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DMD # 35394
1
Influence of Cremophor EL and Genetic Polymorphisms on the Pharmacokinetics of Paclitaxel
and its Metabolites using a Mechanism-Based Model
Martin N. Fransson, Henrik Gréen, Jan-Eric Litton, and Lena E. Friberg
Department of Medical Epidemiology and Biostatistics, Karolinska Institutet, Stockholm,
Sweden; MF, JEL
Division of Drug Research/Clinical Pharmacology, Department of Medical and Health Sciences,
Faculty of Health Sciences, Linköping University, Linköping, Sweden; HG
Department of Pharmaceutical Biosciences, Uppsala University, Uppsala, Sweden; LF
DMD Fast Forward. Published on November 5, 2010 as doi:10.1124/dmd.110.035394
Copyright 2010 by the American Society for Pharmacology and Experimental Therapeutics.
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Running title page
a) Pharmacokinetics of Paclitaxel and its Metabolites
b) Martin Fransson, M.Sc. Department of Medical Epidemiology and Biostatistics PO Box 281/Nobels väg 12 A SE-171 77 Stockholm, Sweden Phone: +46 (0)8-524 839 74 Fax: +46 (0) 8-31 49 75 E-mail: [email protected]
c) Number of text Pages: 42 Number of Tables: 5 Number of Figures: 4 Number of References: 40 Number of words in Abstract: 239 Number of words in Introduction: 743 Number of words in Discussion: 1277
d) 6αOH-pac, 6α-hydroxypaclitaxel; p3OH-pac, p-3’-hydroxypaclitaxel; diOH-pac, 6α-, p-3’-dihydroxypaclitaxel; CrEL, Cremophor EL; OFV, Objective Function Value; SE, Standard Error; RSE, Relative Standard Error; IIV, Interindividual Variability; LLP, Log Likelihood Profiling; CV, Coefficient of Variation; d.f., degrees of freedom
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Abstract
The formulation vehicle Cremophor EL has previously been shown to affect paclitaxel kinetics,
but it is not known whether it also affects the kinetics of paclitaxel metabolites. This may be
important for understanding paclitaxel metabolism in vivo, and when investigating the role of
genetic polymorphisms in the metabolizing enzymes CYP2C8 and CYP3A4/CYP3A5, and the
ABCB1 transporter. This study used the population pharmacokinetic approach to explore the
influence of predicted Cremophor EL concentrations on paclitaxel (Taxol) metabolites. In
addition, correlations between genetic polymorphisms and enzyme activity to clearance of
paclitaxel, its two primary metabolites, 6α-hydroxypaclitaxel and p-3’-hydroxypaclitaxel, and its
secondary metabolite, 6α-, p-3’-dihydroxypaclitaxel were investigated. Model building was based
on 1156 samples from a study with 33 women undergoing paclitaxel treatment for gynaecological
cancer. Total concentrations of paclitaxel were fitted to a model previously described. One-
compartment models characterized unbound metabolite concentrations. Total concentrations of
6α-hydroxypaclitaxel and p-3’-hydroxypaclitaxel were strongly dependent on predicted
Cremophor EL concentrations, but this association was not found for 6α-, p-3’-
dihydroxypaclitaxel. Clearance of 6α-hydroxypaclitaxel (fraction metabolized) was significantly
correlated (*p < 0.05) to the ABCB1 allele G2677T/A. Individuals carrying the polymorphisms
G/A (n = 3) or G/G (n= 5) showed a 30% increase while individuals with polymorphism T/T (n =
8) showed a 27% decrease relative the polymorphism G/T (n = 17). The correlation of G2677T/A
to 6α-hydroxypaclitaxel has not been described previously, but supports other findings of the
ABCB1 transporter playing a part in paclitaxel metabolism.
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Introduction
Paclitaxel is a natural substance from the Pacific Yew tree and was recognized for its property to
cause apoptosis by promoting microtubule stabilization (Schiff et al., 1979), and is today used for
the treatment of a number of different cancer types. Due to the large interindividual differences
observed in the pharmacokinetics of the drug, identification of patient factors that can be used to
individualize the dose in clinical practise are desirable. Paclitaxel is dosed by body surface area
but the measure of body size explains only a small part of the variability (Mathijssen et al., 2007).
Other demographic characteristics previously proposed to be attributable to population variability
include gender, age, body weight and bilirubin (Henningsson et al., 2003; Joerger et al., 2006).
Several of the genes involved in the pharmacokinetics of paclitaxel contain single nucleotide
polymorphisms (SNP) that may result in interindividual variability of paclitaxel clearance.
Previously considered polymorphisms for paclitaxel clearance or exposure include SNPs for the
metabolizing enzymes CYP2C8, CYP3A4 and CYP3A5, but also for the ABCB1 transporter
gene (Henningsson et al., 2005a; Nakajima et al., 2005; Sissung et al., 2006; Yamaguchi et al.,
2006; Green et al., 2009; Bergmann et al., 2010). So far, results are ambiguous, with a few
positive findings on SNPs affecting clearance of paclitaxel (Yamaguchi et al., 2006; Green et al.,
2009; Bergmann et al., 2010). Although paclitaxel metabolites are considered not to be active
against the tumours and have been shown to be up to 30-fold less cytotoxic than the parent
compound (Harris et al., 1994a; Sparreboom et al., 1995), the particular metabolic pattern for
paclitaxel may be of interest for identifying correlations between individual clearance and SNP
variants for participating enzymes. The metabolites may also be involved in the neuropathy seen
after paclitaxel-containing chemotherapy (Leskela et al., 2010).
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Elimination of paclitaxel occurs mainly as hepatic metabolism (Walle et al., 1995), carried out
by cytochrome P-450 monooxygenases as a one- or two-step hydroxylation process in either of
two metabolic paths (Monsarrat et al., 1993). In the first step, paclitaxel is oxidised by CYP2C8
to 6α-hydroxypaclitaxel (6αOH-pac) or by CYP3A to p-3’-hydroxypaclitaxel (p3OH-pac)
(Cresteil et al., 1994; Harris et al., 1994b; Rahman et al., 1994). 6αOH-pac is the predominate
metabolite in most cases (Kumar et al., 1994; Harris et al., 1994a; Sonnichsen et al., 1995), with
an estimated overall formation in vitro of 63% (Cresteil et al., 2002). In the second step, 6αOH-
pac and p3OH-pac may be further oxidised to the secondary metabolite 6α-, p-3’-
dihydroxypaclitaxel (diOH-pac) by CYP3A and CYP2C8, respectively (Sonnichsen et al., 1995;
Monsarrat et al., 1998). Together, paclitaxel and the three metabolites constitute a diamond-
shaped pathway with each P-450 monooxygenase in parallel on the two arms (Figure 1).
Distribution and/or elimination of total concentrations of paclitaxel (Taxol) have earlier been
suggested to be saturable (Sonnichsen et al., 1994; Gianni et al., 1995; Karlsson et al., 1999). The
observed non-linear kinetics of total concentrations, when administered as Taxol, have been
attributed primarily to micelle encapsulation by the formulation vehicle Cremophor EL (CrEL)
(Sparreboom et al., 1996). When binding of paclitaxel to CrEL and plasma proteins is taken into
account, unbound concentrations of paclitaxel will fit a model with linear kinetics (Henningsson
et al., 2001). The use of this more mechanism-based model ideally requires measurements of
unbound concentrations of paclitaxel and concentrations of CrEL in addition to total plasma
concentrations. However, the model has been shown to be at least as good as using a more
empirical explanation of the non-linear behaviour (Gianni et al., 1995) when only total paclitaxel
concentrations are available for analysis (Fransson and Green, 2008). CrEL concentrations were
predicted from a previously developed model (Henningsson et al., 2005b) and a similar approach
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can be taken to investigate if and how CrEL also is influencing the metabolite kinetics of
paclitaxel.
The purpose of the present study was to investigate the influence of CrEL on paclitaxel
(Taxol) metabolite kinetics, and to investigate correlations of paclitaxel and metabolites’
clearances with enzyme activity and SNP variants of the metabolizing enzymes CYP2C8,
CYP3A4, CYP3A5 and the transporter protein ABCB1. In particular, the metabolic pattern
suggests that a correlation may exist for the proportion of clearance of paclitaxel to 6αOH-pac
and p3OH-pac, and clearances of these metabolites to diOH-pac. Using information on both
parent and metabolite concentrations, in addition to predictions of CrEL concentrations, in a
population pharmacokinetic model, can provide a better understanding for the elimination of
paclitaxel, and potential correlations may be easier to elucidate.
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Materials and Methods
Patients and study design
Thirty-three Caucasian women, 36 to 75 years of age (median 62), with different types of
gynaecological cancers: epithelial ovarian cancer (n = 26), peritoneal cancer (n = 4), ovarian or
peritoneal (n = 1), carcinoma in corpus uteri (n = 1) and in cervix uteri (n = 1), were included in
the study as previously described (Green et al., 2009). The patients received a combination
therapy of paclitaxel (Taxol) (Bristol-Myers Squibb, Wallingford, CT, USA), administrated as an
intravenous infusion with a target time of three hours and dosing at 175 mg/m2 (n = 30) or 135
mg/m2 (n = 3, due to poor general condition) and carboplatin, with AUC 5 or 6 mg*min/mL
according to Calvert’s formula (Calvert et al., 1989). For thirty-one patients treatment consisted
of at least six cycles of chemotherapy. One patient received only a single cycle due to
septicaemia and another patient was withdrawn after four cycles due to severe neurotoxicity.
Blood samples for pharmacokinetic analysis were obtained during one cycle per patient from the
1st to 8th cycle (median cycle number 3), and collected in EDTA tubes. Target times for sampling
were immediately before infusion, 30 min and 1 h after start of infusion, immediately before stop
of infusion, at 5, 15, 30 min and 1, 2, 4, 8 and 24 h after stop of infusion. Centrifuged plasma
samples were stored in −80° C until analysis. The regional ethics committees approved the study
and written informed consent was obtained from each patient.
Assays and samples
Total concentrations of paclitaxel, 6αOH-pac and p3OH-pac from all patients, and diOH-pac,
from fifteen patients, were analysed in plasma samples using solid phase extraction, reverse-
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phase high-performance liquid chromatography and an ion trap mass spectrometer with a sonic
spray ionization interphase as described elsewhere (Green et al., 2006b). For paclitaxel, 6αOH-
pac and p3OH-pac, docetaxel (Aventis Pharma, Vitry Alforville, France) was used as an internal
standard, and for diOH-pac, paclitaxel was used as reference. The lower limit of quantification
was 0.5 ng/mL for paclitaxel and 2 ng/mL for hydroxymetabolites (Green et al., 2006b), but
observations below the lower limit of quantification were included in the analysis if detected.
Twenty-seven observations were considered non-detectable. For one patient, 15 observations of
paclitaxel (n = 5), 6αOH-pac (n = 4), p3OH-pac (n = 3) and diOH-pac (n = 3) were removed
because of a large (> 30%) within-sample variability for paclitaxel. In total, 1156 observations of
paclitaxel (n = 345), 6αOH-pac (n = 332), p3OH-pac (n = 336) and diOH-pac (n = 143) remained
for pharmacokinetic analysis.
Enzyme activity and genotyping
The selection of CYP3A4 phenotyping method was based on finding an non-radioactive assay
without any risk of sedation and with an reaction similiar to that of paclitaxel, i.e., an
hydroxylation. We finally settled on the use of oral quinine tablets followed by a simple HPLC
method for the quantification of the ratio in plasma. Enzyme activity for CYP3A4 in vivo was
determined by administration of a 250 mg quinine tablet to the patients 24 to 48 h prior to start of
chemotherapy followed by blood sampling 16 h later (Mirghani et al., 1999; Mirghani et al.,
2001). The CYP3A4 activity was expressed as metabolic ratio of quinine (concentration of
quinine / concentration of hydroxylquinine) and was in the range of 2.2 to 41.3 (median 10.0),
where a low value indicates a high metabolic ratio. For two patients CYP3A4 activity could not
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be determined. For these cases, the missing values were imputed as the median of the remaining
patient group.
The individual patients’ genotypes were determined using Pyrosequencing according to the
manufacturers’ protocol and as previously described (Green et al., 2006a; Green et al., 2009). The
genotype frequencies of the study group are shown in Table 1 and have previously been
published (Green et al., 2009), except CYP2C8 Haplotype C and CYP3A5*3.
Population Pharmacokinetic Analysis
For population pharmacokinetic analysis the NONMEM software (Beal, Sheiner and
Boeckmann, version VI, level 2.0, Icon Development Solutions, Ellicott City, Maryland, USA,
2006) was used in combination with PsN (version 3.1.0, http://psn.sourceforge.net). Additional
calculations of NONMEM output and graphical analysis was performed in Xpose (version 4.1.0,
http://xpose.sourceforge.net) for R (version 2.10.0, http://www.r-project.org, R Foundation for
Statistical Computing, Vienna, Austria, 2009). Fortran files were compiled using the G77
compiler.
The mechanism-based model (Henningsson et al., 2001) was used to fit total concentrations of
paclitaxel. The mechanism-based model consists of a linear three-compartment model for
unbound paclitaxel and the total paclitaxel concentrations were described as:
[ ] [ ] [ ] [ ] [ ] [ ][ ]um
umaxuCrELulinut pacK
pac*Bpac*CrEL*Bpac*Bpacpac
++++=
Eq. 1
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where [pac]t is the plasma concentration of total paclitaxel, [pac]u is the corresponding unbound
concentration, Blin is the linear binding to plasma components, BCrEL describes the binding
directly proportional to the CrEL concentration [CrEL], Bmax is the maximum non-linear binding
to plasma components and Km is the concentration at half Bmax.
Only total concentrations of paclitaxel and metabolites were available and unbound
concentrations were estimated from total concentrations. In case of unbound concentrations of
paclitaxel, Eq. 1 was used, while systematic testing of various models was applied to find the best
structures in terms of fit (see below) for prediction of unbound metabolite concentrations. It has
been shown that the mechanism-based model structure is not identifiable (with high probability)
without information on unbound concentrations of paclitaxel (Fransson and Green, 2008).
Therefore, the approach with frequentist priors (Gisleskog et al., 2002) was used in the current
study to stabilize the analysis. The priors (mean and standard error) used in the final model are
presented in Table 2. Since CrEL concentrations were not available from the study, a model
describing the population pharmacokinetics of CrEL, with three compartments and saturated
elimination, was implemented and used to predict CrEL concentrations at any time point
(Henningsson et al., 2005b). Model parameters for CrEL were tried as priors or as fixed
estimates. Earlier identified covariate relations were not used in the CrEL model. The paclitaxel
model and the CrEL model were specified using the ADVAN 6 subroutine in NONMEM VI, and
all estimations were performed with the First Order Conditional Estimation method with
Interaction.
Interindividual variability (IIV) for an individual i was in general modelled exponentially:
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)exp(η*θθ ipopi =
Eq. 2
where θpop is the parameter for the typical value for the population and η ~ N(0, ω2). Residual
errors for observed concentrations (cobs) vs. predicted concentrations (cpred) were modelled using
a proportional error in combination, if needed, with an additive error according to:
22
21predpredobs ε)ε*(ccc ++=
Eq. 3
where ε1 ~ N(0, σ12) and ε2 ~ N(0, σ2
2).
The combined paclitaxel-CrEL model was first fitted to total paclitaxel concentrations only.
Priors were used on all parameters previously reported at the population level, and for IIV the
prior for clearance of unbound paclitaxel was included (Henningsson et al., 2001). Significance
of IIV in remaining parameters was tested one at a time without additional priors. The
mechanism-based model structure of paclitaxel was extended to also include the metabolites.
Initially the paclitaxel parameters were fixed to the estimates obtained in the first step. Total
metabolite concentrations were fitted sequentially in the following order: only 6αOH-pac, only
p3OH-pac, 6αOH-pac in combination with p3OH-pac, and 6αOH-pac and p3OH-pac in
combination with diOH-pac. For metabolites, the issue of identifiability caused by not knowing
the unbound fraction implies that the size of any linear terms cannot be estimated in an equation
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connecting unbound and total concentrations. Hence, a parameter corresponding to Blin for
metabolites cannot be estimated. All metabolite parameters will therefore be scaled by the
(unknown) fraction that is linearly bound.
The NONMEM objective function value (OFV), which is proportional to −2xlog likelihood of
the data, was used to guide model development. For nested models, the OFV is χ2 distributed and
a new model was selected if the addition of one parameter caused a drop in OFV by at least
10.83, which corresponds to a significance level of ***p < 0.001. In addition, the new parameter
should not cause problems with identifiability. Individual plots and plots of conditional weighted
residuals versus time (Hooker et al., 2007) were also used to determine the importance of the new
parameter.
For parameter estimates not supported by priors, the standard errors provided by NONMEM
were complemented by log-likelihood profiling (LLP). By fixing each parameter at a time in the
original model, log-likelihood profiling will calculate the parameter value that results in an
increase in OFV for a pre-specified significance level. Since a model with a fixed parameter is
nested relative the original model, the lower and higher parameter value that each cause an
increase in OFV by 3.84, will constitute a 95% confidence interval for the specific parameter. As
the search is performed on both sides of the final estimate no symmetry assumptions are made.
For parameter estimates supported by priors, the informativeness of the study specific data was
investigated by calculating the quota of prior relative standard errors (RSE) to model relative
standard errors. The predictive performance of the final model was evaluated using visual
predictive checks based on 1000 simulations.
Sensitivity analysis was also performed to determine the influence of frequentist priors on
parameter estimates and significance of covariates by (1) increasing the standard error for each
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prior by 50%, (2) decreasing and (3) increasing the estimate for one of the priors with − / +2x the
standard error, and (4) using a different set of priors (Henningsson et al., 2005a).
Covariate testing
Shrinkage in the random effects was calculated to evaluate the appropriateness of using the
Empirical Bayes estimates for investigation of potential covariate relationships (Savic and
Karlsson, 2009). Testing for significant covariates was performed directly in NONMEM, using
step-wise covariate modelling in PsN with forward selection and backward elimination. Due to
the relatively small population (n = 33) covariate testing was considered to be the secondary aim
of the work, and was hence performed only as a univariate analysis. Covariates were to be
included in the final model only if they were significant in both the forward-selection (**p <
0.01) and backward-elimination step (***p < 0.001). Inclusion of priors was not compatible with
step-wise covariate modelling as implemented in PsN (version 3.1.0) and therefore parameters
supported by priors (i.e., all structural paclitaxel parameters except clearance) were fixed to the
estimates of the final model. In addition, significance testing was performed in the R software,
using one-way ANOVA on Empirical Bayes estimates derived from the POSTHOC step in
NONMEM, since it has been reported earlier that ANOVA tests in some cases may be more
reliable for dealing with type-1 errors than the likelihood ratio test obtained by NONMEM OFV
(Bertrand et al., 2009). All IIV parameters, except those that were fixed, were tested against age.
In addition, paclitaxel and metabolites’ clearances and the relative fraction parameter, fp3OH/fmpac,
were tested for relationships to SNP variants and CYP3A4 enzyme activity.
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Results
Model structure for paclitaxel metabolites
Observed total concentrations of paclitaxel and its three metabolites are shown in Figure 2. The
previously developed mechanism-based-CrEL model adequately described total paclitaxel
concentrations, using IIV in clearance for the three-compartment model structure of unbound
paclitaxel. Inclusion of IIV in Blin (Eq. 1) further improved the fit (ΔOFV = −85), and after
inclusion IIV in other population parameters was not significant (***p < 0.001).
Using frequentist priors instead of fixed parameter values in the CrEL model had little effect
on estimates in the combined mechanism-based-CrEL model, and the CrEL parameters were
therefore fixed to stabilize the analysis.
The final parameter estimates are presented in Table 3. The ratio of relative standard errors for
estimates and priors was less than 1 for all population parameters, confirming that the current
data set on paclitaxel contained new information and was in line with the data the priors were
derived from. The priors for clearance of unbound paclitaxel and the related IIV parameter were
omitted in the final model not to interfere with covariate testing.
The mechanism-based model was extended with compartments to fit metabolite
concentrations. The fraction eliminated by different elimination routes cannot be estimated unless
the metabolites are administered. To keep the model structure identifiable, it was therefore
assumed that all parent drug and primary metabolites were converted into the here observed
metabolites.
A one-compartment model with linear elimination and binding of predicted unbound
concentrations of 6αOH-pac to predicted CrEL concentrations resulted in a drop in OFV of −230
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units and improved CWRES plots. A nonlinear binding component, similar to Bmax and Km in Eq.
1, was found to improve the OFV further (−61) but could be simplified to a single non-specific
binding parameter (Bnsp,6αOH) without increase in OFV. A small decrease (−4) in OFV was found
by multiplying the constant with CrEL concentrations. To explain the steep increase in total
6αOH-pac concentrations (Figure 2), a Hill factor was applied in the Cremophor EL binding
mechanism and was found significant (ΔOFV = −123). IIV in the Hill coefficient decreased OFV
further with 55 units. The final model for the relationship between unbound and total
concentrations of 6αOH-pac is presented below:
[ ] [ ] [ ][ ] [ ] [ ]CrEL*BOH6*CrEL)(CrEL
CrEL*BOH6OH6 OHnsp,6uHillHill
50
HillOHCrEL,6
utCrELCrEL
CrEL
αα ααα +
++=
Eq. 4
where BCrEL,6αOH is the maximal binding rate to CrEL, Bnsp,6αOH is the non-specific binding
parameter to CrEL, CrEL50 is the CrEL concentration at half maximal binding rate and HillCrEL is
the Hill coefficient for CrEL concentration. Allowing an additive error at the time of the first
sample improved the stability of the model and lowered the OFV with 15 units.
The final model structure for unbound p3OH-pac was also described with a one-compartment
model with linear elimination and the relationship between the total and unbound metabolite and
CrEL concentration was identical to Eq. 4. The parameters HillCrEL and CrEL50 in Eq. 4 were set
to be the same for both primary metabolites. There was no need for an additive error on first
samples for p3OH-pac.
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The distribution of clearance of unbound paclitaxel to the formation of the primary
metabolites was modelled using a relative fraction parameter. Preliminary modelling attempts
indicated that this parameter was not identifiable at a population level and was therefore fixed to
a corresponding literature value describing in vitro formation of p3OH-pac, which has been
estimated to 37% of the paclitaxel metabolized to 6αOH-pac and p3OH-pac (Cresteil et al.,
2002). To allow IIV for the relative fraction parameter, fp3OH/fmpac, but to keep individual
estimates in the range of 0 to 1 logit transformation was used, so that:
( )( )βexp1
βexp/fmf pacp3OH +
=
Eq. 5
where IIV was described additively:
ηββ pop +=
Eq. 6
and βpop is the population value corresponding to fp3OH/fmpac = 0.37, and η ~ N(0, ω2). Using a
block structure with three additional covariance parameters for IIV in CL6αOH/fmpac, CLp3OH/fmpac
and β in Eq. 6 did not convey a significant change (*p < 0.05) in OFV. When fitting the two
primary metabolites without using a block structure IIV in CLp3OH/fmpac was not significant (*p <
0.05), and was consequently removed.
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Total concentrations of the secondary metabolite diOH-pac was included using a one-
compartment model with linear elimination. No association between total diOH-pac and CrEL
was found. An additive error, on top of a proportional, reduced the OFV with −71 units.
For the full model, the log-likelihood profiling for each parameter not supported by a prior is
presented in Table 3. The boundaries of the 95% confidence intervals are in agreement with the
symmetric 95% confidence intervals calculated from the standard errors reported by NONMEM,
but showed a trend of being right-skewed. Observed concentrations versus population
predictions, stratified on parent drug and the different metabolites, are shown in Figure 3 and
visual predictive checks are shown in Figure 4.
Covariate analysis
Rare SNP variants (Table 1) were pooled with larger groups before covariate analysis; C3435T
C/C was pooled with T/C, G2677T/A G/A was pooled with G/G, CYP2C8*1B A/A was pooled
with C/A and CYP2C8 Haplotype C G/G was pooled with C/G.
Shrinkage for non-fixed random effects ranged from 6.2-34%. For compatibility reasons, all
parameters using priors had to be fixed to their respective estimate from the final model (Table 3)
when applying the automatic step-wise covariate model building procedure in PsN. All
covariates significant on p < 0.1, corresponding to a drop in OFV with at least −2.71 units for one
additional degree of freedom, were tested using one-way ANOVA. The results from the covariate
analysis are presented in Table 4. No parameters were significantly correlated to the investigated
covariates for **p < 0.01, which was considered to be the required level for inclusion in the final
model during the forward-selection step. However, CL6αOH/fmpac, which was significantly (*p <
0.05) affected by GM2677T/A was also tested by inclusion in the final model using frequentist
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priors instead of fixed estimates. Individuals with SNP variant G/A or G/G (pooled) showed a
30% (2.8-62%, 80% confidence interval) increase as compared to the reference group constituted
by the G/T heterozygous patients, while individuals with variant T/T showed a 27% (9.4-42%,
80% confidence interval) decrease in CL6αOH/fmpac relative the reference group G/T. Patients with
the wild type G/G or G/A genotype had the highest CL6αOH/fmpac, while G/T individuals were
intermediate and T/T homozygous patients in position 2677 had the lowest CL6αOH/fmpac.
Inclusion of the covariate decreased the IIV (CV%) in CL6αOH/fmpac from 36.6% to 30.5%. CLpac
also showed a significant (*p < 0.05) correlation to CYP3A5*3, and was tested separately in the
final model. Individuals with SNP variant G/A showed a 20% (4.7-32%, 95% confidence
interval) decrease relative the reference group G/G. Inclusion of the covariate decreased the IIV
(CV%) in CLpac from 15.3% to 12.7%. In addition, there was a tendency that CLpac and
CLdiOH/fmmet were correlated (p < 0.1) to CYP2C8*1C and CYP3A4*1B, respectively.
Since inclusion of the covariates only resulted in a minor reduction in OFV, two alternative
models that included IIV in V1 and V2 were evaluated to investigate the consistency in covariate
effects. In Alternative model 2 also the IIV in the linear binding of paclitaxel to plasma proteins
(Blin) was excluded to exactly mimic the parameterization in the original model (Henningsson et
al., 2001). Only GM2677T/A showed a significant effect for all three models (*p < 0.05 for
ANOVA and p < 0.1 based on drop in OFV).
The results from the sensitivity analysis are presented in Table 5. CL6αOH/fmpac was
significantly (*p < 0.05) correlated to GM2677T/A regardless of the tested sets of prior estimates.
The parameter CL6αOH/fmpac, without inclusion of covariate, is presented to show the effect on a
parameter estimate when using different sets of frequentist priors.
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Discussion
To our knowledge, this is the first time the pharmacokinetics of both paclitaxel and its most
acknowledged metabolites have been characterized using a population approach with nonlinear
mixed effects modelling. Previously, paclitaxel and 6αOH-pac have been modelled using
nonlinear kinetics for both parent drug and metabolite (Gianni et al., 1995), without considering
the formulation vehicle CrEL. It has later been shown that the nonlinear kinetics for paclitaxel
most likely is a result of binding to CrEL and plasma components, and that unbound
concentrations follow linear kinetics (Henningsson et al., 2001). In this work, we have presented
strong indications that the same may be true for the two primary metabolites, since total
concentrations of 6αOH-pac and p3OH-pac both seemed to be dependent on the predicted time-
course of CrEL and by extensive and non-linear binding, while no such association was apparent
for the secondary metabolite diOH-pac.
A Hill equation has earlier been used to describe micelle kinetics (Piszkiewicz, 1977),
although for catalytic micelles rather than for substrate binding only. Still, the estimate of 2.71 in
Table 3 for the Hill coefficient is well within the range of the previously derived coefficients for a
number of combinations of detergents and substrates, which has been reported to range from
approximately 1 to 6 with the majority below 3 (Piszkiewicz, 1977).
The visual predictive checks in Figure 4 show good adequacy of the models, although for total
diOH-pac concentration the lower percentile was over predicted. It is plausible that the low
number of patients (n = 15) contributing with observations to diOH-pac, in combination with
relatively noisy data, contributed to the relatively poor visual predictive check for diOH-pac.
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The maximum binding rate to CrEL in the Hill term was five times higher for 6αOH-pac than
for p3OH-pac (Table 3), explaining the more steep increase in total 6αOH-pac concentrations
than for total p3OH-pac concentrations during the infusion (Figure 2).
No significant correlation between the pathways of paclitaxel to p3OH-pac and 6αOH-pac to
diOH-pac or paclitaxel to 6αOH-pac and p3OH-pac to diOH-pac could be detected. In addition,
the first two pathways were not significantly correlated to the CYP3A4 phenotype. The absence
of these associations is noteworthy but may depend on the relatively small study group. For
parameters where shrinkage in random effects were relatively high (CLpac, 21%; CLdiOH/fmmet,
34%), the approach with ANOVA may not help in detecting false negatives (Bertrand et al.,
2009). It has also been shown earlier that study groups with less than 50-100 individuals may
cause problems in characterizing covariate effects (Ribbing and Jonsson, 2004). This issue should
also be considered for the finding in this work of reduced clearance (fraction metabolized) of
6αOH-pac/fmpac for carriers of the ABCB1 G2677T/A G/T and T/T polymorphisms. The study
group under consideration here has previously been used to show (non-parametrically) a
significantly higher clearance for total paclitaxel concentrations in individuals carrying the G/A
variant of G2677T/A (Green et al., 2009), but this is the first time G2677T/A has been
significantly correlated to the primary metabolite 6αOH-pac. Since 6αOH-pac is the major
metabolite for most patients, it may also reflect paclitaxel clearance, which makes it plausible
that the finding in this model-based analysis is related to the same source as the earlier finding for
the parent drug. Previously, Yamaguchi et al. found a positive correlation of the ABCB1 total
mutant allele number to the clearance of paclitaxel in 13 Japanese ovarian cancer patients
(Yamaguchi et al., 2006). Nakajima et al. did not present a similar finding in 23 ovarian cancer
patients, although they found that carriers of the ABCB1 genotype C3435T had a significantly
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higher AUC of p3OH-pac (Nakajima et al., 2005). Sissung et al. did not either find a correlation
between the ABCB1 genotypes C3435T and G2677T/A and paclitaxel pharmacokinetics
(Sissung et al., 2006), although that study was also small (n = 26). Correlations between kinetics
for unbound paclitaxel and the genotypes CYP2C8*2, CYP2C8*3, CYP2C8*4, CYP3A4*3 and
the C3435T genotype were not found in a large study with 97 individuals (Henningsson et al.,
2005a). However, that study was based on a less homogenous group of patients than the current
study, since it included a large number of dosing schedules, infusion times, and both males and
females being treated for different kinds of tumours (Henningsson et al., 2005a). More recently,
in a relatively large (n = 93) and more homogenous study a significant correlation between
CYP2C8*3 and clearance of unbound paclitaxel was reported (Bergmann et al., 2010), but no
correlation between ABCB1 genotypes and clearance was found. In the present study, the
CYP2C8*3 correlation could not be detected, which may be caused by too few individuals (n =
6) carrying the specific genotype.
All correlations significant at p < 0.1 from the step-wise covariate modelling have been
summarised in Table 4, together with their corresponding p-value from ANOVA using Empirical
Bayes estimates. Although effects can be considered small, they are consistent between
NONMEM OFV and ANOVA, which would reduce the probability of a type-1 error (Bertrand et
al., 2009). The significant correlation of CLpac to CYP3A5*3 may be in correspondence with a
recent finding (Leskela et al., 2010), where the allele was shown to have a protective effect
against neurotoxicity. In the current study, carriers of CYP3A5*3 G/A showed a 20% decrease in
clearance of unbound paclitaxel relative the reference group G/G. This is somewhat surprising,
since the G/G group is carrying an inactive allele and would thus be expected to have lower
clearance. However, it should be pointed out that only five individuals were carriers of the G/A
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genotype and that a larger population would be desirable to further clarify this outcome, and, for
the two alternative models, the genotype was not statistically significant (Table 4).
In contrast to the finding for CYP3A5*3, the significant correlation of CL6αOH-pac/fmpac of
G2677T/A was significant over all models, and also consistent over different sets of frequentist
priors as presented in Table 5. The latter implies that the significant correlation is not an artefact
of a particular set of priors. The estimated covariate effects for G2677T/A on clearance of 6αOH-
pac/fmpac were relatively large, with an increase and decrease of 30 and 27% for G/G pooled with
G/A and T/T respectively, compared with the effect of CYP2C8*3 on clearance of unbound
paclitaxel reported by Bergmann et al, which was only a decrease of 11% (Bergmann et al.,
2010). However, the effect estimates of G2677T/A in this study were associated with a high
uncertainty, and the 95% and 90% CIs (but not the 80% CI) for the estimates included zero.
The correlation of clearance of diOH-pac/fmmet could very well be an artefact, since only three
individuals carried the specific genotype. To our knowledge, there is no information in literature
concerning the role of CYP3A4 in clearance of diOH-pac. The correlation of CYP2C8*1C to
clearance of unbound paclitaxel was not found in Bergmann et al., and was not consistent for the
Alternative models.
In conclusion, our study supports the previous findings of the ABCB1 transporter playing a
part in paclitaxel metabolism (Nakajima et al., 2005; Yamaguchi et al., 2006) or paclitaxel
treatment outcome (Green et al., 2006a). For the first time, we have also presented strong
indications that the formulation vehicle Cremophor EL, similar to the parent drug, affects the
pharmacokinetics of the two primary metabolites. Finally, the finding by Leskela et al. that alleles
associated with decreased paclitaxel metabolism seem to contribute to a lower risk for
neurotoxicity (Leskela et al., 2010) could imply that paclitaxel metabolites play a role in adverse
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effects in paclitaxel treatment. If so, paclitaxel metabolites could be clinically relevant, in which
case the description of metabolites kinetics developed in this work may be important.
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Acknowledgments
We thank Sven Sandin for support in statistics and helpful discussions throughout the project.
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Authorship Contributions
Participated in research design: Fransson, Gréen, and Friberg.
Conducted experiments: Gréen.
Contributed new reagents or analytic tools: .
Performed data analysis: Fransson, Gréen, and Friberg.
Wrote or contributed to the writing of the manuscript: Fransson, Gréen, Litton, and Friberg.
Other: Fransson, Gréen, Litton, and Friberg acquired funding for the research.
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Footnotes
a)
This work has been supported by the Swedish Knowledge Foundation through the Industrial
Ph.D. programme in Medical Bioinformatics at the Strategy and Development Office (SDO) at
Karolinska Institutet; the Swedish Cancer Society; Gunnar Nilsson’s Cancer Foundation; and the
County Council in Östergötland.
b)
Previously presented at PAGE 19 (2010) Abstr 1912 [www.page-meeting.org/?abstract=1912]
c)
Martin Fransson, M.Sc.
Department of Medical Epidemiology and Biostatistics
PO Box 281/Nobels väg 12 A
SE-171 77 Stockholm, Sweden
Phone: +46 (0)8-524 839 74
Fax: +46 (0) 8-31 49 75
E-mail: [email protected]
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Legends for figures
Figure 1. Metabolic pathways for paclitaxel by CYP2C8 and CYP3A.
Figure 2. Observed total plasma concentrations of paclitaxel (n = 345), 6α-hydroxypaclitaxel (n =
332), p-3’-hydroxypaclitaxel (n = 336) and 6α-, p-3’-dihydroxypaclitaxel (n = 143). Paclitaxel,
6α-hydroxypaclitaxel and p-3’-hydroxypaclitaxel were observed in 33 individuals and 6α-, p-3’-
dihydroxypaclitaxel was observed in 15 individuals.
Figure 3. Observed concentrations versus population predictions of paclitaxel, 6α-
hydroxypaclitaxel, p-3’-hydroxypaclitaxel and 6α-, p-3’-dihydroxypaclitaxel for the final model.
Figure 4. Visual predictive checks based on 1000 simulations. 95% CI of 5th, 50th and 95th
percentiles of simulated data (dashed lines). Solid lines are 5th, 50th and 95th percentiles of
observed data.
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Tables
Table 1
Genotype frequencies in the study group
Gene Allele Polymorphism n
ABCB1 C3435T C/C 4
T/C 19
T/T 10
G2677T/A G/G 3
G/A 5
A/A 0
G/T 17
T/A 0
T/T 8
CYP2C8 *1B C/C 23
C/A 9
A/A 1
*1C T/T 21
T/G 12
G/G 0
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*3 A/A 27
A/G 6
G/G 0
*4 C/C 29
G/C 4
G/G 0
Haplotype C C/C 20
C/G 11
G/G 2
CYP3A4 *1B A/A 30
A/G 3
G/G 0
CYP3A5 *3 G/G 28
G/A 5
A/A 0
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Table 2
Priors used for the mechanism-based model of paclitaxel (Henningsson et al., 2001)
Parametera Prior Estimate Prior RSEb (%)
V1 (L) 229 17
V2 (L) 856 15
V3 (L) 303 21
Q2 (L/h) 134 22
Q3 (L/h) 213 23
Blin 7.59 12
BCrEL 3.78 10
Bmax (µmol/L) 0.0245 27
Km (µmol/L) 0.000106 43
a V1, V2, V3, volumes of the central, first- and second peripheral compartment for unbound
concentrations of paclitaxel; Q2, Q3, intercompartmental clearances between the central and
peripheral compartments for unbound concentrations of paclitaxel; Blin, linear binding to plasma
components; BCrEL, binding directly to proportional to CrEL concentration; Bmax, maximal
binding to plasma components; Km, concentration at half of the maximal binding to plasma
components.
b Relative Standard Error.
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Table 3
Parameter estimates for the final model without covariate relations
Parametera Estimate RSE (%) LLP 95% CI RSE/RSE Prior
Lower Upper
CLpac (L/h) 378 8.4 322 441
V1 (L) 188 11 0.66
V2 (L) 1100 8.2 0.54
V3 (L) 222 14 0.68
Q2 (L/h) 123 10 0.45
Q3 (L/h) 181 13 0.57
Blin 7.89 10 0.84
BCrEL 3.62 9.1 0.91
Bmax (µmol/L) 0.0207 22 0.81
Km (µmol/L) 0.000123 36 0.83
ε1,pac (%) 24.4 4.7 22.3 26.8
IIVCLpac (CV%)b 15.3 39c 10.0 22.3
IIVBlin (CV%)b 101 34c 67.3 176
CL6αOH/fmpac (L/h) 2830 26 1850 4750
V6αOH /fmpac (L) 1390 24 945 2230
BCrEL,6αOH 43.0 40 24.4 99
Bnsp,6αOH (µmol/L) 0.000754 12 0.000588 0.000947
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ε1, 6αOH (%) 25.4 5.6 22.9 28.4
ε2, 6αOH, i=1 (µmol/L) 0.00447 30 0.00250 0.00772
IIVCL6αOH/fmpac (CV%)b 36.6 36c 25.1 53.8
CLp3OH/fmpac (L/h) 1470 16 1090 2020
Vp3OH /fmpac (L/h) 1140 13 883 1490
BCrEL,p3OH 8.60 32 5.24 16.1
Bnsp,p3OH (µmol/L) 0.00124 10 0.00103 0.00149
ε1, p3OH (%) 37.7 4.8 34.5 41.6
IIVfp3OH/fmpac 0.425d 0.29c 0.245d 0.769d
CrEL50 (mL/L) 4.48 18 3.55 6.21
HillCrEL 2.71 13 2.20 3.39
IIVHillCrEL (CV%)b 40.1 38c 26.8 58.9
CLdiOH/fmmet (L/h) 831 15 606 1140
VdiOH /fmmet (L) 167 23 97.1 246
ε1, diOH (%) 49.8 8.4 42.6 59.3
ε2, diOH (µmol/L) 0.00197 22 0.00134 0.00315
IIVCLdiOH/fmmet (CV%)b 60.7 39c 40.8 104
a CLpac, clearance of unbound concentrations of paclitaxel; V1, V2, V3, volumes of the central,
first- and second peripheral compartment for unbound concentrations of paclitaxel; Q2, Q3,
intercompartmental clearances between the central and peripheral compartments for unbound
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concentrations of paclitaxel; Blin, linear binding to plasma components; BCrEL, binding directly to
proportional to CrEL concentration; Bmax, maximal binding to plasma components; Km,
concentration at half of the maximal binding to plasma components; CL6αOH/fmpac, CLp3OH/fmpac,
clearance of unbound concentrations of 6αOH-pac and p3OH-pac over fraction metabolized
unbound paclitaxel; V6αOH /fmpac, Vp3OH /fmpac, volume of distribution of unbound concentrations
of 6αOH-pac and p3OH-pac over fraction metabolized unbound paclitaxel; BCrEL,6αOH, BCrEL,p3OH,
maximal binding rate to CrEL of 6αOH-pac and p3OH-pac; Bnsp,6αOH, Bnsp,p3OH, non-specific
CrEL component for 6αOH-pac and p3OH-pac; CrEL50, CrEL concentration at half maximal
binding rate; HillCrEL, Hill coefficient for CrEL concentration; CLdiOH/fmmet, clearance of unbound
concentrations of diOH-pac over fraction metabolized unbound primary metabolite; VdiOH /fmmet,
volume of distribution of unbound concentrations of diOH-pac over fraction metabolized
unbound primary metabolite; ε1, proportional residual error for total concentrations; ε2, 6αOH, i=1,
additive error for first sample for each individual of total concentration of 6αOH-pac; ε2,diOH,
additive error for total concentration of diOH-pac; IIVCLpac, IIVBlin, IIVCL6αOH/fmpac, IIVfp3OH/fmpac,
IIVHillCrEL, IIVCLdiOH/fmmet, interindividual variability in the designated parameter.
b Coefficient of Variation, calculated as (exp(ω2) – 1)0.5.
c With respect to the variance term, ω2.
d Estimate given for the corresponding variance term, ω2, of β in Eq. 5 and Eq. 6.
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Table 4
Step-wise covariate modelling and ANOVA
Parameter Covariatea Δd.f. ΔOFVb p (ΔOFV)c p (ANOVA)d
CL6αOH/fmpac (L/h) G2677T/A 2
Final model −7.38 0.025 0.012
Alternative model 1e −4.79 0.091 0.048
Alternative model 2f −5.86 0.054 0.033
CLpac (L/h) CYP3A5*3 1
Final model −5.91 0.015 0.024
Alternative model 1 −2.96 0.085 0.12
Alternative model 2 −0.37 0.54 0.57
CLdiOH/fmmet (L/h) CYP3A4*1B 1
Final model −3.52 0.061 0.13
Alternative model 1 −3.35 0.067 0.14
Alternative model 2 −3.13 0.077 0.15
CLpac (L/h) CYP2C8*1C 1
Final model −3.42 0.064 0.070
Alternative model 1 −3.42 0.064 0.082
Alternative model 2 −0.01 0.93 0.91
aCovariates significant on p < 0.1 in the final model using step-wise covariate modelling.
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b Relative a model with fixed estimates instead of priors for paclitaxel parameters.
c p-value corresponding to the drop in OFV.
d Using Empirical Bayes estimates from the corresponding model supported by priors.
e Identical to the final model but also using IIV, supported by priors (Henningsson et al., 2001),
on the distribution volumes V1 (CV 46%, d.f. 28) and V2 (CV 40%, d.f. 13) for unbound
paclitaxel.
f Identical to Alternative model 1 but without IIV on the parameter Blin for plasma protein
binding. The model structure is hierarchical to Alternative model 1 but not to the Final model.
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Table 5
Sensitivity analysis for significant ABCB1 allele G2677T/A using Empirical Bayes estimates
Modela p (ANOVA)
G2677T/A on CL6αOH/fmpac
CL6αOH/fmpac (L/h)
no covariate
Final model 0.012 2830
Test 1 0.012 2790
Test 2 0.010 2800
Test 3 0.014 2870
Test 4 0.011 2290
a Estimates for the final model, as presented in Table 3; Test 1, increased standard error for each
prior by 50%; Test 2, prior for BCrEL set to prior estimate – 2 x standard error; Test 3, prior for
BCrEL set to prior estimate + 2 x standard error; Test 4, prior estimates from Henningsson et al.,
(2005a) for unbound paclitaxel parameters only (V1, V2, V3, Q2 and Q3).
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