitesides, G.H., Oates, J.F., Green, S.M. & Kluberdanz,
R.P. (1988) Estimating primate densities from transects
in a West African rainforest: a comparison of techni-
ques. Journal of Animal Ecology, 57, 345±367.
Wing, L.D. & Buss, I.O. (1970) Elephants and forests.
Wildlife Monographs, 19, 1±92.
Wrogemann, D. (1992) Wild chimpanzees in Lope, Gabon:
census method and habitat use. PhD Thesis. Bremen
University, Bremen, Germany.
Received 10 June 1998; revision received 28 December 1999
Appendix 1
t-test to test di�erences in density estimates (L. Tho-
mas, personal communication).
This test may be more appropriate than the Z-test
for small sample sizes. The only approximations
available are designed for the case where the t distri-
bution is being used to compare two sample means.
Their performance when comparing two estimates is
unknown. However, an approximation is as follows:
t � �densityÿ1ÿ densityÿ2�=sigmawhere sigma (the standard error, or standard devia-
tion of the di�erence in estimates) is estimated by:
p��SE survey 1�2 � �SE survey 2�2�The degrees of freedom for this t-test are:
� ��SE 1�2 � �SE 2�2��p
��SE 1�4=dfÿ1� �SE 2�4=dfÿ2�d.f._1 and d.f._2 come from the formulae in Buck-
land et al. (1993, pp. 89±90).
Appendix 2
Statistical power of Z-test (P. Rothery, personal com-
munication; L. Thomas, personal communication).
To approximate the power of the Z-test the actual
di�erence and the standard error of the estimated
di�erence are required. This can be seen as follows.
A di�erence is detected at the 5% level when the
standardized di�erence D/s[D] is larger than 1�96 or
less than ÿ1�96, where D is the estimated di�erence.
The power of the test is then given by:
Power � 1 ÿ Prob� ÿ 1�96 < D=SE�D�
< 1�96� � 1 ÿ Prob� ÿ 1�96�SE�D�
< D < 1�96�SE�D��
If Dtrue is the true di�erence, then the above
expression for power can be written as:
Power � 1 ÿ Prob� ÿ 1�96�SE�D� ÿ Dtrue
< D ÿ Dtrue < 1�96�SE�D� ÿ Dtrue�
or
Power � 1 ÿ Prob� ÿ 1�96 ÿ Dtrue=SE�D�
< �D ÿ Dtrue�=SE�D�
< 1�96 ÿ Dtrue=SE�D��If D follows a normal distribution with mean
Dtrue and standard error SE[D], then the quantity
Z� (DÿDtrue)/SE[D] follows a standardized nor-
mal distribution with mean zero and standard devia-
tion of one. The power is then given by:
Power � 1 ÿ Prob� ÿ 1�96 ÿ Dtrue=SE�D�
< Z < 1�96 ÿ Dtrue=SE�D��The probability can be looked up in tables of the
367A.J. Plumptre
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368
standardized normal distribution or calculated using
a statistical package such as Minitab.
If we apply the above formula to calculate power
for detecting a di�erence of two standard errors, i.e.
Dtrue � 2*SE[D], then we have:
Power � 1 ÿ Prob� ÿ 3�96 < Z
< ÿ 0�04� � 0�52The corresponding power for detecting a di�er-
ence of three standard errors is give by:
Power � 1 ÿ Prob� ÿ 4�96 < Z
< ÿ 1�04� � 0�85The method can be related to the estimation of
changes in density as follows. Let D1true and
D2true denote the true densities at times 1 and 2,
with change in density given by:
Dtrue � D2true ÿ D1true � R�D1true
Let D1 and D2 be estimated densities at times 1
and 2, respectively, with change estimated as
D�D2ÿD1. If the coe�cient of variation of each
estimated density is equal to C, then:
SE�D1� � C�D1;SE�D2� � C�D2
The standard error of the estimated di�erence is
then given by:
SE�D� � C�D1true�p�1 � �1 � R�2�
So:
Dtrue=SE�D� � R=fC�p�1 � �1 � R�2�gFor a 10% change (R� 0�10) and C� 0�036 then:
Dtrue=SE�D� � 0�10=�0�036�1�49� � 1�87with corresponding power of about 53%. For 80%
power, Dtrue/SE[D]� 2�8 and C� 0�024.
368Line transect
surveys in
tropical forests
# 2000 British
Ecological Society
Journal of Applied
Ecology, 37,
356±368