ORIGINAL RESEARCH ARTICLE
Pooled Population Pharmacokinetic Analysis of Phase I, II and IIIStudies of Linifanib in Cancer Patients
Ahmed Hamed Salem • Denise Koenig • Dawn Carlson
Published online: 4 December 2013
� Springer International Publishing Switzerland 2013
Abstract
Background and Objective Linifanib is a multi-targeted
receptor tyrosine kinase inhibitor, which can inhibit
members of the vascular endothelial growth factor and
platelet-derived growth factor receptor families. The
objective of this analysis was to characterize the population
pharmacokinetics of linifanib in cancer patients.
Methods We pooled 7,351 linifanib plasma concentra-
tions from 1,010 cancer patients enrolled in 13 clinical
studies. Population pharmacokinetic modelling was per-
formed using NONMEM version 7.2. The covariates that
were screened included the cancer type, co-medications,
creatinine clearance, formulation, fed status, liver function
markers (bilirubin, blood urea nitrogen [BUN], aspartate
aminotransferase [AST], alanine aminotransferase [ALT]),
albumin, age, sex, race, body weight, surface area and body
mass index.
Results A two-compartment model with first-order
absorption and disposition best described linifanib phar-
macokinetics. An increase in body weight was associated
with less than proportional increases in volumes of distri-
bution. Subjects with hepatocellular carcinoma and renal
cell carcinoma were estimated to have 63 and 86 % larger
volumes of distribution, respectively, than subjects with the
other cancer types. Females had 25 % slower oral clear-
ance (CL/F) than males, while subjects with colorectal
cancer had 41 % faster CL/F than other subjects. For
linifanib bioavailability, subjects with refractory acute
myeloid leukaemia or myelodysplastic syndrome had 43 %
lower bioavailability, evening doses were associated with
27 % lower bioavailability than morning doses, and
administration of linifanib under fed conditions decreased
the bioavailability by 14 %. Finally, the oral solution for-
mulation showed two-fold faster absorption than the tablet
formulations.
Conclusion The use of mixed-effects modelling allowed
robust assessment of the impact of the concomitant effects
of body size, different cancer types, formulation, diurnal
variation, sex and food on linifanib pharmacokinetics. The
developed population pharmacokinetic model describes
linifanib concentrations adequately and can be used to
conduct simulations or to evaluate the linifanib exposure–
response relationship.
1 Introduction
Angiogenesis is essential for tumour growth and metasta-
sis. Lack of adequate vasculature results in tumours
becoming necrotic or apoptotic, and restrict the tumour size
[1, 2]. Angiogenesis involves an imbalance between anti-
angiogenic and proangiogenic molecules such as vascular
endothelial growth factor (VEGF) secreted from tumour
cells [3]. In addition, platelet-derived growth factor
(PDGF) stimulates tumour growth and enhances angio-
genesis by facilitating pericyte coverage of new micro-
vessels [4, 5]. Thus, inhibition of VEGF and PDGF
receptors (VEGFR and PDGFR) has been a compelling
target for cancer therapy [6, 7].
Results from clinical studies of bevacizumab, a selective
monoclonal antibody against VEGFR, validated the
A. H. Salem (&) � D. Koenig � D. Carlson
Clinical Development, AbbVie Inc., 1 North Waukegan Road,
AP13A-3, Dept. R4PK, North Chicago, IL 60064, USA
e-mail: [email protected]
A. H. Salem
Department of Clinical Pharmacy, Faculty of Pharmacy,
Ain Shams University, Cairo, Egypt
Clin Pharmacokinet (2014) 53:347–359
DOI 10.1007/s40262-013-0121-2
targeting of VEGF-induced angiogenesis as an effective
anti-cancer therapeutic strategy [8–10]. Combined inhi-
bition of VEGFR and PDGFR is hypothesized to have a
greater antitumour effect than inhibition of individual
receptors [11]. In fact, there are three receptor tyrosine
kinase inhibitors—sorafenib, sunitinib and pazopanib—
that target both VEGFR and PDGFR, and they are already
approved for treatment of various solid tumour types,
with many more being in development. Linifanib (ABT-
869) is an orally active, multi-targeted receptor tyrosine
kinase inhibitor, which inhibits members of the VEGFR
and PDGFR families [12]. Linifanib exhibits more
selective inhibitory activity than other small molecules
targeting VEGFR and PDGFR tyrosine kinases, with less
activity against other unrelated tyrosine or serine/threo-
nine kinases [13]. Linifanib has demonstrated potent
antiproliferative and apoptotic effects on cancer cells and
has exhibited efficacy in human fibrosarcoma and breast,
colon and small cell lung carcinoma xenograft models
[13]. Evidence of encouraging clinical activity of linifanib
monotherapy has been demonstrated in relapsed or
refractory non-small cell lung cancer (NSCLC), hepato-
cellular carcinoma (HCC) and sunitinib-resistant renal cell
carcinoma (RCC) [14, 15].
Pharmacokinetic assessments in cancer patients have
shown that linifanib is rapidly absorbed, with an average
time to reach the peak concentration (tmax) of 2–3 h [16,
17]. The elimination half-life of linifanib ranged from 13.9
to 24 h in clinical studies [17, 18]. Linifanib pharmacoki-
netics showed dose proportionality over a 0.1–0.3 mg/kg
dose range [19]. Linifanib is predominantly metabolized,
with urinary recovery analysis showing that less than 5 %
of the linifanib dose is recovered in the urine as the
unchanged drug and metabolite [20]. The main systemic
metabolite for linifanib is the carboxylate metabolite [17].
The objectives of this analysis were to integrate the li-
nifanib concentration–time data from 13 clinical studies to
characterize the population pharmacokinetics of linifanib,
including identifying the structural pharmacokinetic model,
estimating pharmacokinetic parameters and associated
inter-individual variability, and testing patient demo-
graphics and covariates for their potential influence on
linifanib pharmacokinetics.
2 Methods
2.1 Clinical Studies and Patient Population
The population pharmacokinetic analysis included linifanib
plasma concentration data from 1,010 adults who partici-
pated in six phase I, six phase II and one phase III linifanib
clinical trials.
Table 1 summarizes the clinical studies used in this
analysis and their dosing and sampling schemes. The study
protocols were approved by the institutional review boards
of the individual study sites, and written informed consent
was obtained from each subject prior to enrolment. All
subjects were older than 18 years, with a histologically
confirmed malignancy.
2.2 Sample Collection and Quantification
Blood samples were collected, via venipuncture or a cen-
tral line, into ethylenediaminetetraacetic acid (EDTA)
tubes and stored on ice until centrifugation. Plasma sam-
ples were then stored at approximately -20 �C until ana-
lysis. Samples from all studies were analysed for plasma
concentrations of linifanib, using a validated liquid chro-
matography with tandem mass spectrometric detection
assay. The coefficient of variation was B7.7 %, indicating
the precision of the assay. The accuracy of the assay was
101.7 % at the lower limit of quantification (LLQ) and
ranged between 96.7 and 102.2 % at higher standard levels.
The LLQ was 1 ng/mL. Observations below the LLQ were
not included in the analysis.
2.3 Nonlinear Mixed-Effects Modelling
The population pharmacokinetic model was built using
nonlinear mixed-effects modelling in NONMEM ver-
sion 7.2 software (Icon Development Solutions, Ellicott
City, MD, USA). The first-order conditional estimation
method with interaction (FOCEI) was employed within
NONMEM. Diagnostic graphs and additional statistical
analyses were conducted using SAS version 9.3 and
R version 2.15.2 software. Development of the population
pharmacokinetic model started with construction of the
base model, including the structural pharmacokinetic
model and models for the inter-individual and residual
variabilities. Once the base model was developed, covari-
ate models were developed to explain the inter-individual
and residual variabilities.
2.3.1 Development of the Base Model
After the dose proportionality of linifanib was established,
standard linear compartmental models with first-order
absorption and elimination (ADVAN2, ADVAN4 or
ADVAN12) were evaluated for describing linifanib phar-
macokinetics. Different structures of the X matrix were
explored. Inter-individual variability in pharmacokinetic
parameters was modelled using an exponential error model
as shown for oral clearance (CL/F) in Eq. 1:
CL=F ¼ h1 � expðg1Þ ð1Þ
348 A. H. Salem et al.
Ta
ble
1C
har
acte
rist
ics
of
the
clin
ical
tria
lsin
clu
ded
inth
ean
aly
sis
Stu
dy
no
.S
ubje
cts
(n)
Stu
dy
po
pula
tio
nD
ose
sP
har
mac
ok
inet
icsa
mp
lin
gti
mes
Ag
e[y
ears
]aB
od
yw
eig
ht
[kg
]aS
ex[n
;m
ale/
fem
ale]
Rac
e[n
;W
hit
e/A
sian
/oth
er]
Ph
ase
Ist
ud
ies
13
3A
dv
ance
dn
on
-hae
mat
olo
gic
alm
alig
nan
cies
10
mg
;0
.1,
0.2
5,
0.3
mg
/kg
Inte
nsi
ve
(cycl
e1
day
1:
0,
0.5
,1
,2
,3
,4
,6
,8
,2
4h
;cy
cle
1d
ay1
5:
0,
0.5
,1
,2
,3
,4
,6
,8
h;
add
itio
nal
sam
ple
so
ncy
cle
3d
ay1
and
ever
y2nd
trea
tmen
tper
iod
ther
eaft
er)
57
.3(1
1.6
)
56
{2
9–7
6}
57
.7(1
4.1
)
56
{3
6–
10
7}
16
/17
0/3
1/2
24
4A
ML
or
MD
S1
0,
12
.5,
15
,2
0m
gIn
ten
siv
e(c
ycl
e1
day
1:
0,
0.2
5,
0.5
,1
,2
,3
,4
,6
,8
,2
4h
;cy
cle
1d
ay8
:0
,0
.25
,0
.5,
1,
2,
3,
4,
6,
8h
;ad
dit
ion
alsa
mp
les
on
cycl
e3
day
1an
dat
the
end
of
ever
y2
nd
cycl
eth
erea
fter
)
56
.4(1
5.7
)
59
{2
3–8
1}
78
.8(1
9.0
)
75
{4
6–
12
8}
29
/15
36
/7/1
31
8S
oli
dtu
mo
urs
0.0
5,
0.1
0,
0.2
0,
0.2
5m
g/k
gIn
ten
siv
e(c
ycl
e1
day
1:
0,
0.5
,1
,2
,3
,4
,6
,8
,2
4h
;cy
cle
1d
ay1
5:
0,
0.5
,1
,2
,3
,4
,6
,8
h)
52
.9(9
.99
)
52
{3
8–6
9}
57
.6(1
0.4
)
56
{4
5–
78
}
6/1
20
/18
/0
43
4A
dvan
ced
or
met
asta
tic
soli
dtu
mours
0.2
5m
g/k
gIn
tensi
ve
(day
1:
0.5
,1,
2,
3,
4,
6,
8,
10
,1
2,
24
,4
8,
72
h;
day
7:
0,
0.5
,1
,2
,3
,4
,6
,8
,1
0,
12
,2
4,
48
,7
2h
;d
ay2
1an
dd
ay3
0:
0,
1,
2,
3,
4,
6,
8h
)
60
.2(1
2.1
)
58
{3
6–8
1}
77
.5(2
0.5
)
71
{5
2–
14
7}
13
/21
31
/1/2
51
3A
dvan
ced
or
met
asta
tic
soli
dtu
mours
17.5
mg
Inte
nsi
ve
(day
1o
fea
chper
iod:
0,
0.5
,1
,2
,3
,4
,6
,8
,1
0,
12
,2
4,
48
,7
2,
96
h)
64
.6(8
.93
)
62
{4
9–7
8}
77
.5(1
7.8
)
77
{5
1–
10
7}
8/5
12
/1/0
61
0N
SC
LC
7.5
,1
2.5
mg
Inte
nsi
ve
(cy
cle
1d
ay2
1an
dcy
cle
2d
ay1
:0
,2
,3
,4
,8
,2
4h
)5
8.4
(9.0
3)
60
{4
3–6
9}
61
.7(1
2.9
)
62
{4
0–
79
}
7/3
0/1
0/0
Ph
ase
IIst
ud
ies
73
9H
CC
0.2
5m
g/k
gIn
ten
siv
ein
27
sub
ject
s(d
ay1
:0
,1
,2
,3
,4
,6
,8
,2
4,
48
h)
Sp
arse
in1
2su
bje
cts
(wee
ks
2an
d4
day
1,
end
of
wee
k8
)
58
.6(1
3.8
)
63
{2
0–8
1}
63
.0(1
3.9
)
59
{4
2–
11
5}
32
/72
/37
/0
81
28
NS
CL
C0
.10
,0
.25
mg
/kg
Sp
arse
(wee
ks
2,
3,
4,
5,
8)
61
.1(9
.92
)
62
{3
3–8
5}
71
.3(1
9.3
)
69
{3
5–
16
9}
75
/53
75
/47
/6
94
1R
CC
0.2
5m
g/k
gS
par
se(d
ays
8,
15
,2
9,
wee
ks
8an
d1
2)
59
.3(8
.54
)
60
{4
0–8
0}
88
.1(2
1.7
)
83
{5
7–
15
9}
34
/73
3/1
/7
10
10
Lo
call
yre
curr
ent
or
met
asta
tic
bre
ast
cance
r0
.15
,0
.20
mg
/kg
Inte
nsi
ve
(cy
cle
1d
ay2
8an
dcy
cle
2d
ay1
5:
0,
1,
2,
3,
4,
6,
8,
24
h)
53
.9(1
1.8
)
57
{3
0–7
3}
67
.2(1
7.6
)
64
{4
8–
10
7}
0/1
01
/2/7
11
10
6C
RC
7.5
,1
2.5
mg
Inte
nsi
ve
in8
sub
ject
s(c
ycl
e1
day
14
:0
,1
,2
,3
,4
,6
,8
,2
4h
;cy
cle
2d
ay1
:1
,2
,3
,4
,6
,8
,2
4h
)
Sp
arse
in9
8su
bje
cts
(cy
cle
1d
ay1
:0
.75
,2
,6
h;
cycl
es2
,3
,4
,6
,8
day
1:
0,
2h
;4
cycl
esth
erea
fter
day
1:
0h
)
58
.5(1
0.7
)
59
{3
1–8
1}
73
.0(1
4.0
)
72
{4
7–
10
6}
61
/45
79
/23
/4
PopPK Analysis of Linifanib in Cancer Patients 349
where h1 is the typical value (population mean) of CL/F and
g1 is an inter-individual random effect. The g values were
assumed to be independently, identically distributed, with
means of 0 and variances of x2: g * N(0, x2).
Residual variability was modelled using an additive
error model (Eq. 2), a proportional error model (constant
coefficient of variation, Eq. 3) or a combined additive and
proportional error model (Eq. 4), as follows:
Cij ¼ Cij þ eij ð2Þ
Cij ¼ Cij � ð1þ eijÞ ð3Þ
Cij ¼ Cij � ð1þ e1ijÞ þ e2ij ð4Þ
where Cij is the jth measured plasma concentration in indi-
vidual i, Cij is the jth model-predicted value in individual i, eij
is the residual random error for individual i and measurement
j, e1ij is the proportional component, and e2ij is the additive
component of the residual random error. The e values were
assumed to be independently and identically distributed, with
means of 0 and variances of r2: e * N(0, r2).
2.3.2 Identification of Significant Covariates
Empirical Bayesian estimates of individual parameters of
the base model were calculated by the posterior conditional
estimation technique (POSTHOC) in NONMEM, and their
association with pharmacokinetic parameters was investi-
gated. The covariates that were screened included the
cancer type, co-medications, creatinine clearance (CLCR),
linifanib formulation, fed status, liver function markers
(bilirubin, blood urea nitrogen [BUN], aspartate amino-
transferase [AST] and alanine aminotransferase [ALT]
levels), albumin level, age, sex, race, total body weight
(WT), body surface area and body mass index. Linifanib
exposures were previously reported to be higher following
morning administration than following evening adminis-
tration [21]. Therefore, we also tested the time of admin-
istration as a potential covariate for linifanib
bioavailability. Covariate modelling was performed using
the forward-inclusion, backward-elimination approach.
Power models were used for continuous covariates, with
the covariate scaled by the typical value, as shown in the
following example (Eq. 5):
TVVi ¼ h1 �WTi
70
� �h2
ð5Þ
where TVVi is the typical value of the apparent volume of
distribution (Vd/F) for an individual with WTi, and h1 is the
typical value of Vd/F for a 70 kg individual.
Dichotomous and categorical covariates were intro-
duced multiplicatively in the model via an indicator vari-
able. For example (Eq. 6):Ta
ble
1co
nti
nu
ed
Stu
dy
no
.S
ubje
cts
(n)
Stu
dy
po
pula
tio
nD
ose
sP
har
mac
ok
inet
icsa
mp
lin
gti
mes
Ag
e[y
ears
]aB
od
yw
eig
ht
[kg
]aS
ex[n
;m
ale/
fem
ale]
Rac
e[n
;W
hit
e/A
sian
/oth
er]
12
94
NS
CL
C7
.5,
12
.5m
gIn
ten
siv
ein
10
sub
ject
s(c
ycl
e1
day
21
and
cycl
e2
day
1:
0,
1,
2,
3,
4,
6,
8,
24
h)
Sp
arse
in8
4su
bje
cts
(cy
cle
1,
2,
3,
4d
ay1
:3
,6
h;
cycl
e1
day
s8
and
15
:0
h;
ever
ytw
ocy
cles
afte
rcy
cle
4d
ay1
)
59
.8(9
.23
)
60
{3
5–7
9}
69
.4(1
4.5
)
69
{4
1–
11
5}
55
/39
83
/6/5
Ph
ase
III
stud
y
13
44
0H
CC
17
.5m
gS
par
se(d
ay1
of
wee
k1
and
day
1o
fw
eek
3)
58
.3(1
1.7
)
59
{2
1–8
4}
68
.1(1
3.2
)
65
{3
8–
12
3}
38
0/6
01
29
/305
/6
AM
Lac
ute
myel
ogen
ous
leukae
mia
,C
RC
colo
rect
alca
nce
r,H
CC
hep
ato
cell
ula
rca
rcin
om
a,M
DS
myel
od
ysp
last
icsy
ndro
me,
NSC
LC
non-s
mal
lce
lllu
ng
cance
r,R
CC
renal
cell
carc
ino
ma,
SD
stan
dar
dd
evia
tio
na
Val
ues
are
exp
ress
edas
mea
n(S
D);
med
ian
{ra
ng
e}
350 A. H. Salem et al.
TVCLi ¼ h1
IF CAT:EQ:1ð ÞTVCLi ¼ h1 � h2
IF CAT:EQ:2ð ÞTVCLi ¼ h1 � h3
ð6Þ
where TVCLi is the typical value of clearance for indi-
vidual i, h1 is the typical value of CL/F for the reference
group with categorical covariate (CAT) = 0, and h2 and h3
represent the fixed effects of the categorical covariate.
2.3.3 Model Selection and Evaluation of the Final Model
Model selection was based on evaluation of the goodness-
of-fit plots, and attainment of physiologically reasonable
and statistically significant parameter estimates. In addi-
tion, the differences in the objective function value (OFV)
were used to guide model building. Since the OFV pro-
vided by NONMEM is approximately v2 distributed, the
likelihood ratio test was used for hypothesis testing to
discriminate among alternative nested population pharma-
cokinetic models. Likelihood ratio tests were assessed at
the 0.01 significance level (OFV drop [6.63 for a change
of one degree of freedom), but tests in the backward-
elimination step of the covariate selection procedure were
assessed at the 0.001 significance level (OFV increase of
10.83 for a change of one degree of freedom). Comparison
between non-hierarchical models was performed using the
Akaike information criterion.
The robustness of the final model parameter estimates
was evaluated using bootstrapping. A total of 1,000 boot-
strap replicates were constructed by randomly sampling
(with replacement) 1,010 subjects from the original dataset.
Model parameters were estimated for each bootstrap rep-
licate, and the resulting values were used to calculate
medians and confidence intervals. Bootstrap statistics were
Table 2 Patient demographics and clinical characteristics
Patient characteristic n (%) Mean (SD) Median Range
Age (years) 1,010 58.8 (11.4) 60.0 20.0–85.0
Height (cm) 1,010 166.9 (8.9) 168.0 130.0–196.0
Body weight (kg) 1,010 70.0 (16.4) 67.0 35.0–169.0
Body mass index (kg/m2) 1,010 25.1 (5.1) 24.2 13.7–50.5
Sex
Female 294 (29.1)
Male 716 (70.9)
Race
Asian 489 (48.4)
Other 40 (4.0)
White 481 (47.6)
Formulation
Oral solution 258 (25.5)
Uncoated tablets 330 (32.7)
Coated tablets 453 (44.9)
Cancer type
Breast cancer 19 (1.9)
CRC 118 (11.7)
HCC 483 (47.8)
NSCLC 232 (23.0)
Solid tumours 68 (6.7)
AML/MDS 44 (4.4)
RCC 46 (4.6)
Bilirubin (mg/dL) 1,010 0.7 (0.47) 0.59 0.1–3.5
Albumin (g/dL) 1,010 4.0 (0.47) 4.00 2.1–5.1
Creatinine (mg/dL) 1,010 0.9 (0.24) 0.81 0.4–2.0
Aspartate aminotransferase (IU/L) 1,010 46.6 (35.3) 34.0 8.0–211.0
Alanine aminotransferase (IU/L) 1,010 36.0 (29.8) 27.0 5.0–221.0
Creatinine clearance (mL/min) 1,010 92.0 (31.3) 87.8 21.3–290.4
AML acute myelogenous leukaemia, CRC colorectal cancer, HCC hepatocellular carcinoma, MDS myelodysplastic syndrome, NSCLC non-small
cell lung cancer, RCC renal cell carcinoma, SD standard deviation
PopPK Analysis of Linifanib in Cancer Patients 351
based only on replicates that converged successfully.
Model parameters based on the original dataset were
compared against the bootstrap results.
The predictive performance of the final models and its
usefulness for describing observations was assessed using
prediction and variance-corrected visual predictive checks
(VPCs), where the final parameter estimates were used to
simulate 1,000 replicates of the observed dataset. Both
observations and the simulated data were normalized on
the typical model prediction for the median independent
variable in each bin in order to account for variation in
sampling times and predictive covariates introduced by
binning of the observations [22]. The median and the 5th
and 95th percentile concentrations of the simulated datasets
were then plotted against the original observations.
3 Results
3.1 Base Model
A total of 7,351 plasma concentrations from 1,010 cancer
patients were included in the analysis. The demographic
and clinical characteristics of the patient population
included in the analysis are summarized in Table 2.
A two-compartment disposition model with first-order
absorption and elimination best described the data. The
model was parameterized in terms of the absorption rate
constant (ka), apparent clearance from the central com-
partment (CL/F), the apparent volume of the central
compartment (Vc/F), apparent inter-compartmental clear-
ance (Q/F), and the apparent volume of the peripheral
compartment (Vp/F). The model provided a better fit than a
one-compartment model with an OFV drop of 160. Adding
a third compartment did not further improve the fit. Using a
lag time for describing a potential absorption delay led to
unstable parameter estimates, although it decreased the
OFV significantly. Therefore, it was decided not to include
the lag time in the model.
The residual unexplained variability was best charac-
terized using a combined additive and proportional error
model, while additive and proportional residual error
models provided inferior fits. The data supported including
inter-individual variability terms for CL/F, Vc/F and ka,
which were estimated with high precision. Estimating
inter-individual variability in Vp/F and Q/F was associated
Table 3 Final estimates of the population pharmacokinetic parameters obtained using NONMEM and bootstrap analysis of the final model
Parameter Original data result Bootstrap resulta
Estimate (%RSE) Median 95 % CI
CL/F (L/h) 2.82 (2.30) 2.82 2.76–2.87
Vc/F (L) 50.75 (4.40) 50.76 50.00–51.55
ka (L/h) 0.46 (8.70) 0.46 0.44–0.48
Q/F (L/h) 1.14 (30.00) 1.14 0.97–1.35
Vp/F (L) 10.36 (16.00) 10.38 9.34–11.34
Oral solution on ka 1.97 (14.00) 1.98 1.85–2.16
Time of dose administration on F 0.73 (1.70) 0.73 0.71–0.75
CRC on CL/F 1.41 (4.50) 1.41 1.37–1.45
Body weight on Vc/F and Vp/F 0.52 (18.00) 0.52 0.47–0.56
Sex on CL/F 0.75 (3.30) 0.75 0.74–0.76
HCC on Vc/F and Vp/F 1.63 (6.40) 1.63 1.60–1.65
Food condition on F 0.86 (1.80) 0.86 0.82–0.91
AML/MDS cancer on F 0.57 (5.20) 0.57 0.55–0.58
RCC on Vc/F and Vp/F 1.86 (13.00) 1.87 1.81–1.93
IIV on CL/F (%CV) 42 (5.30) 42 41–42
IIV on Vc/F (%CV) 39 (16.00) 39 37–40
IIV on ka (%CV) 97 (11.00) 97 94–99
Proportional component (%CV) 34 (0.80) 34 34–34
Additive component (ng/mL) 8 (7.70) 8 7–9
AML acute myelogenous leukaemia, CI confidence interval, CL/F apparent clearance from the central compartment, CRC colorectal cancer, CV
coefficient of variation, F bioavailability, HCC hepatocellular carcinoma, IIV inter-individual variability, ka absorption rate constant, MDS
myelodysplastic syndrome, NSCLC non-small cell lung cancer, Q/F apparent inter-compartmental clearance, RCC renal cell carcinoma, RSE
relative standard error, Vc/F apparent volume of the central compartment, Vp/F apparent volume of the peripheral compartmenta Based on 854/1,000 successful runs
352 A. H. Salem et al.
with unphysiological estimates of Vp/F and Q/F and hence
were not included in the model. Estimating the full
covariance matrix between CL/F, Vc/F and ka was
attempted; however, the covariance parameters were esti-
mated with poor precision. Therefore, covariance between
only CL/F and Vc/F was included throughout model
development, with their correlation estimated to be 0.52 in
the base model.
3.2 Covariate Model
Covariates identified by the univariate stepwise forward-
inclusion procedure as significant determinants of linifanib
pharmacokinetic parameters were as follows: sex, cancer
type (colorectal cancer [CRC]) and cytarabine co-admin-
istration as covariates on CL/F, WT, cancer type (HCC and
RCC) as covariates on Vc/F and Vp/F, formulation effect on
ka and cancer type (refractory acute myeloid leukaemia
[AML] or myelodysplastic syndrome [MDS]), time of dose
administration and fed status on bioavailability. No other
evaluated covariates were found to significantly improve
the goodness of fit. Removal of the cytarabine effect on
CL/F in the stepwise backward elimination was associated
with a nonsignificant increase in OFV (p value [0.05);
hence, the cytarabine effect was removed from the model.
After reaching the final model, we tested the need for
estimating the exponent of the allometric model for WT on
Vc/F and Vp/F to ensure model parsimony. Fixing the
exponents to 1, as suggested by some researchers, resulted
in a significant increase in the OFV (p value \0.001);
hence, estimating the exponent was deemed appropriate.
3.3 Final Model
The final model parameter estimates and the precision
associated with their estimation are shown in Table 3. Both
fixed and random effects were precisely estimated, with a
relative standard error (RSE) of 30 % or less. In the final
model, an increase in WT was associated with a less than
proportional increase in Vc/F and Vp/F. Subjects with HCC
and RCC were estimated to have 63 and 86 % larger vol-
umes of distribution, respectively, than subjects with the
other cancer types. With regard to CL/F, females had 25 %
slower clearance than males. Furthermore, subjects with
colorectal cancer had 41 % faster CL/F than non-colorectal
cancer subjects.
For linifanib bioavailability, subjects with relapsed/
refractory AML/MDS had 43 % lower bioavailability, and
evening doses were associated with 27 % lower bioavail-
ability than morning doses, while administration of linifa-
nib under fed conditions decreased the bioavailability by
14 %. Finally, the oral solution formulation showed
approximately two-fold faster absorption than the tablet
formulations.
Relative to the base model, the covariates explained
27, 9 and 29 % of the variability of Vc/F, CL/F and the
correlation between Vc/F, CL/F, respectively. The
effects of some covariates on linifanib CL/F and
Vc/F are shown in Fig. 1. Figure 2 demonstrates the
effect of sex on CL/F and the lack of association
between body weight and CL/F.
The final equations for the typical values (TVs) of the
structural model parameters are presented in Eqs. 7, 8, 9
and 10:
TVCL=F ¼ 2:82� hCRC � hSEX ð7Þ
where:
hCRC ¼1:41; colorectal cancer
1; else
�;
hSEX ¼0:75; female
1; male
�
TVVc=F ¼ 50:75� WT=70ð Þ0:52�hHRC ð8Þ
where:
hHRC ¼1:63;1:86;
1;
hepatocellular carcinoma
renal cell carcinoma
else
8<:
TVka ¼ 0:46� hSOL ð9Þ
where:
hSOL ¼1:97; oral solution
1; tablets
�
TVF ¼ hAMPM � hFCOND � hAML MDS ð10Þ
where:
hAMPM ¼0:73; evening dose
1; morning dose
�
hFCOND ¼0:86; non-fasting
1; else
�
hAML MDS ¼0:57; Refractory AML/MDS cancer
1; else
�
The goodness of fit for the final model was evaluated
graphically (Figs. 3, 4). The individual and population
predicted linifanib concentrations versus the observed
concentrations were randomly distributed across the line
of unity, indicating that the model adequately described the
observations over the entire linifanib concentration range.
The conditional weighted residuals plots showed
symmetrical distribution and no time- or concentration-
related trends.
PopPK Analysis of Linifanib in Cancer Patients 353
Fig. 1 Effects of cancer type,
body weight and sex on
linifanib pharmacokinetic
parameters. The boxes represent
the 25th, 50th and 75th
percentiles; the whiskers
represent the lowest datum still
within 1.5 interquartile ranges
(IQRs) of the lower quartile, and
the highest datum still within
1.5 IQRs of the upper quartile
range; the bullets represents
outliers. AML acute
myelogenous leukaemia, CL/F
apparent clearance from the
central compartment, CRC
colorectal cancer, HCC
hepatocellular carcinoma, MDS
myelodysplastic syndrome,
NSCLC non-small cell lung
cancer, RCC renal cell
carcinoma, Vc/F apparent
volume of the central
compartment
Fig. 2 Relationships between
sex and body weight versus
ETA on apparent clearance
from the central compartment
(CL/F) in the base and final
models. The boxes represent the
25th, 50th and 75th percentiles;
the whiskers represent the
lowest datum still within 1.5
interquartile ranges (IQRs) of
the lower quartile and the
highest datum still within 1.5
IQRs of the upper quartile
range; the bullets represents
outliers
354 A. H. Salem et al.
Fig. 3 Diagnostic plots of the
final model
Fig. 4 Population predicted
linifanib concentration–time
after last dose profiles for all
studies. The solid lines ? error
bars denote the medians and
90 % percentiles of the
population predicted linifanib
concentrations, and the circles
denote the observed linifanib
concentrations
PopPK Analysis of Linifanib in Cancer Patients 355
In order to confirm the stability of the model preci-
sion of the estimated pharmacokinetic parameters, a
non-parametric bootstrap analysis was performed, and
85 % of the bootstrap replicates converged successfully.
In accordance with the estimated standard error of
estimate (SEE) values for pharmacokinetic parameters in
the linifanib pharmacokinetic model, the bootstrap
showed narrow confidence intervals for all parameters.
The median and the 5th and 95th percentiles of the
parameter estimates from the fit of the final model to the
bootstrap samples are shown in Table 3. The asymptotic
estimates obtained from the original dataset showed
close agreement with the median and were all included
within the 5th to the 95th percentiles of the bootstrap-
ping values, indicating model stability. None of the
95 % confidence intervals for the parameters from the
bootstrap datasets included zero, confirming the robust-
ness of the parameters.
In the VPC plots shown in Fig. 5, the 5th, 50th and 95th
percentiles of the prediction-corrected observations were in
close agreement with the confidence intervals of the 5th,
50th and 95th percentiles of the prediction-corrected sim-
ulated data, indicating a robust predictive ability of the
model to describe linifanib concentrations. Only 4 % of the
data were below the 5th percentile, and 5 % of the data
were above the 95th percentile of the predictions.
4 Discussion
Using non-linear mixed-effects analysis, linifanib concen-
tration–time data from 13 clinical studies were integrated
across the different development phases in order to char-
acterize the effect of covariates on linifanib pharmacoki-
netics. The developed model showed high parameter
estimate precision, as well as good predictability and hence
will be of immense value in predicting linifanib pharma-
cokinetics in various cancer patient populations.
The final structural pharmacokinetic model was a two-
compartment model with first-order absorption and elimi-
nation. Compared with the one-compartment model, the
use of a two-compartment model in our analysis was
associated with a better fit to individual profiles and a
larger reduction in the objective function value. A previous
analysis based on a phase II study used a one-compartment
model for linifanib in subjects with NSCLC [23]. The
sparse data included in the previous analysis may not have
allowed characterization of the biphasic disposition of
linifanib.
The population estimate of linifanib CL/F in the final
model was 2.8 L/h. Previous pharmacokinetic assessments
of individual studies have shown similar estimates. In a
phase I study in refractory solid tumours, linifanib
CL/F was 2.7 (±1.2) L/h [17]. In phase II studies, linifanib
Fig. 5 Prediction and variance-
corrected visual predictive
check for the final model. The
circles denote the prediction-
corrected observations; the lines
denote the 5th, 50th, and 95th
percentiles of the prediction-
corrected observed data; the
shaded areas denote the
confidence intervals of the 5th,
50th, and 95th percentiles of the
prediction-corrected simulated
data
356 A. H. Salem et al.
CL/F ranged from 3 to 3.9 L/h [23, 24]. The steady-state
volume of distribution (Vss/F) of linifanib was estimated to
be 61.1 L. This may indicate extensive distribution of
linifanib in the body, which is consistent with its high
lipophilicity (Log D of 4.2 at pH of 7.4) [12]. The beta-
phase half-life of 17.2 h is supportive of the once-daily
dosing used throughout development.
We explored the effect of body size measures on
linifanib pharmacokinetic parameters. No association was
found between the body size measures and linifanib CL/F,
despite the wide body weight range of the subjects included
in the analysis (Table 1). This corroborates the switch of
linifanib dosing from body weight-guided dosing in phase I
and II studies to fixed dosing in the phase III study. On the
other hand, Vc/F and Vp/F were associated with body
weight, and the data supported the estimation of the
exponent of the allometric size model. Subjects with WT
that is 10 and 20 % larger than the population typical body
weight of 70 kg are expected to have 5 and 10 % larger
Vss/F values than the population typical estimate.
The final model also estimated that morning dosing was
associated with 27 % greater exposure than evening dos-
ing. This diurnal variation has been demonstrated previ-
ously in a phase I study, which assessed the impact of the
dose time on linifanib pharmacokinetics [21]. In order to
minimize variability and improve the tolerability of
linifanib, the hepatocellular carcinoma subjects enrolled in
the phase III study were instructed to administer the doses
in the evening.
Diurnal variation in pharmacokinetics, often referred to
as chronopharmacokinetics, is exhibited by several orally
administered anti-cancer drugs; such as 6-mercaptopurine,
busulfan and tegafur/uracil [25–29]. Moreover, some
anticancer drugs, such as fluorouracil and doxorubicin, also
show diurnal variation in their plasma levels although they
are administered by constant continuous intravenous infu-
sion [30–33]. It is hypothesized that such diurnal variations
are often masked by the high inter-individual variability
observed in cancer patients [34]. Diurnal variation has been
also reported with drugs from other classes [35, 36].
The lower linifanib exposure in the evening could be
explained by the reduction in the gastric emptying rate in
the evening, due to reduced enterokinesis [37]. The slower
gastric emptying rate in the evening was deemed respon-
sible for lower peak concentrations and longer tmax values
for many lipophilic drugs [37]. Another possible mecha-
nism is the circadian rhythm in the activity of metabolizing
enzymes. Animal studies have shown several-fold greater
activity in some microsomal oxidases during the dark span
than in the light span [38–40]. Previous population phar-
macokinetic analyses reported strong associations between
microsomal oxidases activity and the clearance of another
anticancer drug, gefitinib, with 60 % of the variability of
unbound gefitinib plasma concentrations being explained
by individual cytochrome P450 3A4 activity [41, 42].
This population analysis showed that the cancer type
was an important determinant of linifanib pharmacokinet-
ics. According to the final model, subjects with colorectal
cancer have 41 % faster linifanib oral clearance. Colorectal
cancer subjects included in the analysis were co-medicated
with mFOLFOX6 (oxaliplatin [85 mg/m2], folinic acid
[400 mg/m2] and 5 fluorouracil [400 mg/m2 IV bolus]) on
the first day of each cycle. In a lead-in cohort in this
population, linifanib pharmacokinetics was evaluated with
and without mFOLFOX6. Therefore, we explored the
possibility of a drug interaction between linifanib and
mFOLFOX6 being responsible for the increase in CL/F in
this population. However, mFOLFOX6 showed no effect
on linifanib pharmacokinetics. Furthermore, our analysis
demonstrated 43 % lesser bioavailability in subjects with
relapsed or refractory AML or MDS than in those with
other cancer types. The lesser bioavailability estimated in
this patient population is consistent with the reportedly
greater CL/F estimates in this population (4.1–6.9 L/h)
[20] than in patients with other cancer types (2.7–3.9 L/h)
[17, 23, 24]. We initially attempted to include the relapsed/
refractory AML/MDS cancer type as a covariate on CL/F;
however, including it on bioavailability provided a much
larger OFV reduction. The formulation and assay were
precluded as sources of the lesser bioavailability in this
population, since the same formulation and assay were
used in studies conducted in other populations. We
hypothesize that this reduction in oral bioavailability is due
to cytotoxic therapy-induced malabsorption. The subjects
with relapsed/refractory AML or MDS who were included
in our analysis had been heavily pretreated with cytotoxic
therapy. Cytotoxic therapy affects the dividing cells of the
gastrointestinal mucosa and has been reported to cause
intestinal epithelial damage in AML subjects [43, 44].
Intestinal injury induced by cytotoxic therapy has been
linked to reduced absorption and lesser bioavailability of
several agents, such as acyclovir, ciprofloxacin and
D-xylose [45–47].
Another difference in pharmacokinetics between cancer
types was the higher Vss/F value in subjects with HCC and
RCC. This could be related to fluid retention and increased
fluid volume during hepatic and renal impairment. In
addition, linifanib is highly protein bound ([99 %), and
drugs that are strongly bound to plasma constituents (e.g.
phenytoin, diazepam) are known to demonstrate an
increased volume of distribution in patients with liver or
kidney disease, which is due to lower plasma binding [48].
In order to investigate whether the increase in linifanib
Vd/F in subjects with HCC and RCC could be explained by
change in protein binding in these populations, we explored
the use of albumin concentrations as a covariate in the
PopPK Analysis of Linifanib in Cancer Patients 357
model. However, no relationship was shown between
albumin concentrations and linifanib Vc/F or CL/F. In
addition, plasma protein binding data from 13 subjects with
HCC (eight Child–Pugh class A and five Child–Pugh
class B) showed that [99.7 % of linifanib was protein
bound in plasma, which was similar to values in subjects
with normal hepatic function [49]. Therefore, we do not
believe that the larger Vd/F in HCC and RCC subjects is
linked to a decrease in protein binding.
An oral solution formulation was used initially during
linifanib clinical development, before tablet formulations
were developed. In alignment with the results of compar-
ative bioavailability studies, our population analysis
showed no difference in linifanib bioavailability among the
formulations. Nevertheless, the analysis showed a differ-
ence in the absorption rate constant between the formula-
tions, with the liquid formulation having two-fold faster
absorption than the tablet formulation. We attempted to
estimate different inter-individual variability for ka of the
oral solution compared with the tablet formulations; how-
ever, a high shrinkage ([70 %) in the inter-individual
variability of ka of the oral solution was observed. A model
with only one random effect for ka for all formulations
decreased the shrinkage, and hence the same inter-indi-
vidual variability was estimated for ka regardless of the
formulation.
Our analysis showed a sex effect on linifanib CL/F, with
males having 25 % faster CL/F than females. This differ-
ence is similar to that observed with another tyrosine
kinase inhibitor, erlotinib, where female subjects achieved
greater exposure (25–43 %) than male subjects [50]. Faster
clearance in male subjects for some drugs is often sec-
ondary to the body weight influence on clearance. In an
attempt to investigate whether the sex effect seen on
linifanib CL/F is due to a body weight effect, we explored
the relationship between linifanib CL/F and body weight.
However, no association was found between CL/F and
body weight (Fig. 2). Numerous clinical pharmacokinetic
studies have demonstrated sex differences in drug absorp-
tion and bioavailability for certain drugs [51]. Neverthe-
less, we do not believe that this is the underlying
mechanism of the sex effect on linifanib CL/F, since there
was no difference in Vd/F between males and females. We
hypothesize that sex-based differences in drug metabolism
play a role in the faster clearance observed in males.
In several clinical studies, linifanib was co-administered
with other anti-cancer agents, such as cytarabine, paclit-
axel, carboplatin and mFolfox6. Our analysis suggests that
these drugs do not affect linifanib pharmacokinetics. This
may be because of the multiple pathways involved in
linifanib metabolism. In addition, we found no difference
in pharmacokinetic parameters between Asians, who were
well represented in our dataset, and non-Asian populations.
Finally, there was no association between linifanib
CL/F and CLCR. This was anticipated, since urinary elimina-
tion is a minor pathway in linifanib pharmacokinetics, with
less than 5 % of the linifanib dose being recovered in urine
as the unchanged drug and metabolite [20].
5 Conclusion
The use of mixed-effects modelling allowed robust
assessment of the impact of the concomitant effects of
body size, different cancer types, formulation, diurnal
variation, sex and food. The developed population phar-
macokinetic model describes linifanib concentrations ade-
quately and can be used to conduct simulations or to
evaluate the linifanib exposure–response relationship.
Conflicts of Interest This study was sponsored by AbbVie Inc.
AbbVie Inc. contributed to the study design; research; data interpre-
tation; and writing, review and approval of the manuscript for pub-
lication. Ahmed Hamed Salem, Denise Koenig and Dawn Carlson
are employees of AbbVie Inc.
References
1. Carmeliet P, Jain RK. Angiogenesis in cancer and other diseases.
Nature. 2000;407(6801):249–57.
2. Zetter P, Bruce R. Angiogenesis and tumor metastasis. Annu Rev
Med. 1998;49(1):407–24.
3. Dvorak HF. Vascular permeability factor/vascular endothelial
growth factor: a critical cytokine in tumor angiogenesis and a
potential target for diagnosis and therapy. J Clin Oncol.
2002;20(21):4368–80.
4. Benjamin LE, Golijanin D, Itin A, Pode D, Keshet E. Selective
ablation of immature blood vessels in established human tumors
follows vascular endothelial growth factor withdrawal. J Clin
Invest. 1999;103(2):159.
5. Carmeliet P. Angiogenesis in health and disease. Nat Med.
2003;9(6):653–60.
6. Perona R. Cell signalling: growth factors and tyrosine kinase
receptors. Clin Transl Oncol. 2006;8(2):77–82.
7. Homsi J, Daud AI. Spectrum of activity and mechanism of action
of VEGF/PDGF inhibitors. Cancer Control. 2007;14(3):285.
8. Hurwitz H, Fehrenbacher L, Novotny W, et al. Bevacizumab plus
irinotecan, fluorouracil, and leucovorin for metastatic colorectal
cancer. N Engl J Med. 2004;350(23):2335–42.
9. Reck M, Von Pawel J, Zatloukal Pv, et al. Overall survival with
cisplatin–gemcitabine and bevacizumab or placebo as first-line
therapy for nonsquamous non-small-cell lung cancer: results from
a randomised phase III trial (AVAiL). Ann Oncol. 2010;21(9):
1804–9.
10. Sandler A, Gray R, Perry MC, et al. Paclitaxel–carboplatin alone
or with bevacizumab for non–small-cell lung cancer. N Engl J
Med. 2006;355(24):2542–50.
11. Erber R, Thurnher A, Katsen AD, et al. Combined inhibition of
VEGF and PDGF signaling enforces tumor vessel regression by
interfering with pericyte-mediated endothelial cell survival
mechanisms. FASEB J. 2004;18(2):338–40.
12. Dai Y, Hartandi K, Ji Z, et al. Discovery of N-(4-(3-amino-1
H-indazol-4-yl) phenyl)-N0-(2-fluoro-5-methylphenyl) urea
358 A. H. Salem et al.
(ABT-869), a 3-aminoindazole-based orally active multitargeted
receptor tyrosine kinase inhibitor. J Med Chem. 2007;50(7):
1584–97.
13. Albert DH, Tapang P, Magoc TJ, et al. Preclinical activity of
ABT-869, a multitargeted receptor tyrosine kinase inhibitor. Mol
Cancer Ther. 2006;5(4):995–1006.
14. Linifanib. Drugs R D. 2010;10(2):111–22.
15. Toh HC, Chen PJ, Carr BI, et al. Phase 2 trial of linifanib (ABT-
869) in patients with unresectable or metastatic hepatocellular
carcinoma. Cancer. 2013;119(2):380–7.
16. Asahina H, Tamura Y, Nokihara H, et al. An open-label, phase 1
study evaluating safety, tolerability, and pharmacokinetics of
linifanib (ABT-869) in Japanese patients with solid tumors.
Cancer Chemother Pharmacol. 2012;69(6):1477–86.
17. Wong CI, Koh TS, Soo R, et al. Phase I and biomarker study of
ABT-869, a multiple receptor tyrosine kinase inhibitor, in
patients with refractory solid malignancies. J Clin Oncol.
2009;27(28):4718–26.
18. Steinberg J, Tan E, Wei-Peng Y. Preliminary analysis of ABT-
869 safety, pharmacokinetics and efficacy in three phase 2 solid
tumor studies [abstract no. 477P]. 33rd Congress of the European
Society for Medical Oncology; Stockholm; 12–16 Sep 2008.
19. Humerickhouse R, Gupta N, Goh B. Phase 1 comparison of
pharmacokientics, safety and efficacy with low versus high doses
of ABT-869 in refractory solid tumors [abstract no. 476P]. 33rd
Congress of the European Society for Medical Oncology;
Stockholm; 12–16 Sep 2008.
20. Wang ES, Yee K, Koh LP, et al. Phase 1 trial of linifanib (ABT-
869) in patients with refractory or relapsed acute myeloid leu-
kemia. Leuk Lymphoma. 2012;53(8):1543–51.
21. Gupta N, Yan Z, LoRusso P, Ricker J, Carlson D, Pradhan R.
Assessment of the effect of food on the oral bioavailability and
assessment of diurnal variation in the pharmacokinetics of
linifanib. Mol Cancer Ther. 2009;8(12 Suppl):B53.
22. Bergstrand M, Hooker AC, Wallin JE, Karlsson MO. Prediction-
corrected visual predictive checks for diagnosing nonlinear
mixed-effects models. AAPS J. 2011;13(2):143–51.
23. Tan EH, Goss GD, Salgia R, et al. Phase 2 trial of linifanib
(ABT-869) in patients with advanced non-small cell lung cancer.
J Thorac Oncol. 2011;6(8):1418–25.
24. Tannir NM, Wong YN, Kollmannsberger CK, et al. Phase 2 trial
of linifanib (ABT-869) in patients with advanced renal cell cancer
after sunitinib failure. Eur J Cancer. 2011;47(18):2706–14.
25. Etienne-Grimaldi M, Cardot J, Francois E, et al. Chronophar-
macokinetics of oral tegafur and uracil in colorectal cancer
patients. Clin Pharmacol Ther. 2007;83(3):413–5.
26. Hassan M, Oberg G, Bekassy A, et al. Pharmacokinetics of high-
dose busulphan in relation to age and chronopharmacology.
Cancer Chemother Pharmacol. 1991;28(2):130–4.
27. Koren G, Langevin AM, Olivieri N, Giesbrecht E, Zipursky A,
Greenberg M. Diurnal variation in the pharmacokinetics and
myelotoxicity of mercaptopurine in children with acute lym-
phocytic leukemia. Arch Pediatr Adolesc Med. 1990;144(10):
1135.
28. Muggia FM, Wu X, Spicer D, et al. Phase I and pharmacokinetic
study of oral UFT, a combination of the 5-fluorouracil prodrug
tegafur and uracil. Clin Cancer Res. 1996;2(9):1461–7.
29. Vassal G, Challine D, Koscielny S, et al. Chronopharmacology of
high-dose busulfan in children. Cancer Res. 1993;53(7):1534–7.
30. Metzger G, Massari C, Etienne M-C, et al. Spontaneous or
imposed circadian changes in plasma concentrations of 5-fluo-
rouracil coadministered with folinic acid and oxaliplatin: rela-
tionship with mucosal toxicity in patients with cancer. Clin
Pharmacol Ther. 1994;56(2):190–201.
31. Petit E, Milano G, Levi F, Thyss A, Bailleul F, Schneider M.
Circadian rhythm-varying plasma concentration of 5-fluorouracil
during a five-day continuous venous infusion at a constant rate in
cancer patients. Cancer Res. 1988;48(6):1676–9.
32. Squalli A, Oustrin J, Houin G. Clinical chronopharmacokinetics of
doxorubicin (DXR). Annu Rev Chronopharmacol. 1989;5:393–6.
33. Levi F. Circadian rhythms in 5-fluorouracil pharmacology and
therapeutic applications. In: Rustum YM. Fluoropyrimidines in
cancer therapy. Totowa: Humana Press, 2003. p. 107–28.
34. Levi F, Okyar A, Dulong S, Innominato PF, Clairambault J.
Circadian timing in cancer treatments. Annu Rev Pharmacol
Toxicol. 2010;50:377–421.
35. Zhang C, Denti P, Decloedt E, et al. Model-based approach to
dose optimization of lopinavir/ritonavir when co-administered
with rifampicin. Br J Clin Pharmacol. 2012;73(5):758–67.
36. Iwahori T, Takeuchi H, Matsuno N, et al. Pharmacokinetic dif-
ferences between morning and evening administration of cyclo-
sporine and tacrolimus therapy. Transplant Proc. 2005;37:
1739–40.
37. Lemmer B. Chronopharmacokinetics: implications for drug
treatment. J Pharm Pharmacol. 1999;51(8):887–90.
38. Belanger P. Chronobiological variation in the hepatic elimination
of drugs and toxic chemical agents. Annu Rev Chronopharmacol.
1988;4:1–46.
39. Radzialowski FM, Bousquet WF. Daily rhythmic variation in
hepatic drug metabolism in the rat and mouse. J Pharmacol Exp
Ther. 1968;163(1):229–38.
40. Gachon F, Olela FF, Schaad O, Descombes P, Schibler U. The
circadian PAR-domain basic leucine zipper transcription factors
DBP, TEF, and HLF modulate basal and inducible xenobiotic
detoxification. Cell Metab. 2006;4(1):25–36.
41. Lu J-F, Eppler SM, Wolf J, et al. Clinical pharmacokinetics of
erlotinib in patients with solid tumors and exposure-safety rela-
tionship in patients with non-small cell lung cancer. Clin Phar-
macol Ther. 2006;80(2):136–45.
42. Li J, Karlsson MO, Brahmer J, et al. CYP3A phenotyping
approach to predict systemic exposure to EGFR tyrosine kinase
inhibitors. J Natl Cancer Inst. 2006;98(23):1714–23.
43. Bow EJ, Kilpartick MG, Scott BA, Clinich JJ, Cheang MS. Acute
myeloid leukemia in Manitoba. Cancer. 1994;74(1):52–60.
44. Bow EJ, Loewen R, Cheang MS, Shore TB, Rubinger M, Sch-
acter B. Cytotoxic therapy-induced D-xylose malabsorption and
invasive infection during remission-induction therapy for acute
myeloid leukemia in adults. J Clin Oncol. 1997;15(6):2254–61.
45. Johnson E, MacGowan A, Potter M, et al. Reduced absorption of
oral ciprofloxacin after chemotherapy for haematological malig-
nancy. J Antimicrob Chemother. 1990;25(5):837–42.
46. Sitar DS, Aoki FY, Bow EJ. Acyclovir bioavailability in patients
with acute myelogenous leukemia treated with daunorubicin and
cytarabine. J Clin Pharmacol. 2008;48(8):995–8.
47. Bow E, Meddings J. Intestinal mucosal dysfunction and infection
during remission-induction therapy for acute myeloid leukaemia.
Leukemia. 2006;20(12):2087–92.
48. Klotz U. Pathophysiological and disease-induced changes in drug
distribution volume: pharmacokinetic implications. Clin Phar-
macokinet. 1976;1(3):204–18.
49. Gupta N, Chiu Y, Toh H, et al. Preliminary pharmacokinetics and
safety comparison of Child–Pugh A (CPA) vs Child–Pugh B
(CPB) patients enrolled in a phase 2 study in hepatocellular
carcinoma (HCC). Presented at Annals of Oncology; 2010.
50. Frohna P, Lu J, Eppler S, et al. Evaluation of the absolute oral
bioavailability and bioequivalence of erlotinib, an inhibitor of the
epidermal growth factor receptor tyrosine kinase, in a random-
ized, crossover study in healthy subjects. J Clin Pharmacol.
2006;46(3):282–90.
51. Gandhi M, Aweeka F, Greenblatt RM, Blaschke TF. Sex differ-
ences in pharmacokinetics and pharmacodynamics. Annu Rev
Pharmacol Toxicol. 2004;44:499–523.
PopPK Analysis of Linifanib in Cancer Patients 359