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Veeqo helps multichannel retailers keep their inventory levels accurate, streamline their operations and ship orders on time.
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Keppel Shipyard, a subsidiary of Keppel Offshore & Marine, reported today that the Company has secured two contracts worth US $103 million (S$150 million) for the upgrading, modification and conversion of two vessels. Work on the vessels is expected to commence immediately.
Single Buoy Moorings Inc. (SBM) awarded Keppel the first contract for the upgrading and conversion of the 255,272 dwt tanker MT Accord into the P-57 FPSO. The FPSO will be deployed in Petrobras' deepwater Jubarte field in Brazil's Campos Basin and have a production capacity of 180,000 bopd and 71 million cf/d of natural gas.
The contract includes hull and marine conversion, spread mooring aids installation, accommodation block extensions/refurbishment, fabrication and installation of marine pipe rack, topside module supports, and part of the topside modules installation. The FPSO is expected to sail from Keppel Shipyard in the last quarter of 2009 to Brazil, where the remainder of the work (65% of the contract) will be completed.
Production from the Jubarte field is currently under way in a Long-Duration Test from the FPSO JK (P-34). A pre-salt field in the Campos Basin, Jubarte is off the southern coast of Espirito Santo.
Awarded by Golar LNG, the second contract involves the conversion of the Golar Winter from a Membrane LNG Carrier into a Floating Storage Re-gasification Unit (FSRU). To be completed in the second quarter of 2009, the FSRU Golar Winter contract includes the installation of a re-gasification plant system, as well as the upgrade of control systems, electrical systems and marine systems.
The FSRU Golar Winter will have the capacity to re-gasify 14 million cubic meters of natural gas a day. The vessel will be operated by Petrobras and moored at a pier in the Guanabara Bay offshore Rio de Janiero.
Keppel recently delivered the world's first FSRU, the Golar Spirit, to Golar LNG. The Golar Spirit, which is also operated by Petrobras, is moored at the Port of Pecem in northeast Brazil.
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Steve Gamlin is an award-winning professional speaker, entertainer and author. In November 2008, he was awarded First Place in the Toastmasters District 45 'Humorously Speaking' competition.
Steve's Books Include:
"20 to Life (In a Good Way)"
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Over the last 19 years, Steve has enjoyed life as a professional speaker, radio personality, DJ and stand-up comic…which all goes against the grain of his childhood as a shy kid with very little self-confidence.
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New Hope Business Plan Is Complete!
From left: Roy March, Bill Dinino, Barbara March, April Gordon, Larry Murphy, Italian Translator, Mara and Vicky Quondamatteo
Co-founder of New Hope Orphanage & Clinic, Vicky Quondamatteo came to Los Angeles last week to meet with the March to the Top team!! After months of hard work, we created a New Hope Orphanage & Clinic Business Plan! We are thrilled with the results and are confident this business plan will help shape the future for New Hope to continuing thriving for years to come.
11845 W. Olympic Blvd.
West Tower, 11th Floor
Los Angeles, CA 90064
March to the Top - Africa (M2T) is a 501(c)(3) non profit organization.
Copyright © 2017, March to the Top - Africa (M2T), All rights reserved.
Your contribution is tax deductible to the extent allowed by law. FEIN: 26-1625731


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Smilelign revolutionary orthodontic aligners give you the straight smile you always dreamed of. It replaces the need to use ugly metal braces and wires and is practically invisible so people won't even know you're having your teeth straightened. Smilelign enables you to be confident, look great and smile better.
Teeth straightening, known within dentistry as Orthodontics, traditionally used metal brackets and ugly wires to straighten your teeth. By contrast Smilelign is an invisible orthodontic aligner system that uses the latest technology on the UK dental market. Smilelign's revolutionary clear brace aligner gives you the straight smile you always dreamed of. Smilelign is practically invisible, so people won't even know you're having your teeth straightened.
- Smilelign treatment is completed with a series of virtually invisible, removable aligners.
- The aligners are changed every two to four weeks for the next stage.
- The process can take as little as 10 weeks depending on the alterations required.
- Each aligner is carefully designed for teeth and will move them in very small increments little by little, week by week.
- You will wear the clear aligners until they have moved your teeth to the final position prescribed by your dentist.
- Comfortable
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- Invisible
- Affordable
- Clinically effective
- Free Consultation
- Braces
- Free Teeth Whitening
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- Retainers


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A.G. Edwards Brings Back Hargrove to Expand Product Line
Related Articles
- GOING PLACES. // Crain's Cleveland Business;5/10/2004, Vol. 25 Issue 19, p16
The article presents information on job changes by various executive officers in the field of architecture, construction, education, engineering and finance. Coral Co.'s Tony LaGruth has become the director of construction, Leanne van Beers-Werneke has become the associate director of marketing...
- School Superintendent Switches to A.G. Edwards. Carvlin, Elizabeth // Bond Buyer;9/21/2004, Vol. 349 Issue 31973, p6
Reports on the entry of finance executive Robert Regan as a banker and vice president of A.G. Edwards & Sons Inc., a finance company in East Lansing, Michigan Career background; Responsibilities in the firm; Statement of Don Elliot, manager of the Michigan public finance office, regarding the...
- Manage Your Career. Shaw, Geoff // NZ Marketing Magazine;Oct2002, Vol. 21 Issue 9, p43
No abstract available.
- Transitioning to a New Career. Hubler, Liz // Women in Business;Jul/Aug2001, Vol. 53 Issue 4, p38
Presents tips on making career changes. What to consider in performing a self-assessment; Skills that are critical to a worker's marketability in almost any field; Benefits of maintaining a professional network.
- The late show. Warren, Diana // People Management;02/25/99, Vol. 5 Issue 4, p64
Discusses the valuable lessons that could be learned from a major career change. Importance of taking continuing professional development (CPD) programs; Pieces of advice in formulating plans for CPD.
- Find Ways to Adapt to 'Radically Changing World' Owen, Ted // San Diego Business Journal;5/20/2002, Vol. 23 Issue 20, p46
Presents views on managing radical change in jobs. Commitment to the job; Acceptance of ambiguity and uncertainty; Accountability of results.
- The grass isn't always greener. Jones, Chandrika M. // Black Enterprise;Nov98, Vol. 29 Issue 4, p54
Offers advice for employees on finding happiness within their chosen careers. Sample cases of employees switching to other careers; Importance of knowing why one was hired; Learning to communicate in the job environment; Listing one's accomplishments; Changing jobs; Changing professions.
- How can you make the most of a career break? // Bloomsbury Business Library - Get the Best from a Career Break;2005, piv
A quiz concerning career break is presented.
- Career Fear. Bried, Erin E. // Glamour;Jan99, Vol. 97 Issue 1, p82
Reveals the indications that a person is afraid of career commitment, from Linda Barbanel, author of `Sex, Money & Power.' Ways to improve one's position before making another change.


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has The controller has Some adblockers wireless outdoor security cameras reviews
USA DVDDistributor 2006 USA DVD DVD-R "Lawman: The Souvenir 1.
The monitoring systems come down in less than 6 inches x 7 inches.
Nice pix good to have a listen at some point I wouldn't have to set up on my HTC m8. Just says caroo stopped when the equipment included.
119 friends 140 reviews Was this review helpful Was this review …. Useful 7 Funny Cool David Z.


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Inspired by Ferragamo's iconic rainbow wedge, created in 1938 for Judy Garland, the Sara Battaglia for Salvatore Ferragamo capsule collection of handbags lets you show your true colors. ARTICLE PUBLISHED: 05/06/16
Men's underwear brand the Eighth created a custom pair of printed skivvies for this month's edition of Andy's Candy. ARTICLE PUBLISHED: 05/06/16
Filled with passion, soul, and authenticity, Washington D.C. born and based artist Chaz French planted his seed in 2014 with his debut album Happy Belated, and in December 2015, he released his follow-up These Things Take Time. ARTICLE PUBLISHED: 03/24/16
Jupe by Jackie designer Jackie Villevoye created a custom shirt and tie for this month's Andy's Candy. ARTICLE PUBLISHED: 02/26/16
"We wanted to pay homage to Andy's shadow prints and use of color, so we used the simple backdrop of our luxe collection sheets as a striking contrast to the vibrancy of the shades," explain Brooklinen founders Vicki and Rich Fulop, who created a custom set of their lavish yet affordable bed linens for this month's Andy's Candy. ARTICLE PUBLISHED: 11/17/15
Stacked with big, layered swooning hooks, slinky and powerful vocals, and an '80s-esque throughline that recalls the isolating intimacy of Cocteau Twins, Tamaryn's latest album Cranekiss sets aside subtlety in favor of a sophisticated celebration of the pop song. ARTICLE PUBLISHED: 08/26/15


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| | More
We want to RUSH this book out to you as soon as possible. Select below to purchase the appropriate shipping and handling for your FREE copy of Lynn's book, The 100 Best Things I've Sold on eBay.
An entertaining, touching, and inspiring chronicle of the author's most memorable eBay adventures, The 100 Best Things I've Sold on eBay uses the world of online auctions as the setting for a personal story of friendship, loss, and growth.
Lynn Dralle is the granddaughter of Cheryl Leaf, an antiques dealer and larger-than-life personality who passed away in August of 2000 at the age of 88. Lynn literally grew up in the antiques business; she started accompanying her grandmother to antique shows at the age of seven, and over the years came to depend not only on her grandmother's business insights, but on her wisdom, strength of character, and humor. All of these played a part in Lynn's journey towards learning how to be an eBay expert.
Near the end of her grandmother's life, Lynn returned home to help run the family antiques store. She eventually began buying and selling on eBay to pay for her grandmother's nursing home expenses. As Lynn weaves memories of her time with her grandmother into stories about the items she has sold on eBay, she creates a book that is partly a memoir of the woman who inspired and brought together her entire family and partly a behind-the-scenes look at what it really takes to succeed at online auctions. Lynn share's what she's found to be the top products sold online, tips for selling items on eBay, and her greatest scores.
Through it all, Lynn's fresh and enthusiastic voice keeps the tone upbeat. This book will appeal to readers who enjoy stories about family as well as those who just like to read about auction successes! You'll learn to be an eBay expert alongside Lynn as she shares her tips for selling items on eBay.Get your FREE copy now! Simply select below to purchase the appropriate shipping and handling for your FREE copy of Lynn's book, The 100 Best Things I've Sold on eBay.
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Yesterday I got up at the crack of dawn and headed to NYC for the Wendy Williams show.
#1 I don't watch. I just wanted a day in NY no kidds, no worries, jus hanging out.
We were there pretty early - 7:40ish got good placement in line but they put us waaaaaaay up top.
#2 I was irked.
It was definitely interesting to watch everything that goes into putting on a LIVE TV show. The makeup, the host, the guests, I will say I enjoyed it. (Oh, the love affair with the thai stone, is so OVER!)
#3 I think we failed "the look" test. Boooo!!!
I was wearing jeans, cute shoes and a navy military style jacket. My natural hair (in twist) was just tied back with a plain headband. One of my friends was natural and the other a professional but similar dress style – casual - cute. But I will admit we were not NY fabulous and perhaps we could have "put it on" a bit more. Well Wendy you're no Oprah, but point taken.
You live and learn. Not sure I would go back for Wendy, but I did have a
good great time visiting! We had lunch, cocktails, sightseeing, a girls day out!
Here was one of my favorite things at the show:
LYBO (laughing your behind off) ;)


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This property has been removed by the agent. It may be sold or temporarily removed from the market
3 bedroom house for saleThe Limes, Stony Stratford, Milton Keynes
Sold STC £310,000
Property Description
Key features
- Semi Detached House
- Large Lounge
- Large Extended Kitchen/Dining Room
- Conservatory
- Three Bedrooms
- Ground Floor Shower Room
- First Floor Bathroom
- Off-road Parking & Garage
- Convenient Location
Full description
An extended three bedroom semi detached house with a garage and benefiting from a large kitchen and a large living room.
The property has accommodation set over two floors to comprise a hall, ground floor shower room, large living room, extended kitchen/dining room and a conservatory. On the first floor there are three bedrooms and a bathroom. The property has front and rear gardens, off-road parking and a good size garage. The Limes is a popular road within walking distance of the town centre and picturesque riverside walks on the outskirts of the town.
Ground Floor - A good size hall has stairs to the first floor and doors to the shower room and lounge.
The shower room has a modern white suite comprising w.c., wash hand basin set into a vanity unit and shower cubicle.
The large living room has a feature fireplace with a gas coal effect fire. Solid oak floorboards. Window to the front and patio doors to the conservatory.
The kitchen/dining room has two defined areas. The dining area has space for a table and French doors to the garden and an understairs cupboard. The kitchen area has been fitted in an extensive range of solid wood fronted units to wall and base levels with roll-top worksurfaces over and a ceramic sink. Appliances to remain include the range cooker and an integrated dishwasher. Stone tiling with under-floor heating for the floor and a door to the garage.
First Floor - The landing has a window to the side, access to the loft and doors to all rooms.
Bedroom one is a double bedroom located to the rear, bedroom two is a double bedroom located to the front and bedroom three is a single bedroom located at the front.
The family bathroom has a white suite comprising low level w.c., wash hand basin and bath with a shower over, varnished floorboards and a window to the rear aspect.
Exterior - The front garden is partly enclosed by a mature hedge and has a driveway providing off-road parking for two cars.
The rear garden is enclosed by fencing and has a paved patio area and step up to the lawn with stocked beds.
Garage - Attached good size single garage with an up and over door and a rear access door to the kitchen.
Heating - The property has gas to radiator central heating.
Location - Stony Stratford - An attractive and historic coaching town referred to as the Jewel of Milton Keynes. The town is set on the north/western corner of Milton Keynes and is bordered to most sides by attractive countryside and parkland with lovely riverside walks. The attractive and well used High Street has many historic and listed buildings and offers a diverse range of shops that should suit all your day to day needs.
Disclaimer - Whilst we endeavour to make our sales particulars accurate and reliable, if there is any point which is of particular importance to you please contact the office and we will be pleased to verify the information for you. Do so, particularly if contemplating travelling some distance to view the property. The mention of any appliance and/or services to this property does not imply that they are in full and efficient working order, and their condition is unknown to us. Unless fixtures and fittings are specifically mentioned in these details, they are not included in the asking price. Some items may be available subject to negotiation with the Vendor.
More information from this agent
To view this media, please visit the on-line version of this page at www.rightmove.co.uk/property-for-sale/property-57016261.html
Energy Performance Certificates (EPCs)
To view this media, please visit the on-line version of this page at www.rightmove.co.uk/property-for-sale/property-57016261.html
Listing History
Map & Street View
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Market Info
Disclaimer - Property reference 26442612. The information displayed about this property comprises a property advertisement. Rightmove.co.uk makes no warranty as to the accuracy or completeness of the advertisement or any linked or associated information, and Rightmove has no control over the content. This property advertisement does not constitute property particulars. The information is provided and maintained by Carters Estate Agents, Stony Stratford & Milton Keynes . Please contact the selling agent or developer directly to obtain any information which may be available under the terms of The Energy Performance of Buildings (Certificates and Inspections) (England and Wales) Regulations 2007 or the Home Report if in relation to a residential property in Scotland.
Map data ©OpenStreetMap contributors.


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Surya Caesar CAE1027-810OV Hand Tufted Rug, 8' x 10' Oval
Item #: 901-1323165SUR
Model #: CAE1027-810OV
Brand: Surya
Not yet rated.Be the first to Write a Review
$904.20 Each
Product Highlights
- Brand: Surya
Help with furniture delivery, assembly,...Read more + Read less -
protection plans and more.
Plus, you've got choices! You'll find options for those DIYers on a budget, those that want us to do all the work and everyone in-between. Want all the details? Get them right here.
Get an attractive decor accent like the Surya Caesar CAE1027-810OV Hand Tufted Rug, 8' x 10' Oval to dress up your floor Grace your living room or office lobby with this attractive "Surya Caesar CAE1027-OV Hand Tufted Rug". Made from wool, you can have a beautiful room with this transitional style rug. Mix and match your room decor with this black & gray rug to give it a complete look. Designed to complement most decor themes, this trendy color makes a smart choice for contemporary as well as classic style set up. Designed to depict a oval, it measures 8' x 10' that is apt for most spaces.
- Color: Beige/Burgundy/Charcoal/Chocolate/Mocha/Moss/Olive/Rust/Slate/Taupe
- Pattern: Floral
- Material: 100% Wool
- Country of Origin: India
- Dimensions: 8' x 10'
- Style: Transitional
- Hand tufted
- Indoor Rug
- Pile Height: 0.63"
|Brand : Surya
|Weight : 60.00 lbs. per Each
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text:
About Japura Scholarship Scheme (JSS)About Japura Scholarship Scheme (JSS)
The Japura Scholarship Scheme is our flagship program where young undergraduates are provided with some financial assistance during their studies. In our short history of 5 years since 2011, over 4 million rupees has been distributed among 120+ students. All these distributions were made from the investment income while preserving initial sponsor capital, a unique feature of our scholarship offering. We thank all our scholarship sponsors for the trust and confidence placed on us to manage their hard earned money. Today, we manage over 7 Million rupees of such donations capital and continue to provide guarantee to sponsors. JSS is the brainchild of Japura Alumni's first president, Jayamini Kariyawasam and many other dedicated team members have contributed over the years to make this a sustainable program.
How JSS work.
JSS operates on three simple principles.
JSS sponsorship unit
Investment for a JSS unit is set at $4,000 for next five years. (2016-2020). One-time payment of AU$4,000 will give you the right to nominate a scholarship recipient for the life of JSS. (As long as JSS in operation)
Inflation effect on student contributions and investment income returns are taken in to account in determining this value and next review would be undertaken in early 2020.
Student benefit
The amount of student payment varies from year to year according to annual investment income. However, we have managed to maintain student benefit over the last 5 years in Rs.25,000 to 35,000 range per year.
Application process
Undergraduate students enrolled in University of Sri Jayewardenepura as of 1st November each year with at least 1 year of academic year ahead of them are eligible to apply. Scholarships are awarded for 10 month (from March to December). Online applications are accepted from 1st of November to 31st December each year.


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Our Cincinnati cosmetic surgery lawyers don't think there's anything pretty about botched procedures
When we visit a health care facility, we expect all health care providers to help us and treat us according to the highest standards, but that does not always happen. When medical treatment does not meet the standard for adequate care and causes harm rather than good, you may have a medical malpractice claim. Whether you needed emergency treatment, a regular checkup or cosmetic surgery, if you were injured after receiving substandard medical care, you could be entitled to compensation.
Just call 1-800-ELK-OHIO to have your case reviewed by one of our experienced, knowledgeable Cincinnati personal injury attorneys or contact us online.
Lawyers and medical professionals who have represented injury victims for over 50 years
For over 50 years, Elk & Elk has taken on large insurance companies and corporations in pursuit of the compensation our medical malpractice victims need. We work hard to provide clients with effective legal representation after cosmetic surgery mistakes such as:
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- Infection
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We have the resources to find the facts and prove your case
Our attorneys can help you get your life back on track if you have been injured by a substandard cosmetic surgical procedure. Our approach to proving challenging malpractice claims begins with our team of doctors, nurses, other medical professionals and life care consultants who can assess what happened in your case. We also have access to accountants, forensic engineers, investigators and other experts to get you the compensation you need.
Call 1-800-ELK-OHIO to schedule your free consultation if you have suffered from a cosmetic surgical error
If you or someone you know has been injured by a cosmetic surgery mistake, you can rely on the Cincinnati medical malpractice attorneys at Elk & Elk. Call our Cincinnati cosmetic surgery lawyers today for a free consultation. We're available 24 hours a day, seven days a week, 365 days a year. Call 1-800-ELK-OHIO or contact us online.


text: Lounge SoHo to Open in Greenwich The 16,000-square-foot store with a rock 'n' roll vibe that closed on Broadway in 2009 will be reborn on April 20 in Connecticut. By Sharon Edelson on March 20, 2012 NEW YORK — Lounge SoHo, the edgy 16,000-square-foot store on Broadway with a rock 'n' roll vibe that closed in 2009, will be reborn on April 20 in Greenwich, Conn. While preppy and conservative Greenwich seems like an incongruous match for Lounge's club kid aesthetic, owner Jack Menashe said, "the new Lounge is not going to feel really rock 'n' roll. Greenwich is perfect for launching Lounge." The polished 2,000-square-foot flagship, opposite Saks Fifth Avenue, will focus on contemporary."This is the first of many, many stores," Menashe said. "I'm very actively looking for other locations. We could open a downtown store and we could have a store on the Upper East Side or Upper West Side of New York. It takes a while to find the right powerful locations. I don't want little baby stores. I want a lot of traffic." Menashe said he's working on deals at top malls in the area. An outlet store is bowing at Jersey Gardens in Elizabeth, N.J., in August. Menashe said he's negotiating a lease for a third store and plans to unveil four locations in 2013, then three to four units a year thereafter. Asked how the stores are being financed, he said, "Jack Menashe Inc." Menashe tried to roll out Lounge stores before. A unit was slated for the Cosmopolitan Resort & Casino in Las Vegas, but the owner defaulted on the property. A Lounge at Aventura Mall, north of Miami, closed in 2009. Menashe in May 2010 launched the Limelight Marketplace, 25,000 square feet of shops, restaurants and cafes housed in a former Gothic Revival church on Sixth Avenue and 20th Street here. A year after opening, Menashe reimagined the concept as a department store. "I handed it over to my partners a year ago and they're operating it now," he said. "I'm not really that in touch with them. I built it, sweated it, leased it and finished it. That was all part of the plan."Unlike the original Lounge SoHo, which closed in 2009, men's wear won't be sold at the Greenwich store. "We're targeting a 22- to 45-year-old woman," Menashe said, "someone very trendy and very sophisticated. There's a big void in the contemporary ladies' retail market. There's a lot of juniors stores, but Forever 21 is controlling everything."In addition to brands such as Jamison, Madison Marcus, Rory Becca, Chelsea Flower, Liebskind, Botkier and Haute Hippie, Lounge SoHo will sell a private label brand, priced from $100 to $400. Art Zulu, a design and branding company with clients such as Sean John and Jennifer Lopez, is helping with Lounge SoHo's branding.The merchandise mix, 50 percent branded and 50 percent private label, "will encompass the whole downtown lifestyle," Menashe said. "It's all designed for the mother shopping with her daughter. The store is moody and dark with luxurious finishes. Lounge SoHo stores have a real downtown personality and that's the way our buyer has been buying. A dressy top with a pair of hot jeans and a pair of high-heeled shoes. That's the mix." load comments blog comments powered by Disqus


text:
We all want our children to be intelligent and make every effort to encourage a healthy learning experience, but do we already have smart babies? New research shows that metacognition has been found in younger children, which means babies might already be thinking deeper than we … [Read more...]
Tips To Having an All Natural Birth
All natural births seem to be the newest craze, but for many people it is just the way they feel comfortable giving birth to their new bundle of joy. It has been done for generations, so having a natural birth should seem like an easy thing to accomplish, but with today's … [Read more...]


text:
BUENOS AIRES -- Banking sources said Argentina's creditor banks have elected to convert at least 80% of the country's $23 billion of commercial debt into par-value bonds under the proposed restructuring agreement.
Most of the creditors had reportedly submitted their choices - between the par and discount bond options - by midday Monday, rather than by last Friday's deadline.
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text:
Adipose Organ Laboratory
Adipose Organ Laboratory
Vernochet C.,Harvard University |
Mourier A.,Max Planck Institute for Biology of Ageing |
Bezy O.,Harvard University |
Bezy O.,Pfizer |
And 16 more authors.
Cell Metabolism | Year: 2012
Obesity and type 2 diabetes are associated with mitochondrial dysfunction in adipose tissue, but the role for adipose tissue mitochondria in the development of these disorders is currently unknown. To understand the impact of adipose tissue mitochondria on whole-body metabolism, we have generated a mouse model with disruption of the mitochondrial transcription factor A (TFAM) specifically in fat. F-TFKO adipose tissue exhibit decreased mtDNA copy number, altered levels of proteins of the electron transport chain, and perturbed mitochondrial function with decreased complex I activity and greater oxygen consumption and uncoupling. As a result, F-TFKO mice exhibit higher energy expenditure and are protected from age- and diet-induced obesity, insulin resistance, and hepatosteatosis, despite a greater food intake. Thus, TFAM deletion in the adipose tissue increases mitochondrial oxidation that has positive metabolic effects, suggesting that regulation of adipose tissue mitochondria may be a potential therapeutic target for the treatment of obesity. © 2012 Elsevier Inc.
Neuhofer A.,Medical University of Vienna |
Neuhofer A.,Christian Doppler Laboratory |
Zeyda M.,Medical University of Vienna |
Zeyda M.,Christian Doppler Laboratory |
And 15 more authors.
Diabetes | Year: 2013
Obesity-induced chronic low-grade inflammation originates from adipose tissue and is crucial for obesity-driven metabolic deterioration, including insulin resistance and type 2 diabetes. Chronic inflammation may be a consequence of a failure to actively resolve inflammation and could result from a lack of local specialized proresolving lipid mediators (SPMs), such as resolvins and protectins, which derive from the n-3 polyunsaturated fatty acids eicosapentaenoic acid (EPA) and docosahexaenoic acid (DHA). We assessed obesity-induced changes of n-3-derived SPMs in adipose tissue and the effects of dietary EPA/DHA thereon. Moreover, we treated obese mice with SPM precursors and investigated the effects on inflammation and metabolic dysregulation. Obesity significantly decreased DHA-derived 17-hydroxydocosahexaenoic acid (17-HDHA, resolvin D1 precursor) and protectin D1 (PD1) levels in murine adipose tissue. Dietary EPA/DHA treatment restored endogenous biosynthesis of n-3-derived lipid mediators in obesity while attenuating adipose tissue inflammation and improving insulin sensitivity. Notably, 17-HDHA treatment reduced adipose tissue expression of inflammatory cytokines, increased adiponectin expression, and improved glucose tolerance parallel to insulin sensitivity in obese mice. These findings indicate that impaired biosynthesis of certain SPM and SPM precursors, including 17-HDHA and PD1, contributes to adipose tissue inflammation in obesity and suggest 17-HDHA as a novel treatment option for obesity-associated complications. © 2013 by the American Diabetes Association.
Vitali A.,Marche Polytechnic University |
Murano I.,Marche Polytechnic University |
Zingaretti M.C.,Marche Polytechnic University |
Frontini A.,Marche Polytechnic University |
And 3 more authors.
Journal of Lipid Research | Year: 2012
White and brown adipocytes are believed to occupy different sites in the body. We studied the anatomical features and quantitative histology of the fat depots in obesity and type 2 diabetes-prone C57BL/6J mice acclimated to warm or cold temperatures. Most of the fat tissue was contained in depots with discrete anatomical features, and most depots contained both white and brown adipocytes. Quantitative analysis showed that cold acclimation induced an increase in brown adipocytes and an almost equal reduction in white adipocytes; however, there were no significant differences in total adipocyte count or any signs of apoptosis or mitosis, in line with the hypothesis of the direct transformation of white into brown adipocytes. The brown adipocyte increase was accompanied by enhanced density of noradrenergic parenchymal nerve fibers, with a significant correlation between the density of these fibers and the number of brown adipocytes. Comparison with data from obesity-resistant Sv129 mice disclosed a significantly different brown adipocyte content in C57BL/6J mice, suggesting that this feature could underpin the propensity of the latter strain to develop obesity. However, the greater C57BL/6J browning capacity can hopefully be harnessed to curb obesity and type 2 diabetes in patients with constitutively low amounts of brown adipose tissue. Copyright © 2012 by the American Society for Biochemistry and Molecular Biology, Inc.
Cinti S.,Marche Polytechnic University |
Cinti S.,Adipose Organ Laboratory
DMM Disease Models and Mechanisms | Year: 2012
The main parenchymal cells of the adipose organ are adipocytes. White adipocytes store energy, whereas brown adipocytes dissipate energy for thermogenesis. These two cell types with opposing functions can both originate from endothelial cells, and co-exist in the multiple fat depots of the adipose organ - a feature that I propose is crucial for this organ's plasticity. This poster review provides an overview of the adipose organ, describing its anatomy, cytology, physiological function and histopathology in obesity. It also highlights the remarkable plasticity of the adipose organ, explaining theories of adipocyte transdifferentiation during chronic cold exposure, physical exercise or lactation, as well as in obesity. White-to-brown adipocyte transdifferentiation is of particular medical relevance, because animal data indicate that higher amounts of brown adipose tissue are positively associated with resistance to obesity and its co-morbidities, and that 'browning' of the adipose organ curbs these disorders. © 2012. Published by The Company of Biologists Ltd.
Tran K.-V.,University of Massachusetts Medical School |
Gealekman O.,University of Massachusetts Medical School |
Frontini A.,Marche Polytechnic University |
Zingaretti M.C.,Marche Polytechnic University |
And 9 more authors.
Cell Metabolism | Year: 2012
Adipose tissue expansion involves the enlargement of existing adipocytes, the formation of new cells from committed preadipocytes, and the coordinated development of the tissue vascular network. Here we find that murine endothelial cells (ECs) of classic white and brown fat depots share ultrastructural characteristics with pericytes, which are pluripotent and can potentially give rise to preadipocytes. Lineage tracing experiments using the VE-cadherin promoter reveal localization of reporter genes in ECs and also in preadipocytes and adipocytes of white and brown fat depots. Furthermore, capillary sprouts from human adipose tissue, which have predominantly EC characteristics, are found to express Zfp423, a recently identified marker of preadipocyte determination. In response to PPARγ activation, endothelial characteristics of sprouting cells are progressively lost, and cells form structurally and biochemically defined adipocytes. Together these data support an endothelial origin of murine and human adipocytes, suggesting a model for how adipogenesis and angiogenesis are coordinated during adipose tissue expansion. © 2012 Elsevier Inc.


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I am a nobody. If the different classes of America were color-coded, I would be in the yucky brown, one rung up from the bottom. I grew up in Naples, Florida and live near the Mississippi River now with my husband and two dogs. I am part of the slowly disappearing middle-class. I was a musician most of my life: drummer/singer/keyboards—but I retired before the plastic surgery flu hit. I have no degrees, which could be a good thing…depending on how you view our educational system. I do have three patents…but that really doesn't make me a somebody. The one thing that is constant in my life is my OPINIONS, which i have more than perhaps even Carl Sagan could have imagined…mostly political. (yes…my ancestors were crabby buggers)
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The Marijuana Craving Questionnaire (MCQ) is a valid and reliable, 47-item self-report instrument that assesses marijuana craving along four dimensions: compulsivity, emotionality, expectancy, and purposefulness. For use in research and clinical settings, we constructed a 12-item version of the MCQ by selecting three items from each of the four factors that exhibited the greatest within-factor internal consistency (Cronbach's alpha coefficient).
Adult marijuana users (n = 490), who had made at least one serious attempt to quit marijuana use but were not seeking treatment, completed the MCQ-Short Form (MCQ-SF) in a single session.
Confirmatory factor analysis of the MCQ-SF indicated good fit with the 4-factor MCQ model, and the coefficient of congruence indicated moderate similarity in factor patterns and loadings between the MCQ and MCQ-SF. Homogeneity (unidimensionality and internal consistency) of MCQ-SF factors was also consistent with reliability values obtained in the initial validation of the MCQ.
Findings of psychometric fidelity indicate that the MCQ-SF is a reliable and valid measure of the same multidimensional aspects of marijuana craving as the MCQ in marijuana users not seeking treatment.
Marijuana (cannabis) is the most commonly used illicit drug throughout the world (Coffey et al., 2002; Degenhardt et al., 2008, Perkonigg et al., 2008). In the United States, prevalence among the population aged 12 and older is 40% for lifetime use and 6% for past month use (Substance Abuse and Mental Health Services Administration, 2007). Across various countries, prevalence of lifetime marijuana dependence ranges from 1% to 7% (Chen et al., 2005; Coffey et al., 2002; Stinson et al., 2006; Perkonigg et al., 2008). Craving is identified as a symptom of marijuana dependence (Coffey et al., 2002) and marijuana withdrawal (Budney et al., 2004; Copersino et al., 2006; Haney, 2005). Craving is typically described as a strong drive or urge, serving to promote continued drug use (dependence symptom) or to trigger relapse during abstinence (withdrawal symptom) (American Psychiatric Association [APA], 2000; Pickens and Johanson, 1992).
Marijuana craving has been reported in individuals seeking treatment and in laboratory studies with daily marijuana users. Among adults presenting for treatment, McRae et al. (2007) found that marijuana-dependent patients reported greater levels of marijuana craving than cocaine-dependent patients reported cocaine craving. In a separate treatment sample, 93% of marijuana-dependent adults reported experiencing mild craving for marijuana, and 44% rated their past craving as severe (Budney et al., 1999). A retrospective survey of marijuana users reporting about their most recent quit attempt revealed that craving was second only to irritability in severity and frequency; more than 50% of participants indicated that craving had contributed to failed quit attempts (Budney et al., 2008). Similarly, craving was the most frequent (82%) withdrawal symptom endorsed by marijuana-dependent adolescents seeking treatment (Cornelius et al., 2008). Daily marijuana users participating in residential (Haney et al., 2004) and nonresidential (Vandrey et al., 2008) laboratory studies reported significant increases in craving during periods of marijuana deprivation. Laboratory studies have also reported increased craving in response to marijuana-related imagery scripts (Singleton et al., 2002) and visual pictures (Wolfling et al., 2008) compared to neutral stimuli.
An impediment to a full understanding of the role of craving in addiction is the lack of agreement regarding its clinical significance, meaning, and measurement (Pickens and Johanson, 1992; Sayette et al., 2000). For example, DSM-IV does not list craving as a criterion of substance dependence (APA, 2000); however, craving is an optional diagnostic criterion in ICD-10 (World Health Organization, 2005). The varied conceptualizations of craving (Heishman et al., 2001) have yielded inconsistent approaches to measurement. The majority of studies described in the preceding paragraph assessed marijuana craving using single-item questions that have face validity, but precluded the determination of internal consistency and reliability (Tiffany, 1992; Wewers et al., 1990). To overcome these deficiencies, measures of craving have been developed, using one to three items assessing urges and desires (e.g., Kozlowski et al., 1996). However, neither single items nor any single measure captures the varied nature of craving experienced by individuals along the drug-dependence continuum and the range of theoretical perspectives on craving (Verheul et al., 1999; Mezinskis et al., 2001). Given the absence of a psychometrically valid instrument with which to measure such multiple dimensions of marijuana craving, we developed the Marijuana Craving Questionnaire (MCQ).
The MCQ is a 47-item multidimensional scale covering a broad range of clinically and theoretically distinct explanations of marijuana craving. In the initial validation study (Heishman et al., 2001), the MCQ was administered to 217 current marijuana smokers not seeking treatment. Exploratory and confirmatory factor analyses yielded 17 items with significant loadings on four latent constructs (factors) that characterized marijuana craving. We examined item content and correlations between factor scores and variables commonly found in marijuana studies to assign meaning to the factors: 1) compulsivity, an inability to control marijuana use; 2) emotionality, use of marijuana in anticipation of relief from withdrawal or negative mood; 3) expectancy, anticipation of positive outcomes from smoking marijuana; and 4) purposefulness, intention and planning to use marijuana for positive outcomes. The four MCQ factor subscales had respectable internal consistencies, exhibited low to moderate positive intercorrelations, and were significantly correlated with history of marijuana use and a wide range of single-item measures of craving. Singleton et al. (2002) further documented the reliability and validity of the 47-item MCQ by demonstrating internal consistency and unidimensionality of the four factors, suggesting that each factor was tapping unique dimensions of marijuana craving. The validity of the MCQ as a state measure of craving has been demonstrated by increases in factor scores after exposure to marijuana-related visual, tactile, and olfactory cues (Lundahl et al., 2007) and auditory imagery scripts that differed in the intensity of marijuana-urge content (Singleton et al., 2002).
A disadvantage of the 47-item MCQ is that it takes 7 min to complete (Heishman et al., 2001), which likely would limit its use in clinical settings where patients are assessed with numerous forms and in research studies where measures are repeated frequently. Indeed, more than one-third of participants in the initial validation study suggested eliminating item repetition. Theoretically, a shorter form of any multiple-item questionnaire can be created without reducing reliability (Tiffany et al., 2000). One approach to constructing a shorter, yet reliable, scale would be to use only the MCQ items with significant factor loadings, but even a 17-item questionnaire might prove too lengthy to administer and score. Additionally, either all or most items on two of the factors (emotionality and purposefulness) were worded negatively to reduce variance due to acquiescence and might be more indicative of participants' inattention to rating than with their response to item content. Although we included practice items to ensure that participants understood the rating scale, negatively-worded items required additional calculations before summing scores for each factor.
There is no generally accepted limit to the minimum number of items required to maintain psychometric fidelity between original and brief versions of any instrument, although there is agreement that at least three indicators (items) per factor are desirable in the development and validation of multidimensional scales (Marsh and Hau, 1999). Thus, we constructed a 12-item version of the MCQ (MCQ-Short Form, MCQ-SF) by retaining 6 of the 17 items with significant factor loadings (3 items each as indicators for Factors 3 and 4) and by selecting 6 of the remaining 11 items that exhibited the greatest within-factor internal consistency (Cronbach's alpha coefficient) as indicators for Factors 1 and 2 (3 items each). We worded all items in the positive direction, consistent with development of brief versions of similarly-constructed craving questionnaires (Cox et al., 2001; Heishman et al., 2008; Paliwal et al., 2008). We estimated that completion of the MCQ-SF would take about 30 sec, based on results with a similar 12-item tobacco craving scale (Heishman et al., 2004; 2008).
The purpose of this study was to compare the factor structure of the MCQ-SF to that of the MCQ by administering the MCQ-SF to an independent sample of marijuana smokers who were not interested in reducing or quitting their marijuana use. We hypothesized that the MCQ 4-factor structure would be replicated in the MCQ-SF. We examined items for congruence in factor patterns and loadings between the MCQ and MCQ-SF. We also included questions about the intensity, frequency, and duration of recent marijuana craving to explore the convergent validity of the MCQ-SF.
Marijuana smokers (n = 490) were recruited from the greater Baltimore community via print, radio, and television advertisements. Inclusionary criteria were: at least 18 years old and having made at least one "serious" (self-defined) attempt to quit marijuana. Participants gave written informed consent according to guidelines for the protection of research volunteers of the U.S. Department of Health and Human Services and were paid for their participation. The NIDA Institutional Review Board approved the study.
The study consisted of a single session lasting about 45 min. Participants completed a questionnaire about the "most difficult time you had intentionally stopping all marijuana use while not in a controlled environment such as jail or hospital," including reasons for quitting, coping strategies, and withdrawal symptoms (data to be reported elsewhere). Participants then completed the MCQ-SF and eight additional questions concerning their current, past week, or past month marijuana craving (definition, frequency, duration, change, and intensity). Questions about craving intensity were rated on a 100-mm visual analog scale (VAS), anchored from low to high or low to most ever in life.
The distribution of MCQ-SF items based on the 4-factor scale structure of the MCQ is shown in Table 1. Items were rated on a Likert-type scale from 1 (strongly disagree) to 7 (strongly agree). Factor scores for each participant were obtained by summing the 3 items in each factor scale, yielding a score ranging from 3 to 21. The MCQ-SF factors were operationally defined the same as those of the MCQ: 1) compulsivity, an inability to control marijuana use; 2) emotionality, use of marijuana in anticipation of relief from withdrawal or negative mood; 3) expectancy, anticipation of positive outcomes from smoking marijuana; and 4) purposefulness, intention and planning to use marijuana for positive outcomes. In the initial validation study (Heishman et al., 2001), estimates of internal consistency (Cronbach's alpha; Cronbach, 1951) of MCQ Factors 1-4 and number of items in each factor (in parentheses) were 0.82 (7), 0.78 (4), 0.55 (3), and 0.68 (3), respectively.
The statistical package Comprehensive Exploratory Factor Analysis (CEFA; Browne et al., 2004) was used to determine if the MCQ-SF maintained the 4-factor structure of the MCQ. We conducted confirmatory factor analysis (CFA) using Maximum Wishart Likelihood estimation and oblique rotation with Kaiser normalization to a least squares fit to match the 4-factor MCQ target matrix. Target specification for the assignment of MCQ-SF items to each respective factor matched the manner in which similar items were assigned to the same factor in the MCQ: Factor 1 would include items 2, 7, and 10; Factor 2 would include items 4, 6, and 9; Factor 3 would include items 5, 11, and 12; and Factor 4 would include items 1, 3, and 8. Models assumed no higher-order factors, correlated first-order factors, and uncorrelated residuals. Goodness-of-fit for the unrotated factors was examined using the Steiger-Lind root mean square error of approximation statistic (RMSEA; Steiger, 1980) produced in CEFA. We used hypothesis tests developed to test the statistical significance of the fit (Browne and Cudeck, 1993) for the 4-factor model, with exceedance probabilities for perfect fit (H0: RMSEA = 0) and close fit (H0: RMSEA ≤ 0.05). For RMSEA, values < 0.05 constitute good fit, values 0.05-0.08 acceptable fit, values 0.08-0.10 marginal fit, and values > 0.10 poor fit of the model (Browne and Cudeck, 1993).
We compared next the rotated matrices of factor loadings obtained for the 4-factor MCQ-SF model (comparison) and for the assigned items in the original MCQ model (target) using Tucker's coefficient of congruence (f) as a statistical index of similarity in factor patterns and magnitude of factor loadings between sets of factors derived from identical items (Wrigley and Neuhaus, 1955). Empirical studies indicate f values of 0.70-0.79 represent moderate, 0.80-0.89 high, and > 0.90 very high similarity between target and comparison factors (Koschat and Swayne, 1991; ten Berge, 1986).
We evaluated homogeneity of factors two ways. First, we conducted principal components analysis (PCA) of the assigned items for each MCQ-SF factor. If more than one component per factor was retained by the PCA, this would indicate a significant departure from unidimensionality for that factor. Second, Cronbach's alpha coefficients and inter-item correlations were calculated for each factor. We conducted internal consistency reliability and inter-item analyses to examine further whether each factor contained an optimal set of items that measured a unique aspect of craving.
Forward stepwise multiple regression analysis was conducted to determine the subset of Factors 1-4 that best predicted current, past-week, and past-month intensity of marijuana craving (VAS). Only factors with significant betas were retained. Multivariate analysis of variance (MANOVA) was used to test differences in factor scores as a function of how participants defined craving and to test the hypothesis that factor scores varied as a function of self-reported frequency and duration of marijuana craving. The tests of significance were based on Wilks' lambda and were converted to F values (Rao's R) by means of a set of procedures developed by Rao (1951).
The majority of participants were Black (83%) and male (58%). The sample comprised 240 Black men (49%), 169 Black women (35%), 46 White men (9%), and 35 White women (7%). Mean age was 31.2 years (S.D. = 10.3). Participants reported first marijuana use at age 14.8 (S.D. = 3.2), first regular (at least once per week) marijuana use at age 16.6 (S.D. = 3.7), and an average of 5.4 (S.D. = 7.7) lifetime quit attempts. Eighty-five percent had used marijuana during the past month, 9% in the past 2-12 months, and 6% had not used marijuana for at least a year. The only sex difference was that women began marijuana use 1.5 years later than men (15.7 vs. 14.2, p < 0.001). There were no racial differences. A correlational pattern hypothesis for equality of correlation matrices indicated that combining the race and sex subgroups was justified, RMSEA = 0.029, χ2 (198) = 218.81, p > .14.
For comparison, we summarize briefly the sample demographics of the initial MCQ validation study (Heishman et al., 2001). Of the 217 participants, 79% were male, 50% were Black, and 44% were White. Mean age was 31.4 years (S.D. = 7.5). Participants reported first marijuana use at age 15.3 (S.D. = 3.9), use of marijuana for 14.3 years (S.D. = 3.9), and an average of 4.3 (S.D. = 6.7) lifetime quit attempts. Goodness of fit of correlational pattern hypotheses for several subgroups within the sample, indicated that the factor structure of the original validation sample was unaffected by differences in demographics.
Table 2 compares factor loadings of the MCQ-SF with those of the MCQ validation study (Heishman et al., 2001). CFA of the MCQ-SF items showed a close fit with the 4-factor target model, χ2 (24, n = 490) = 32.20; RMSEA = 0.026 (90% confidence interval = 0.000-0.055), perfect fit p > 0.122, close fit p > 0.965. Factor scale means (S.D.) were 7.6 (4.8), 8.9 (5.5), 10.3 (5.6), and 11.5 (6.3) for Factors 1-4, respectively.
Factors exhibited positive intercorrelations (all p's < 0.001), with Pearson's r ranging from 0.43 (Factor 1 with Factor 3) to 0.78 (Factor 2 with Factor 3). Cronbach's alpha coefficient and average inter-item correlation (in parentheses) were 0.61 (0.34), 0.75 (0.51), 0.72 (0.46), and 0.84 (0.64) for Factors 1-4, respectively. Individual PCA extracted only one component per factor; component loadings exceeded 0.72 for all items comprising each factor. The variance accounted for was 56%, 67%, 64%, and 75% for Factors 1-4, respectively. The congruence coefficient (f) was 0.78.
Participants were asked to indicate on average the intensity of marijuana craving for the past month, past week, and right now on a VAS, anchored from low to high. There was a trend towards decreased intensity with recency of the time period [past month (M = 49.7, S.D. = 32.4); past week (M = 48.5, S.D. = 33.8); right now (M = 41.8, S.D. = 35.9)]. Participants also rated intensity of current craving on a VAS from low to most ever in life (M = 33.0, S.D. = 30.2). Multiple regression revealed that all MCQ-SF factors were positively and significantly associated with current craving intensity; β ranged from 0.10 (Factor 3) to 0.45 (Factor 4), all p's < 0.05. Factors 1, 3, and 4 were positively and significantly associated with past month intensity (β = 0.14, 0.21, and 0.31, respectively), and with past week intensity (β = 0.14, 0.19 and 0.37, respectively), all p's < 0.001. Factors 1, 2, and 4 were positively and significantly associated with intensity of current craving compared to most ever in life (β = 0.19, 0.19 and 0.32, respectively), all p's < 0.001.
Participants were asked to choose between two definitions of craving for marijuana. They were almost evenly divided between craving as "only a strong urge or desire to smoke marijuana" (53%) versus "any urge or desire to smoke marijuana, even a weak one" (47%). There was no difference between the two response groups on Factors 1-4, Rao's R (4, 482) = 0.42, p > 0.46.
Participants were asked to indicate the average frequency (number of times per day) and duration (in minutes) of their craving for marijuana during the past week. A majority of participants (57%) reported craving marijuana 1-4 times per day, and 18% reported more than 5 episodes per day; 22% reported no craving episodes. With respect to the duration of each craving episode, 56% reported less than 30 min, and 20% reported greater than 30 min. Fig. 1 shows mean MCQ-SF factor scale scores as a function of frequency and duration of craving episodes. MANOVA indicated significant increases in factor scores as a function of increasing frequency, Rao's R (20, 1546) = 8.68, p < 0.001, and duration, Rao's R (28, 1667) = 4.81, p < 0.001. Univariate F tests indicated significant main effects for frequency and duration for all factors (all p's < 0.001). Excluding participants who reported no frequency or no duration of craving did not change outcomes of either the MANOVA or univariate F tests.
Participants were also asked to indicate how their craving for marijuana had changed during the past week; the majority (73%) reported no change. MANOVA indicated significant increases and decreases in factor scores as a function of change, Rao's R (8, 962) = 7.09, p < 0.001. Univariate F tests indicated significant main effects for change for all factors (all p's < 0.001). Post hoc tests revealed that scores on all factors were significantly lower for participants who reported decreased craving compared with those who reported either increased or no change in craving during the past week (all p's < 0.01). Only Factor 4 scores were significantly higher for participants who reported increased craving compared with those who reported no change during the past week (p < 0.01). Finally, there was no difference between the two definitional response groups (section 3.4) on frequency, duration, and change of craving (all p's > 0.23).
We developed the MCQ to be a multidimensional questionnaire using clinically- and theoretically-based categories of craving and found that four factors best characterized marijuana craving. Confirmatory factor analysis of the 4-factor MCQ-SF model indicated good fit to the 4-factor MCQ model. We specified a priori how the MCQ-SF items would empirically fit into four factors, corresponding to item fit on the MCQ. The coefficient of congruence indicated moderate similarity in factor patterns and loadings between the MCQ and MCQ-SF. Visual inspection of the rotated factor structure indicated that factor patterns for significant items (> 0.30) loaded exactly between target (MCQ) and comparison (MCQ-SF) factors, suggesting convergent validity (Kline, 2005). These findings suggest that the MCQ-SF measures the same four latent constructs as the MCQ.
The common practice of assigning items to the factor with the highest loading would have resulted in item 6 being assigned incorrectly to Factor 3 and item 11 being assigned incorrectly to Factor 2. We conducted internal consistency reliability and inter-item analyses to delete all items that were not consistent with Factors 2 and 3 (not shown), but this would have resulted in marked reductions for Factor 2 with item 6 removed (Cronbach's alpha = 0.64 vs. 0.75) and for Factor 3 with item 11 removed (Cronbach's alpha = 0.60 vs. 0.72). Given that some similar items loaded on the same factor (e.g., items 2 and 7, Factor 1), we also examined whether it was possible to delete one of the pair to make the MCQ-SF even shorter without sacrificing reliability. In each case, deleting one item reduced Cronbach's alpha. Retaining all 12 items resulted in a high intercorrelation among the four primary factors, which could indicate that an alternative model with one secondary higher-order factor might explain much of the common variance. Hierarchical factor analysis, however, yielded two secondary higher-order factors influencing four primary factors. Thus, the four factors of the MCQ-SF demonstrate the same unique variance as the MCQ.
Internal consistency reliability estimates ranged from 0.61 (Factor 1) to 0.84 (Factor 4). There were differences in reliability coefficients between the MCQ and MCQ-SF. Cronbach's alpha for MCQ-SF Factors 1 and 2 decreased, whereas Factors 3 and 4 increased compared with Cronbach's alpha for corresponding MCQ factors. Although there is no commonly agreed minimum alpha level (Cortina, 1993; Schmitt, 1996), 0.70 has become convention (Nunnally, 1978). As defined by Cronbach (1951) and elaborated by others (Kaiser & Michael, 1975), alpha is a single-sample measure of internal consistency. Both internal consistency and unidimensionality are needed to establish homogeneity of factor scales. Thus, the central issue is not only whether the three items in each factor are internally consistent, but also are they tapping one dimension of craving.
We used established procedures to evaluate unidimensionality (Cortina, 1993; Schmitt, 1996). According to these authors, when a measure has desirable properties, such as meaningful content coverage and reasonable unidimensionality, low alpha should not be the sole impediment to its use. In this study, PCAs extracted only one measured component per factor, indicating no significant departure from unidimensionality and suggesting that each factor consistently tapped a unique aspect of marijuana craving. If a test is unidimensional, then it has sufficient internal consistency (Gardner, 1995). Taken together, goodness-of-fit, congruence of factors, homogeneity (unidimensionality and internal consistency), and uniqueness of factors suggest that the MCQ-SF reliably measures the same multidimensional aspects of marijuana craving as the MCQ.
Similar to the initial MCQ valiadation study (Heishman et al., 2001), a nearly equal number of participants in the present study defined craving for marijuana as "only a strong urge or desire" or "any urge or desire." Participants endorsing one definition or the other did not differ with respect to MCQ-SF factor scores. This finding with marijuana users is consistent with responses from users of other drugs, including cocaine (Tiffany et al., 1993), alcohol (Kozlowski et al., 1989), and nicotine (Heishman et al., 2003).
Scores on all MCQ-SF factors increased as a function of increasing frequency and duration of craving episodes. Participants who reported craving three or more times per day and those whose cravings lasted more than 10 min had significantly higher scores on all MCQ-SF factors compared with participants who reported no daily craving (Fig. 1). In general, factor scores did not plateau, which might have suggested effective coping skills to prevent escalating craving. Individuals reporting the most frequent and longest lasting craving episodes may be at greatest risk for relapse to marijuana use following a quit attempt. Future studies utilizing ecological momentary assessment (e.g., Epstein et al., in press) are needed to examine relationships between frequency and intensity of craving episodes and marijuana use.
Several limitations of the study should be mentioned. The reliability and validity of the MCQ and MCQ-SF have been investigated in marijuana users who were not interested in reducing or quitting their marijuana use. Thus, these results may not generalize to those trying to quit, former-users, or those who use marijuana only occasionally. The sample comprised a large proportion of Blacks and men; however, the correlational pattern hypothesis test suggested that the factor structure of the MCQ-SF was unaffected by race or sex. Future testing of the MCQ-SF with a more balanced sample may identify a different factor structure. Finally, we have not investigated the utility of the MCQ-SF or MCQ in predicting treatment outcomes. Because self-reported craving is a predictor of treatment outcome among other drugs of abuse (Heinz et al., 2006; Killen et al., 2006; Mol et al., 2007; Paliwal et al., 2008), evaluation of the MCQ-SF in a treatment trial is a next logical step for future validity and reliability testing.
To our knowledge, the MCQ and MCQ-SF are the only multidimensional questionnaires for the assessment of marijuana craving. In this study, we report on the development, reliability, and validity of the MCQ-SF. Results suggest that the MCQ-SF is as valid and reliable as the 47-item MCQ in measuring marijuana craving. Replication of the psychometric properties in an independent sample with different characteristics from the MCQ sample demonstrates further the fidelity between the original and brief versions of the questionnaire. The MCQ-SF provides an assessment of marijuana craving that is minimally burdensome to participants and easy to administer and score.
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